-
rvestd o
increases in return expectation on buying activity. Portfolio
risk levels and changes are more systemat-ically related to return
and risk expectations. In line with nancial theory, risk taking
increases withreturn expectations and decreases with risk
expectations. In response to their expectations, investors
alsoadjust the riskiness of assets they trade.
2014 Elsevier B.V. All rights reserved.
at na
investors have been shown to hold underdiversied portfolios
different from pure meanvariance optimization (Lewellen et
al.,1977; Grinblatt and Keloharju, 2000). Often these deviations
havebeen explained by specic psychological biases, e.g.,
excessivetrading by overcondence (Odean, 1998; Glaser and Weber,
2007).
tion on beliefs and preferences is needed.xpectations in
avestors ate not reprding instit
which imposes some limits on the generality of the resultsever,
our focus is on individual investors for which our samrather
typical. Participants are well informed about nancial mar-kets as,
e.g., their responses in a nancial literacy questionnaireshow. They
also have on average many years of investment expe-rience and
invest non-trivial amounts of money. In three-monthintervals,
survey participants are queried for numerical and quali-tative
expectations and their risk tolerance. We then match expec-tations
of investors to their actual transactions in their online
Corresponding author. Address: Lehrstuhl fr ABWL und
Finanzwirtschaft,Universitt Mannheim, 68131 Mannheim, Germany.
Tel.: +49 6211811531; fax:+49 6211811534.
E-mail address: [email protected] (C. Merkle).
Journal of Banking & Finance 46 (2014) 372386
Contents lists availab
Journal of Bank
w.(Goetzmann and Kumar, 2008), to trade frequently (Odean,
1999;Barber and Odean, 2000), to take high idiosyncratic risk
(Calvetet al., 2007), and to gamble in the stock market (Kumar,
2009).There is also evidence that they use various investment
strategies
To this end, we collect return and risk erepeated panel survey
of self-directed private inUK online brokerage provider. These
investors artive for the overall investor population
incluhttp://dx.doi.org/10.1016/j.jbankn.2014.03.0420378-4266/ 2014
Elsevier B.V. All rights reserved.a largeesenta-utions,. How-ple
isindividual investor behavior and what can be observed in
theiractual behavior. Portfolio theory assumes that investors
formexpectations about return and risk of securities and select
portfo-lios according to their expectations and risk
preferences(Markowitz, 1952). As a consequence, they should hold
broadlydiversied portfolios and trade very little. But instead,
private
Empirically, there is only scarce evidence on this question as
theinput parameters are hard to obtain. The economic paradigm
ofrevealed preferences states that beliefs and preferences can
beinferred from observed actions (Samuelson, 1938). But this
alreadyimplies that they are perfectly converted into actions. In
order toreveal whether and where this transfer might fail, direct
informa-D81G02G11
Keywords:ExpectationsBeliefsRiskReturnTrading behaviorPortfolio
choice
1. Introduction
There is a large gap between wh nce models predict for
However, this way one learns very little about the actual
deci-sion making process people go through when they invest. Howdo
investors use their beliefs and preferences in this
process?Available online 24 April 2014
JEL-Classication Codes:
expectations, and risk tolerance of these investors in
three-month intervals between 2008 and 2010. Wecombine the survey
data with investors actual trading data and portfolio holdings. We
nd that investorbeliefs have little predictive power for immediate
trading behavior. The exception is a positive effect ofDo investors
put their money where theiexpectations and investing behavior
Christoph Merkle , Martin WeberChair of Finance and Banking,
University of Mannheim, Germany
a r t i c l e i n f o
Article history:Received 21 February 2013Accepted 30 March
2014
a b s t r a c t
To understand how real inpanel survey of self-directe
journal homepage: wwmouth is? Stock market
ors use their beliefs and preferences in investing decisions, we
examine anline investors at a UK bank. The survey asks for return
expectations, risk
le at ScienceDirect
ing & Finance
elsevier .com/locate / jbf
-
ankibrokerage accounts. We observe volume, timing, and direction
ofall trades within the survey period, and are able to calculate
port-folio holdings of participants.
We develop different measures of nancial risk taking based
ontrading behavior and portfolio holdings of investors. In a rst
step,we consider the direction of stock trading and calculate the
ratio ofbuys over total trades, referred to as buysell ratio. This
corre-sponds to an increase or decrease in investors total equity
posi-tion. We nd that the absolute levels of expectations for
marketreturn and risk do not predict buying and selling behavior.
Anexplanation could be that previous expectations are
alreadyreected in investors portfolios and there is no need for
investorsto engage in further transactions. We therefore also test
whetherchanges in expectations explain buying and selling behavior
corre-sponding to trades reecting changes in portfolios. Indeed,
improv-ing return expectations have a positive impact on buysell
ratios.Thus, quite intuitively, positive return expectations foster
buyingactivity, but there is no effect of changes in risk
expectations or riskattitude on buysell ratios.
While immediate trading behavior and direction of trade is
ameans to alter ones risky position, we also directly
investigateportfolio risk. We calculate portfolio volatility and
beta for inves-tors in our panel as standard risk measures. This is
complementedby additional measures such as relative volatility and
averagecomponent volatility (Dorn and Huberman, 2005). We
considerboth, levels of portfolio risk at the point in time of
survey roundsand changes in portfolio risk between survey rounds.
Levels ofrisk taking of investors can be well explained by their
beliefs,preferences and demographics. All portfolio risk measures
arepositively related to return expectations and risk tolerance,
andnegatively related to risk expectations, age, and wealth of
inves-tors. These results are consistent with nancial theory and
previ-ous literature.
An advantage of our dataset is that it allows studying
thedynamics of this relationship between expectations and risk
tak-ing, i.e., whether investors react to changes in expectations
bychanging their portfolio composition and thus alter risk
exposure.For the volatility measures this is the case, as we nd a
positivechange in volatility when return expectations improve and a
neg-ative change if investors expect increasing stock market risk.
Therelationship is weakest for short-term volatility and portfolio
beta,indicating that investors manage their portfolios rather based
onlong-term volatility as a proxy for risk taking. Our results
arerobust to several alternative specications including the use
oflagged values to address endogeneity concerns. Risk
toleranceremains insignicant in most of our regressions (both
levels andchanges), which sheds some light on the debate, whether
investorscan translate their level of risk aversion into an
adequate portfoliochoice (Ehm et al., 2014).
Finally, we combine the perspectives of trades and portfolio
riskand analyze the volatility of transactions by investors. This
allowsus to gain a deeper understanding of how investors regulate
theirportfolio risk. The analysis reveals that more optimistic
investorsshift part of their investments to more volatile
securities. In addi-tion to expanding their total equity position
by purchases in excessof sales, they also buy riskier assets. This
is consistent with thending that portfolio volatility not just
passively moves with mar-ket volatility, but also relative
portfolio volatility increases for opti-mistic investors.
We continue with a theoretical motivation and an overview
ofrelated literature in Section 2, followed by a description of the
dataset, which contains two main sources, the survey and the
tradingdata. In Section 4 we present results about the
relationship
C. Merkle, M. Weber / Journal of Bbetween investor expectations
and trading behavior, which wethen discuss in Section 5. A nal
section concludes.2. Theory and literature
People acting on their beliefs and preferences are such a
basicassumption in economic theory that it has seldom been
contested.Exemplarily, portfolio theory as the canonical nance
model positsthat investors form expectations about return and risk
of securitiesand then choose an optimal portfolio according to
their risk prefer-ences (Markowitz, 1952). We will now in a more
formal but simpleway derive directional predictions for the inuence
of returnexpectations, risk expectations, and risk tolerance on
nancial risktaking behavior.
We assume an investor to have power utility dened overwealth W
of the form UW W1h 1=1 h. Power utilityhas the desirable property
of declining absolute risk aversion andconstant relative risk
aversion, which is most consistent with realworld observations. The
investor in a simple two-period economyfaces the budget constraint
W1 W01 r0;1, implying that theonly source of wealth at time t = 1
is wealth in t = 0 plus the returnearned on wealth. The
corresponding maximization problem thusis:
maxE0W01 r0;11h=1 h: 1Under the additional assumption that
future wealth W1 is lognor-mally distributed, expression (1)
simplies to (for a detailed deriva-tion cp. Campbell and Viceira,
2002):
max ln E01 r0;1 12 hr20; 2
where r20 is the conditional variance of the log return,r20
Var0ln W1W0 Var0ln1 r0;1. In expression (2) the ingredientsof the
maximization problem are visible: the investor trades offexpected
return against expected risk (variance of returns). Theparameter h
of the utility function describes the investors relativerisk
aversion.
With only two assets, a risky asset s and a riskless asset f,
returnon wealth is r0;1 rf ;0;1 ws;0rs;0;1 rf ;0;1, where ws;0
representsthe weight an investor puts on the risky asset. However,
whiler0;1 is a linear combination of the two asset returns, the log
returnon wealth cannot be expressed as a linear combination of the
logreturns. Instead, Campbell and Viceira (2002) suggest a
Taylorapproximation to rewrite (2) in the form
max ws;0E0rs;0;1 rf ;0;1 12ws;01ws;0r20
121 hw2s;0r20; 3
which can be solved by
ws;0 E0rs;0;1 rf ;0;1 r20=2
hr20: 4
The equation implies that the share of risky investment
shouldincrease with expected returns for the risky asset, and
decreasewith risk expectations and risk aversion. This result can
be general-ized to a multi-asset or multi-period framework and is
fairly robustto the relaxation of several of the chosen
assumptions. A simplemeanvariance optimization comes to the same
conclusions, asdoesfrom a slightly different anglerisk-value theory
(Sarin andWeber, 1993). We take the results of this model as a
predictionfor the role of expectations and risk preferences in
investingbehavior.
Empirically, risk taking behavior of individual investors
hasbeen studied using different approaches and datasets.
Vissing-Jorgensen (2003) analyzes a US individual investor survey
byUBS/Gallup and nds a strong positive effect of expected returnon
equity share in self-reported investor portfolios. Dorn and
ng & Finance 46 (2014) 372386 373Huberman (2005) report
portfolio volatilities for a sample ofGerman brokerage clients and
identify risk aversion as most
-
predictive for portfolio volatility. Moreover, younger,
self-employed, less sophisticated, and poorer investors tend to
holdmore risky portfolios. Calvet et al. (2007) examine
disaggregatedwealth data covering the entire Swedish population and
show apositive impact of wealth, income, and education on risk
taking
3. Data
We obtain survey responses and transaction data for a sampleof
clients at Barclays Stockbrokers, a UK direct brokerage
provider.Barclays is one of the largest brokers in the UK and
attracts a widevariety of customers (for demographic
characteristics of its clientssee below). The accounts are
self-directed in the sense that cus-tomers can inform themselves on
special webpages provided bythe bank but receive no direct
investment advice. Most transac-tions are processed online.
3.1. Survey data
In collaboration with Barclays Wealth, we conduct a
repeatedsurvey taking place every three months, beginning in
September2008 and ending in September 2010. Fig. 1 shows the
developmentof the UK stock market represented by the FTSE all-share
index andthe timing of survey rounds. Our panel consists of nine
rounds cov-ering a time period of highly volatile market
environment. We thusexpect participants to express changing beliefs
about market pros-pects; in the standard model of Eq. (4) this
would in turn lead tochanges in their portfolios.
In the initial survey a stratied sample of the banks client
basewas invited via e-mail to participate in the online
questionnaire(for details on the sampling procedure see Weber et
al., 2013). Intotal 617 clients of the bank participated in the
survey, 394 ofwhichparticipated multiple times. 189 participants
have completed atleast ve rounds, and 52 have participated in all
nine rounds. Wehave a minimum of 130 observations for each of the
nine rounds.
Table 1
374 C. Merkle, M. Weber / Journal of Banking & Finance 46
(2014) 372386measured by portfolio volatility.1 They also break
down portfoliorisk in its various components and reveal interesting
patterns of risktaking. In a follow-up study, Calvet et al. (2009)
present evidence onrebalancing, suggesting that investors actively
control their share ofrisky investments and offset changes brought
about by passive mar-ket variations.
While this literature addresses risk taking behavior of
privateinvestor, it lacks a systematic study of the input variables
we areinterested in: individual investor beliefs in form of return
and riskexpectations, and investor risk preferences. Closest
related to ourstudy is the work by Amromin and Sharpe (2009), Weber
et al.(2013), Hoffmann et al. (2013), and Guiso et al. (2011).
Similar tous Amromin and Sharpe (2009) use panel data, in their
case comingfrom the Michigan Survey of Consumer Attitudes. However,
theyanalyze self-reported portfolio shares of survey participants
anddo not have access to their transactions or actual portfolios.
Theyconcentrate on the interrelation of return expectations and
riskexpectations, but also provide some evidence of the inuence
ofthese variables on portfolio composition. Consistent with
nancialtheory, higher return expectations and lower risk
expectationsincrease the share of equity in portfolios of
investors. Hoffmannet al. (2013) study an investor survey in the
Netherlands, whichis matched to brokerage account data. Their data
spans a timeperiod from April 2008 to March 2009 and survey rounds
areadministered monthly. By eliciting expectations and
portfoliocharacteristics, Hoffmann et al. (2013) establish a link
betweenthe beliefs of investors and their investing behavior. They
nd apositive impact of risk tolerance, risk perception, and return
expec-tations on trading activity, while risk tolerance is identied
as amain driver for risk taking behavior.
Guiso et al. (2011) concentrate in their analysis on risk
aversionmeasured by a qualitative and a quantitative approach. They
reporta substantial increase of risk aversion in the nancial crisis
com-pared to pre-crisis levels. Ownership of risky assets is
negativelyrelated to risk aversion. Guiso et al. (2011) suggest
psychologicalfactors as drivers of risk aversion, as they are able
to rule out alter-native explanations such as wealth or background
risk.
In a previous analysis of our dataset, Weber et al. (2013)
reporta relationship between expectations and investing decisions.
Theyanalyze a survey question which asks participants to split a
hypo-thetical amount of 100,000 between an investment in the
UKstock market and a riskless asset. With this investment task
theyare able to show a strong inuence of changes in expectationsand
risk attitude on changes in the proportion of risky investment.This
inuence is in the expected direction: increases in expectedreturns
or risk tolerance lead to an increase in risky investment,while
higher risk expectations render investors more cautious.We extend
this research by relating return and risk expectationsto the actual
trades and portfolios of investors. By analyzing vari-ous aspects
of investing behavior, we present a more complete por-trayal of the
underlying relationships. We also exploit the full timeseries of
the survey which was not available to the earlier study byWeber et
al. (2013).
1 The seemingly contradictory results might be explained by the
differentcomposition of the datasets. While Dorn and Huberman
(2005) analyze stockportfolios, where wealth and nancial
sophistication usually lead to a better
diversication (and thus less risk), Calvet et al. (2007) use
total wealth portfoliosfor which wealth and sophistication
typically lead to a greater equity share (and thusmore
risk).Demographics of participants.
n Mean Median Std.dev. Min Max
Age (in years) 613 51.4 53 12.9 21 84Gender (male = 1) 617 0.93
1 0.25 0 1Financial literacy
(% correct)614 3.49 4 0.68 0 4
Wealth (in categories) 502 4.80 5 2.39 1 9Income (in categories)
494 3.88 4 1.80 1 8
Notes: The table shows descriptive statistics about demographics
of participants.Age is reported in years, gender as a dummy
variable taking a value of 1 for maleparticipants. Financial
literacy is the number of correct responses in a 4-itemWe will
discuss potential selection effects in Section 4.4.Table 1 shows
some demographic characteristics of survey par-
ticipants. Investors are predominantly male, and they are older
andmore afuent than the general population (for an explicit
Fig. 1. FTSE all-share index and survey rounds. Development of
the FTSE all-shareindex (covers 98% of UK market capitalization)
between June 2008 and December2010. Vertical lines represent the
timing of the nine survey rounds.nancial literacy test (see
Appendix A). Wealth and income are self-reported andmeasured in
categories (see Appendix A). Number of observations varies due
torefusals.
-
Risk tolerance of investors is measured as agreement to
thestatement It is likely I would invest a signicant sum in a high
riskinvestment (on a seven-point scale). The statement is part of
amore complete assessment of risk attitude (eight items) in
theentry questionnaire to our survey. Factor analysis and
Cronbachsalpha show high consistency between the items, and for
brevitythe set of statements was reduced to one for the panel
survey.The selected statement was chosen not for wording, but for
statis-tical properties such as to capture maximal information from
themulti-dimensional measure (for the construction of
psychometricrisk tolerance scores cp. also Egan et al., 2010;
Kapteyn andTeppa, 2011). The correlation between the eight-item
risktolerance score and single-item risk tolerance is 0.77 for the
entryround when both were elicited. Weber et al. (2013) nd high
pre-
Fig. 3). While condence intervals are too narrow in the initial
sur-vey round, investors seem to learn from observed outcomes
that
anking & Finance 46 (2014) 372386 375comparison see again
Weber et al., 2013). However, they closelyresemble typical investor
populations in other studies (e.g.,Barber and Odean, 2001). The
nancial literacy of survey partici-pants is relatively high with on
average 3.5 correct responses outof four questions. This exceeds
values usually found for these ques-tions in household surveys (van
Rooij et al., 2011).
We elicit beliefs about return and risk expectations in two
ways,by a numerical question asking for return expectations in
percentageterms and a more subjective evaluation of risk and
returnon a bipolar scale. The wording of the numerical question is
asfollows:
We would like you to make three estimates of the return of the
UKstock market (FTSE all-share) by the end of the next three
month.
Your best estimate should be your best guess. Your high estimate
should very rarely be lower than the actual out-come of the FTSE
all-share (about once in 20 occasions).
Your low estimate should very rarely be higher than the actual
out-come of the FTSE all-share (about once in 20 occasions).
Please enter your response as a percentage change.
The question asks participants to predict the three-monthreturn
of the UK stock market. We use this time horizon to
avoidoverlapping observations as the distance between survey
roundsis three month as well. One might argue that these
short-termexpectations will be irrelevant, if investors have a
longer invest-ment horizon. However, we nd them to be highly
correlated withone year expectations which were elicited twice
during the survey.We suspect that three-month expectations express
an investorscurrent optimism or pessimism about the market not
limited tothe particular time interval. In addition, high portfolio
turnoverreported below implies that short-term expectations
shouldcertainly matter.
In a design similar to Glaser and Weber (2005), participants
haveto submit a best estimate as well as a high and a low estimate,
whichtogether yield a90%-condence interval.We take thebest estimate
torepresent an investors returnexpectationabout
theUKstockmarket.The high and low estimates allow calculating
implicit expected vola-tility of investors which we use as
numerical risk estimate applyingthe method of Keefer and Bodily
(1983). We use this indirect way asit has been shown that people
often have difculties with numericrisk estimates (Windschitl and
Wells, 1996; Dave et al., 2010).
Furthermore, numeric estimates may not cover all aspects
ofexpected risks and benets which are partly emotional. The
risk-as-feelings hypothesis maintains that subjective risk
perceptionswill often differ from cognitive assessment of risk
(Loewensteinet al., 2001). It is unclear, whether investors
primarily act on theirnumerical expected volatility or an affective
impression of risk.The nance literature uses many different ways to
measure riskexpectations, and it is still debated which best
explains investorbehavior (Hoffmann et al., 2013; Weber et al.,
2013). We thereforeinclude qualitative questions, which ask people
to evaluate returnand risk on a seven-point scale.
How would you rate the returns you expect from an investment
inthe UK stock market (FTSE all-share) over the next 3 months?
Over the next 3-months, how risky do you think the UK stock
mar-ket (FTSE all-share) is?
In the rst question answer alternatives range from extremelybad
to extremely good, in the second question from not risky
C. Merkle, M. Weber / Journal of Bat all to extremely risky. We
ask equivalent questions for inves-tors own portfolios heldwith
Barclays. In total we thus collect eightbelief items per investor
per round.extreme realizations are possible and enlarge their
condenceintervals. Expected volatility thus increases, but is still
belowimplied option volatility. Furthermore after the initial
adjustment,the condence intervals remain insensitive to subsequent
marketdevelopments.dictive power of the single-item risk tolerance
measure for hypo-thetical investment decisions. Besides the core
variables ofbeliefs and preferences, the survey asks for
demographics, psycho-logical dispositions, and investment
objectives. All variables usedin our analysis are described in
Appendix A.
3.2. Survey responses
Average numeric return expectations are relatively low beforethe
peak of the nancial crisis, then rise during the crisis and
fallagain, when the UK stock market recovers. Fig. 2 shows the
patternin detail. In general investors tend to be more optimistic
abouttheir own portfolios: the average return expectations are
consis-tently higher and the difference is non-trivial
(24%-points). Incontrast to market expectations, average portfolio
expectationsremain high throughout 2009 and only decline
afterwards. Whilemarket expectations are in a reasonable range
adding up to anannual return of 812% (compared to a FTSE all-share
historicalreturn of about 8%), the absolute level of portfolio
expectationsseems unrealistically high (probably explained by
overcondencecp. Merkle, 2012).
Investors in our panel (numerically) underestimate stock mar-ket
risk (cp. Glaser et al., 2013). The implied volatilities
calculatedfrom the condence intervals of investors return
expectations aremuch lower than volatility expectations of
sophisticated marketparticipants (represented by implied option
volatilities, seeFig. 2. Numerical return expectations of
investors. Average quarterly returnexpectations of investors for
their own portfolio and the UK stock market (FTSEall-share).
-
trading volume is 72,805. We observe most pronounced
tradingactivity in the initial phase of the nancial crisis;
investors seemto feel a need to react to the turbulent times on
asset markets.
nking & Finance 46 (2014) 372386Compared to the quantitative
measure, qualitative risk expecta-tions elicited on a seven-point
scale reect more closely impliedmarket risk expectations
represented by the FTSE 100 VIX. Whileit is not possible to compare
the absolute magnitudes, we nd acorrelation of 0.78 (p < 0:02)
between average qualitative riskexpectations and implied option
volatilities. Quite intuitively, riskexpectations rise with the
peak of the nancial crisis and then fallafterwards. However, there
are two further increases in panelistsrisk expectations: one
without a corresponding rise in option mar-ket expectations
(September to December 2009), and another,which falls together with
the onset of the European debt crisis(June 2010). In general,
expectations for own portfolio risk followthis trend but are on
average slightly lower and more stable thanmarket expectations. It
is noteworthy that investors appear tobelieve they can earn higher
returns bearing less risk (cp. Kempfet al., 2014).
For investigating trading behavior over time, changes in
expec-tations are particularly important. Table 2 shows average
changesfor all expectation variables. We observe a signicant
increase inaverage return and risk expectations between round one
and threefollowed by a very mixed pattern from round three to four
(furtherincrease of qualitative return and numerical risk
expectations, butsharp drop of qualitative risk expectations).
Changes in expecta-tions are less pronounced for the time after the
immediate crisis.An exception is the very last survey round for
which we observestrongly increasing return expectations and
decreasing risk expec-tations. Similar to Weber et al. (2013), we
nd that the correlationsbetween changes of numeric and qualitative
expectations are often
Fig. 3. Risk expectations of investors. Qualitative risk
expectations for market andown portfolio (scale 17, right axis),
and numerical risk expectations as implied bycondence intervals
(volatilities, left axis). For comparison implied option
volatility(FTSE 100 VIX, left axis).
376 C. Merkle, M. Weber / Journal of Balow (return) or
insignicant (risk). Stronger correlations existbetween market and
portfolio expectations. Average risk toleranceremains fairly stable
over the whole survey period.
3.3. Trading data
Our data also include the trading records of all investors
activein the panel survey. We include three months prior to our rst
sur-vey round and three months after our last survey round. In
theresulting period between June 2008 and December 2010 weobserve
49,372 trades with a total trading volume of258,940,694. Of these
trades 37,022 or 75% are in stocks (63% oftrading volume). In some
parts of the analysis, we will concentrateon these equity
transactions as they are closest related to theexpectations we
elicit among investors. The remaining tradesinclude bonds,
derivatives, mutual funds and ETFs. The average tra-der in the
panel trades 84.1 times within the 2.5 year period (aboutthree
times per month), with an average trading volume of441,126.
However, the distribution is strongly skewed; the med-ian trader
trades only 33 times (about once a month), the medianCombining
trading data with a snapshot of investors portfolios,we are able to
calculate portfolio statistics for our survey period.The median
portfolio is worth 41,687 (average 314,663) andmedian portfolio
turnover on a per round basis (three months) is19% (mean 77%),
which means that the median investor turns overhis portfolio about
twice in the survey period of 2.5 years, andsome turn over their
portfolio ten times or more.2
We use the transaction records to develop several measures
ofrisk taking behavior. As we cannot directly observe the share
ofrisky assets as described in Eq. (4), we dene two alternatives
thatcover different aspects of risk taking. First, we consider the
balanceof purchases and sales of stocks in the trading records of
investors,as in most cases, extending ones equity position
corresponds to anincrease in nancial risk taking, while a reduction
of ones equityposition corresponds to a decrease in risk taking. We
form tworatios of buys divided by total trades, based on the number
andvolume of investors equity transactions, respectively. The
ratiosthus attain values between 0 and 1. Similar buysell ratios
havebeen used by Ritter (1988), Grinblatt and Keloharju (2000),
andBhattacharya et al. (2012).
We expect buysell imbalance to be related to investors
stockmarket expectations: with high return expectations for the
stockmarket, the propensity to buy should rise relative to the
propensityto sell, while the opposite effect is predicted for high
risk expecta-tions and high risk aversion. More precisely, only
changes in expec-tations and preferences should be relevant for
changes in portfolios(cp. Weber et al., 2013). However, as this is
a stark theoreticalassumption, we analyze both levels and changes
of expectations.
A second strategy to assess nancial risk taking of investors
isby measures of portfolio risk such as volatility and beta (cp.
Dornand Huberman, 2005; Calvet et al., 2007; McInish, 1982).
Financialtheory posits that the composition of the risky portfolio
should notchange, but risk is entirely adjusted via the share of
the risky port-folio (fund separation, Tobin, 1958). However, in
practice there arelarge differences in composition and risk of
portfolios suggestingthat investors manage their overall risk
taking at least in part byportfolio risk. Therefore, we apply the
theoretical predictions inEq. (4) also to portfolio risk measures,
and expect higher portfoliorisk in response to a positive change in
return expectations or anegative change in risk expectations.
We calculate volatility of portfolios over one-year and
overthree-month horizons. We calculate portfolio beta over a
one-yearhorizon using the FTSE all-share index as corresponding
marketindex (this choice seems justied as survey participants hold
mostof their investments (>90%) in the UK stock market). Taking
intoaccount that within a volatile market environment a large part
ofthe changes in portfolio volatility will be passively caused
bychanges in market volatility, we also measure relative
volatilityas the ratio of portfolio volatility divided by market
volatility.Dorn and Huberman (2010) argue that portfolio volatility
is notthe correct measure of risk, if investors disregard
correlationsbetween securities. They propose a value-weighted
average ofthe return volatilities of portfolio components (ACV),
whichreects risk taking if investors mainly orient themselves at
the vol-atility of individual securities rather than portfolio
volatility. Again,we consider levels and changes of these
variables. Exact denitionsof all variables can be found in Appendix
A.
2 Compared to similar studies, portfolio value is high. Glaser
and Weber (2007)report a median portfolio value of 15,630, Barber
and Odean (2000) of $16,210,
and Dorn and Huberman (2005) of DM55,000 (about 23,000). On a
monthly basis,median turnover is in the same range as in Barber and
Odean (2000) and Dorn andHuberman (2005) with 6% and 9%
respectively.
-
3.4. Descriptive statistics of investor risk-taking
Table 2Changes in expectations of investors.
Market
Round D risk tolerance D num. return D qual. return D num.
ris
2 (December 08) 0.23 0.020 0.12 0.023
3 (March 09) 0.10 0.014 0.20 0.0014 (June 09) 0.07 0.010 0.30
0.0145 (September 09) 0.15 0.008 0.01 0.0086 (December 09) 0.14
0.016 0.03 0.0117 (March 10) 0.03 0.004 0.05 0.0048 (June 10) 0.21
0.008 0.27 0.0019 (December 10) 0.22 0.009 0.45 0.015
Notes: The table states changes in risk tolerance and changes in
numerical and qualitati Changes are signicantly different from zero
at 10%-level (one-sided t-test). Changes are signicantly different
from zero at 5%-level (one-sided t-test). Changes are signicantly
different from zero at 1%-level (one-sided t-test).
C. Merkle, M. Weber / Journal of BankiFor all rounds, average
buysell ratios exceed 50%, whichimplies that investors are net
buyers. There is almost no differencebetween ratios based on number
of trades and volume, correlationis 0.94 (p < 0:01). We observe
the highest buysell imbalance forlate 2008, at the peak of the
nancial crisis, when the ratios reachabout 0.66. This suggests that
investors in our sample view the cri-sis as an opportunity to buy
at low prices. There is also large cross-sectional variation in
buysell ratios between investors, which iscrucial for our analysis
of the differential inuence of expectationsand preferences.
Fig. 4 displays portfolio volatilities of the median investor,
therst-quartile investor, and third-quartile investor in our panel
atthe time of each survey round. The volatility of the FTSE
all-shareindex serves for comparison. Median portfolio volatility
in ourpanel rises from 0.26 in June 2008 to about 0.40 during the
crisis,before falling to values around 0.18 for the last year of
the survey.It remains constantly above market volatility, which
indicates thata majority of investors hold portfolios that are
riskier than the UKmarket portfolio. The difference between median
portfolio volatil-ity and market volatility is strongly signicant
for all rounds(p < 0:01, Wilcoxon signed-rank test). The third
quartile showsthat many investors hold very volatile portfolios
compared to themarket index, while the rst quartile is still close
to that index.The average component volatility (ACV, not displayed)
exceedsthese portfolio volatilities by about 40% as it does not
account fordiversication effects.0
0.1
0.2
0.3
0.4
0.5
0.6
0.73rd Qrt Investor
Median Investor
Market
1st Qrt Investor
Fig. 4. Portfolio volatility of investors and UK stock market
volatility. Portfoliovolatility is the one-year standard deviation
of daily portfolio returns at point intime of survey rounds.
Displayed are the median investor, the rst-quartile
andthird-quartile investor. UK stock market volatility uses the
FTSE all-share index.High portfolio volatility of investors is not
due to high levels ofsystematic risk, as the median beta is around
0.8 over the wholesample period and most investors hold portfolios
with a beta smal-ler than one. Instead, high volatility is driven
by idiosyncratic riskas a result of a low degree of diversication.
Relative volatilitiessuggest that investors in the immediate phase
of the nancial crisistry to reduce their risk exposure relative to
the market, while theyincrease it again afterwards. Changes in beta
conrm a reduction insystematic risk for the rst phase of the
crisis, while for laterrounds the results remain inconclusive.
4. Results
4.1. Investor trading behavior
We rst investigate whether market expectations drive thedecision
of investors to increase or decrease their stock marketexposure,
which is measured by buysell ratios. We estimate apanel Tobit model
with random effects as the buysell ratios arelimited on the
interval between 0 and 1, and values on the bound-aries occur
frequently. We consider two specications, one inwhich the absolute
levels of expectations are relevant for investors,and another in
which investors are supposed to react on changes
inexpectations.
Columns 1 and 5 of Table 3 show the results of the buysellratios
regressed on expectation levels. More precisely, we
measureexpectations at the time of the survey and then observe
buysellratios in the three month afterwards until the next survey
takesplace. Levels of expectations seem to have little effect on
subse-quent buying and selling behavior. Among the few marginally
sig-
Own portfolio
k D qual. risk D num. return D qual. return D num. risk D qual.
risk
0.43 0.026 0.09 0.023 0.280.03 0.030 0.20 0.007 0.13
0.77 0.003 0.33 0.018 0.240.38 0.019 0.10 0.008 0.020.07 0.014
0.17 0.008 0.06
0.22 0.047 0.11 0.017 0.120.17 0.010 0.09 0.010 0.13
0.29 0.045 0.35 0.011 0.29
ve expectations of investors (compared to the previous survey
round).
ng & Finance 46 (2014) 372386 377nicant effects is a
negative coefcient for risk tolerance. Anexplanation might be that
risk tolerant investors already hold highequity positions and tend
to reduce their exposure during thenancial crisis. However, this
effect is not robust to the inclusionof additional explanatory
variables.
Changes in expectations are dened over the same time
horizon(between surveys), for which buysell ratios are calculated.
Thelower number of observations in the changes regressions is due
tothe fact that for changes in expectations, we need investors to
par-ticipate in the survey for two consecutive rounds. Among
thechanges variables, changes in numeric return expectations exert
asignicant effect on buysell behavior (columns 2 and 6). If
returnexpectations improve, investors tend to move to the buying
side ofthe market, which is consistent with the theoretic
prediction. Foradditional equity purchases thus not the absolute
level of returnexpectations is relevant, but instead changes in
these expectations.This result is robust to the inclusion of the
levels variables (columns3 and 7) and of demographic variables:
age, gender, wealth, income,and nancial literacy (columns 4 and 8).
Income quite intuitively
-
Table 3Buying and selling behavior.
Buysell ratio Buysell volume ratio
(4
0.0.0.0.0.0.0.
0.0.0.
76
unddinglanainclucK
378 C. Merkle, M. Weber / Journal of Banki & Finance 46
(2014) 372386has a positive effect on buysell ratios as it is a
proxy for additionalliquidity investors might want to invest. For
the remaining demo-graphic variables we nd no signicant effect.
Overall the lowpseudo-R2 in the regressions suggests that the
predictive powerof beliefs for immediate trading behavior is rather
low.
The coefcients in Table 3 represent marginal effects (the
coef-cients for the latent variable), which directly allow an
interpreta-
(1) (2) (3)
Num. return 0.068 0.275
Num. risk 0.059 0.043Qual. return 0.014 0.009Qual. risk 0.007
0.018Risk tolerance 0.010 0.010D num. return 0.150 0.293
D num. risk 0.058 0.074D qual. return 0.010 0.014D qual. risk
0.007 0.016D risk tolerance 0.012 0.007
AgeGender (male = 1)WealthIncomeFin. literacy
Pseudo-R2 0.039 0.035 0.049
n 1376 769 769
Notes: The table shows results of a panel Tobit regression with
random effects and robuys/# of total trades) for columns 14 and
buysell volume ratio dened over trainclude levels of expectations
and columns 2 and 6 changes of expectations as expcolumns 4 and 8
additionally controlled for demographics. Demographic
variableswhich are the coefcients of the uncensored dependent
variable. The pseudo-R2 is M They are signicant at 10%-level. They
are signicant at 5%-level. They are signicant at 1%-level.tion in
terms of economic signicance. A 10%-point increase inreturn
expectations will raise buysell ratios by about three per-cent. For
comparison, moving upward one category in incomehas about the same
effect. In unreported results, we exclude heavytraders (the top 10%
in number of trades and trading volume), asthese investors might be
engaged in trading activity independentof their current beliefs or
other situational factors. When investors,who trade less
frequently, place an order, this order might be moreclosely related
to personal return and risk expectations. However,there is almost
no change in the results under this restriction.For robustness, as
the presented panel Tobit model cannot accountfor potential
heteroscedasticity, we test several alternatives: A lin-ear panel
regression with clustered standard errors by individual, axed
effects regression, and a regression with least absolute devi-ation
(LAD) estimators. The results are reported in Table 4.
Clustered standard errors take into account the
non-indepen-dence of observations within our sample. Columns 1 and
4 conrmthe strongly positive impact of changes in return
expectations. In axed effectsmodel, results are less pronounced and
onlymarginallysignicant as much of the cross-sectional variation is
eliminated.Part of the effect is picked up by changes in
qualitative expecta-tions.3 Finally, the LAD regression (columns 3
and 6) has favorablesmall sample properties in reducing the
importance of outliers. Theeffect of changes in return expectations
is robust to this specication.
3 The correlation between changes in numerical and qualitative
expectations ispositive but low (0.26), suggesting that
multicollinearity is not an issue. Anexplanation for the emergence
of the qualitative rating effect is that the used scalelacks
inter-subject comparability, but is a good predictor within
subjects (xed-effects model).4.2. Investor portfolio risk
We now turn to investor portfolio risk, which might be a
morestable measure of investor risk taking. In our analysis, we
interpretthe volatility levels of investors portfolios when the
survey takesplace as the level of risk an investor is taking at
this point in time.Consequently, changes in volatility correspond
to changes in risk
) (5) (6) (7) (8)
257 0.040 0.251 0.2340.029 0.040 0.124 0.106013 0.014 0.011
0.015022 0.008 0.020 0.0240.010 0.012 0.011 0.009288 0.186 0.321
0.316
0.070 0.063 0.115 0.111017 0.012 0.016 0.019018 0.010 0.020
0.022
007 0.011 0.005 0.006
002 0.0020.089 0.1080.013 0.010034 0.028
0.034 0.034067 0.035 0.035 0.049 0.064
7 1376 769 769 767
dummies. Dependent variable is buysell ratio dened over number
of trades (# ofvolume (buying volume/total trading volume) for
columns 58. Columns 1 and 5tory variables. Columns 3 and 7 show
regressions on both, levels and changes, inde age, gender, wealth,
and nancial literacy. The table displays marginal effects,elvey and
Zavoinas R2.ngtaking.4 Similarly, we use levels and changes of
other portfolio riskmeasures (beta, relative volatility, average
component volatility).
Panel A of Table 5 shows correlations between the levels of
thesemeasures; all correlations are positive as they share a common
con-cept of risk, but the variables also capture different aspects
of risk ascorrelations are not perfect. In particular, portfolio
beta shows theweakest relation to other risk measures with
coefcients between0.23 and 0.43. When considering changes (Panel B)
the picturebecomes even more mixed. All but one correlation are
still positive,but especially for beta and three-month volatility
(which is the onlymeasure calculated over a shorter time horizon)
coefcients arelow. As portfolio risk measures differ, we consider
most of themin our regression analysis (except relative volatility
which is redun-dant in the levels analysis). We take the natural
logarithm of thevolatility variables, as volatilities are skewed
within our sample.
We use market expectations as explanatory variables to
avoidreverse causality inherent with portfolio expectations, as
currentportfolio volatility will determine expectations for future
portfolioreturns and volatility. Table 6 shows the results of a
panel GLSregression with random effects and clustered standard
errors (col-umns 14) and a xed effects regression (columns 58). We
ndthat the risk level investors take on in their portfolios
dependson their expectations. In all regressions, a positive impact
ofnumerical return expectations on volatilities and a negative
impact
4 This is a deliberate analogy to levels and changes in the
hypothetical risk takingtask analyzed by Weber et al. (2013). In
this task investors had to divide 100,000between the FTSE all-share
and a riskless asset. If we assume a volatility of 0 for
theriskless asset, the volatility of the chosen portfolio is
monotonically increasing withthe fraction invested in the FTSE.
-
Table 4
Buysell volume ratio
(3) (4) (5) (6)LA
0.0.0.0.0.
C. Merkle, M. Weber / Journal of anking & Finance 46 (2014)
372386 379Robustness tests: Buying and selling behavior
Buysell ratio
(1) (2)clus. SE FE
Num. return 0.199 0.134Num. risk 0.025 0.090Qual. return 0.014
0.038
Qual. risk 0.017 0.025Risk tolerance 0.007 0.023D num. return
0.230 0.179D num. risk 0.034 0.006D qual. return 0.019 0.033of
numerical risk expectations can be observed. Both effects
aresignicant in most specications, the effects are weakest for
port-folio beta (also conrmed by low R2). Risk tolerance and
qualitativeexpectations mostly have no predictive power for
portfolio riskAmong the demographic variables, we nd signicant
effects forage, wealth, and nancial literacy. Younger investors
hold morevolatile portfolios, while wealthier investors tend to own
less riskyportfolios.5 This result is consistent with the ndings of
Dorn andHuberman (2005).
Even though using market expectations addresses the mostobvious
endogeneity problem, there might still be concerns that
D qual. risk 0.013 0.015D risk tolerance 0.006 0.005Age
0.002Gender (male = 1) 0.088Wealth 0.013Income 0.029
Fin. literacy 0.029R2 0.055 0.073
n 767 769
Notes: The table shows results of a panel GLS regression with
random effects andeffects (columns 2 and 5), and a regression using
least absolute deviation and bootover number of trades (# of buys/#
of total trades) for columns 13 and buysell vo46. Independent
variables are as specied in Table 3. For random effects
regrespseudo-R2. Coefcients are signicant at 10%-level. Coefcients
are signicant at 5%-level. Coefcients are signicant at
1%-level.
Table 5Correlation of portfolio risk measures.
Levels of portfolio risk
Vol 1y Vol 3m Rel. Vol Beta ACV
Panel AVolatility 1y 1.00Volatility 3m 0.76 1.00Rel. volatility
0.89 0.59 1.00Portfolio beta 0.42 0.28 0.43 1.00ACV 0.64 0.54 0.50
0.23 1.00
Changes of portfolio risk
D Vol 1y D Vol 3m D Rel. Vol D Beta D ACV
Panel BD Volatility 1y 1.00D Volatility 3m 0.60 1.00D Rel.
volatility 0.39 0.11 1.00D Portfolio beta 0.13 0.05 0.40 1.00D ACV
0.60 0.32 0.06 0.05 1.00
Notes: The table shows pairwise Pearson correlations of levels
(Panel A) and changes(Panel B) of portfolio risk measures. All
correlations are signicant at 1%-level.
5 We do not nd signicant results for portfolio value / wealth as
a measure orelative importance of investors portfolios for their
overall wealth.B.
0.0.
0.0.0.
76
standastrapplumesions
fown portfolio risk determines also market expectations.
Therefore,we repeat the previous analysis using lagged expectations
andlagged preferences. The timing now is such that we use the
expec-tations of each survey date to explain portfolio risk three
month
D clus. SE FE LAD
343 0.173 0.132 0.1740.151 0.130 0.106 0.162008 0.018 0.034
0.011019 0.021 0.031 0.0160.006 0.006 0.022 0.009252 0.276 0.239
0.255
0.025 0.091 0.127 0.020026 0.024 0.035 0.028
004 0.019 0.023 0.010006 0.004 0.006 0.002001 0.002 0.0020.146
0.118 0.1360.006 0.009 0.012032 0.022 0.030
0.010 0.030 0.023047 0.053 0.075 0.043
7 767 769 767
rd errors clustered by participant (columns 1 and 4), a panel
regression with xeded standard errors (columns 3 and 6). Dependent
variable is buysell ratio denedratio dened over trading volume
(buying volume/total trading volume) for columnsoverall R2 is
reported, for xed effects regressions within R2, for
LAD-regressionslater. Results in Table 7 conrm the impact of
numerical returnand risk expectations on portfolio risk. The most
notable differenceis that in the lagged regression risk tolerance
has a more consistentpositive effect on risk taking, suggesting
that it takes some time forinvestors to implement their risk
preferences.6
The interpretation in terms of economic signicance is
straight-forward, as the dependent variable is log transformed.
10%-pointshigher return expectation will induce investors to hold a
portfoliowith 1.65% higher volatility (1.27% for lagged
expectations). Analo-gously, a 10%-points higher expected
volatility relates to a 1.31%decrease in portfolio volatility
(1.16% for lagged expectations).
Up to this point, we dealt with state variables that give us
someinformation which portfolio risk investors choose depending
ontheir expectations, risk tolerance, and demographics. The
panestructure of our data allows us to investigate in more detail
thedynamics of these relationships. We now analyze changes of
port-folio risk in response to contemporaneous changes in
investorexpectations and preferences. The assumption is that
investors inaddition to adjusting their risky share as suggested by
Eq. (4) alsochange portfolio composition. We adopt a parallel
approach to thelevels regression and again estimate a random
effects and a xedeffects model.
Table 8 shows the results of these regressions. With changes
inone-year portfolio volatility (columns 1 and 6) we observe
thesame patterns as in the levels regression. Positive changes
in
6 As a further test we instrument contemporaneous expectations
by laggedexpectations. While the results are consistent in
direction, signicance is weakHowever, instrumentation is costly in
terms of statistical power, as it requiresconsecutive observations.
Additionally, there are concerns about weak instruments
ascorrelations between expectations and lagged expectations are
only around 0.3(common tests for weak instruments attain borderline
results).l
.
-
l(
000
0
nkiTable 6Portfolio risk and expectations.
Random effects model
ln(Vol 1y) ln(Vol 3m) Beta(1) (2) (3)
Num. return 0.165 0.165 0.070
Num. risk 0.131 0.187 0.030Qual. return 0.001 0.000 0.002Qual.
risk 0.000 0.013 0.003Risk tolerance 0.001 0.007 0.004Age 0.006
0.006 0.002Gender (male = 1) 0.085 0.115 0.104
Income 0.016 0.014 0.004Wealth 0.031 0.030 0.016Fin. literacy
0.066 0.066 0.054
380 C. Merkle, M. Weber / Journal of Banumerical return
expectations are accompanied by increased risktaking, while higher
numerical risk expectations result indecreased risk taking. In the
regressions of changes in three-monthvolatilities on changes in
expectations (see Table 8), the coef-cients for numerical
expectations maintain their direction but nolonger reach
statistical signicance. This may be due to the dimin-ished
statistical power of the changes regressions, as we can
onlyconsider investors who participate in two consecutive
surveyrounds. However, another interpretation is that investors
haverather long-term objectives and do not manage their
portfoliosaccording to three-month volatilities. In our
questionnaire, mostinvestors state an investment horizon of 35
years.
For relative volatility and average component volatility
similarpatterns as for volatility emerge. In particular numerical
returnexpectations positively inuence risk taking. Changes in
relativevolatility most closely reect investors active
interventions to
R2 0.368 0.495 0.036 0
n 1924 1911 1926 1
Notes: The table shows results of a GLS panel regression with
random effects and clustecontain round dummies. Dependent variables
are portfolio risk measures: the natural logbeta and the log of
average component volatility (ACV). Expectation variables and
demogfor xed effects regressions within R2. Coefcients are
signicant at 10%-level. Coefcients are signicant at 5%-level.
Coefcients are signicant at 1%-level.
Table 7Portfolio risk and lagged expectations.
Random effects model
ln(Vol 1y) ln(Vol 3m) Beta ln(1) (2) (3) (
Lagged num. return 0.127 0.101 0.060 0Lagged num. risk 0.116
0.136 0.048 Lagged qual. return 0.005 0.006 0.008 0Lagged qual.
risk 0.007 0.022 0.001 Lagged risk tolerance 0.006 0.013 0.003 0Age
0.006 0.006 0.002 Gender (male = 1) 0.080 0.075 0.069 0Income 0.019
0.025 0.007 Wealth 0.030 0.025 0.016 Fin. literacy 0.058 0.036
0.047 R2 0.400 0.542 0.027 0
n 1923 1908 1925 1
Notes: The table shows results of a GLS panel regression with
random effects and clustecontain round dummies. Dependent variables
are portfolio risk measures: the natural logbeta and the log of
average component volatility (ACV). Expectation variables are
includeeffects regressions within R2. Coefcients are signicant at
10%-level. Coefcients are signicant at 5%-level. Coefcients are
signicant at 1%-level.Fixed effects model
n(ACV) ln(Vol 1y) ln(Vol 3m) Beta ln(ACV)4) (5) (6) (7) (8)
.135 0.129 0.102 0.042 0.098
0.086 0.106 0.154 0.006 0.048.002 0.003 0.003 0.004 0.0010.010
0.000 0.012 0.003 0.010.011 0.002 0.002 0.003 0.0060.003
.0590.018
0.022
0.059
ng & Finance 46 (2014) 372386alter portfolio risk, as raw
portfolio volatility is in large part drivenby changes in market
volatility. As already documented for levels,beta is the risk
measure least related to expectations. It is likelythat beta has
little relevance to participants in managing the riskof their
portfolios. Many private investors may not even knowabout this
concept.
In unreported results, we substitute round dummies by
marketvolatility, which is constant across participants and will
thus cap-ture the part of changes in portfolio volatility caused by
a passivechange in overall market volatility. In portfolio
volatility regres-sions, the coefcient of market volatility is
about 0.7, which meansthat about 70% of changes in portfolio
volatilities are driven bychanges in market volatility.
Interestingly, changes in market vol-atility have a negative impact
on relative volatility, suggestinginvestors attempt to counteract
rising market volatility by reduc-ing their portfolio risk relative
to the market.
.290 0.746 0.753 0.089 0.608
817 1924 1911 1926 1817
red standard errors (columns 14) and xed effects (columns 58).
All regressionsarithm of portfolio volatility calculated over a
1-year and 3-month horizon, portfolioraphics are as dened before.
For random effects regressions overall R2 is reported,
Fixed effects model
(ACV) ln(Vol 1y) ln(Vol 3m) Beta ln(ACV)4) (5) (6) (7) (8)
.188 0.092 0.012 0.036 0.144
0.147 0.095 0.080 0.034 0.119.002 0.007 0.008 0.010 0.0020.008
0.006 0.020 0.000 0.006.014 0.005 0.009 0.002 0.011
0.003
.0780.0170.018
0.059
.297 0.794 0.772 0.134 0.641
808 1923 1908 1925 1808
red standard errors (columns 14) and xed effects (columns 58).
All regressionsarithm of portfolio volatility calculated over a
1-year and 3-month horizon, portfoliod as lagged variables. For
random effects regressions overall R2 is reported, for xed
-
Table 8Changes in portfolio risk.
Random effects model
DVol 1y DVol 3m DRel. Vol DBeta D(1) (2) (3) (4) (
D num. return 0.062 0.114 0.059 0.000 0D num. risk 0.079 0.128
0.073 0.017 0D qual. return 0.003 0.005 0.000 0.005 D qual. risk
0.001 0.008 0.000 0.002 D risk tolerance 0.005 0.008 0.004 0.000
Age 0.001 0.001 0.000 0.001 Gender (male = 1) 0.005 0.018 0.012
0.001 Income 0.003 0.012 0.005 0.002 0Wealth 0.001 0.008 0.002
0.003 Fin. literacy 0.008 0.012 0.003 0.009 0.005
R2 0.682 0.652 0.246 0.141 0
n 1038 1031 1038 1009 1
stercha(ACts re
C. Merkle, M. Weber / Journal of Banking & Finance 46 (2014)
372386 3814.3. Volatility of trades
We combine the two approaches of measuring nancial risktaking
and examine the volatility of securities investors are trad-ing.
For this purpose, all securities traded by survey participants(and
for which a sufcient time series of returns is available) aresorted
by return volatility throughout the survey period. We formten
volatility deciles and hereby establish a ranking of securities
bytheir relative riskiness. We then calculate the value-weighted
aver-age of volatility decile each investor trades in. We also
compute thevolatility of purchases and the volatility differential
between pur-chases and sales. The latter two measures we interpret
as indica-tors of nancial risk taking as investors shift money to
volatilesecurities.
Notes: The table shows results of a GLS panel regression with
random effects and clucontain round dummies. Dependent variables
are changes in portfolio risk measures:relative volatility and
portfolio beta, and changes in average component volatilitydened
before. For random effects regressions overall R2 is reported, for
xed effec Coefcients are signicant at 10%-level. Coefcients are
signicant at 5%-level. Coefcients are signicant at 1%-level.Table 9
shows population averages of volatility of trades, of vol-atility
of purchases, and the average buysell volatility differential.We
observe that investors trade securities that are slightly
morevolatile than the total sample of securities (which of course
hasan average decile rank of 5.5). This is due to the fact that
mutualfunds and ETFs are less frequently traded than more volatile
secu-rities such as stocks and options. Volatility of trades and
purchasesis highest in the rst two rounds of the survey; these are
also the
Table 9Volatility of securities traded.
Round Tradevolatility
Buyvolatility
Buysellvol. diff.
Pre-survey (June 08September 08) 6.20 6.42 0.33
Round 1 (September 08December 08) 6.23 6.37 0.29
Round 2 (December 08March 09) 6.02 6.05 0.24Round 3 (March
09June 09) 5.99 5.79 0.39Round 4 (June 09September 09) 6.00 5.88
0.32Round 5 (September 09December 09) 5.96 6.07 0.02Round 6
(December 09March 10) 6.03 6.04 0.06Round 7 (March 10June 10) 5.75
5.60 0.36Round 8 (June 10September 10) 5.86 5.84 0.29Round 9
(September 10December 10) 5.82 5.76 0.23
Notes: The table shows for all survey rounds the average
volatility decile of tradesand purchases, and the average
volatility differential between purchases and sales. This
difference is signicant by a Wilcoxon signed-rank test at
10%-level. This difference is signicant by a Wilcoxon signed-rank
test at 5%-level. This difference is signicant by a Wilcoxon
signed-rank test at 1%-level.only rounds where the buysell
volatility differential is positivewhich conrms the earlier nding
that private investors in oursample seem to view the crisis as an
opportunity to buy risky secu-rities. This behavior then turns
around, in particular for a period ofhigh stock market gains in
mid-2009 (cp. also Fig. 1). Investorsmove back into safer
securities, a behavior that repeats itself forthe nal survey
rounds, for which the average volatility of tradesis lowest.
When we regress the three measures dened above on the lev-els of
investors expectations and risk tolerance (Table 10), we ndno
effect on overall trade volatility, a slight effect on the
volatilityof purchases and a pronounced impact on the buysell
volatilitydifferential. This means that investors shift capital
towards riskiersecurities when they have high return expectations.
This extends
.417 0.733 0.682 0.275 0.170 0.394
018 1038 1031 1038 1009 1018
ed standard errors (columns 15) and xed effects (columns 610).
All regressionsnges in portfolio volatility calculated over a
1-year and 3-month horizon, changes inV). Independent variables are
demographics and changes in expectations, both asgressions within
R2.Fixed effects model
ACV DVol 1y DVol 3m DRel. Vol DBeta DACV5) (6) (7) (8) (9)
(10)
.080 0.051 0.107 0.047 0.009 0.083
.020 0.072 0.149 0.069 0.005 0.0140.006 0.007 0.014 0.004 0.001
0.0080.003 0.000 0.010 0.000 0.000 0.0050.004 0.004 0.009 0.002
0.000 0.0040.0000.018.0040.001the results of the previous section,
as we now learn how investorsadjust their portfolio volatility in
response to positive expecta-tions: they buy high volatility
securities and sell low volatilitysecurities. We also nd that less
risk-averse investors buy securi-ties with higher volatility, in
line with risk habitat theory whichstates that investors select
securities of which volatilities are com-mensurate with their risk
aversion (Dorn and Huberman, 2010).7
Again older, wealthier, and more sophisticated investors trade
lessvolatile securities. We do not report results for a regression
onchanges in expectations in this case, as we nd no signicant
results
4.4. Selection effects
Our sample is clearly not representative, neither for the total
UKpopulation, nor for UK stock market investors, maybe not even
forBarclays online brokerage clients. We make no claim in
thisregard. However, we do believe that our data are meaningful
andallow to draw some inferences about investing behavior
inresponse to personal expectations and preferences. While onehas
to be careful not to overgeneralize our ndings, we have noevidence
of systematic selection in our sample, which would inval-idate our
results. In this section we analyze selection issues in aformal
way.
7 There is no such effect for buysell volatility differentials,
but this is nosurprising as both risk-averse and risk tolerant
investors will sometimes augment andsometimes reduce risk (though
on different levels)..
t
-
Table 10Volatility of trades explained by expectations
Random effects model
ll vo
1467 1343 890
d stcha
382 C. Merkle, M. Weber / Journal of Banki & Finance 46
(2014) 372386Given the relatively low (but not uncommon8) response
rate andthe presence of attrition in our panel, there are two
potential chan-nels of selection. Specic investors might be more
attracted to par-ticipate in the survey, or they leave and rejoin
the sample in anon-random way, both potentially biasing our
results. We have onlylimited data on non-participants, including
age and gender, as wellas some portfolio information (portfolio
value, number of positions,number of transactions).9 We use these
items as explanatory vari-ables in a participation regression,
results are reported in column 1of Table 11. We nd that male
investors and investors with a highernumber of holdings and
transactions are more likely to participate inthe survey. The
latter are potentially more active and interested innancial
markets, which would explain this result.
While this supports the presence of selection on observables
inour sample, it may remain inconsequential for our results. We
runa two-stage Heckmann selection model to test for this
possibility.
Trade volatility Buy volatility Buyse(1) (2) (3)
Num. return 0.467 0.840 1.374
Num. risk 0.042 0.431 0.377Qual. return 0.003 0.002 0.001Qual.
risk 0.038 0.031 0.049Risk tolerance 0.045 0.082 0.050Age 0.017
0.017 0.010Gender (male = 1) 0.704 0.604 0.077Income 0.047 0.048
0.023Wealth 0.102 0.116 0.031Fin. literacy 0.391 0.376 0.005
R2 0.085 0.108 0.041
n 1467 1343 890
Notes: The table shows results of panel regression with random
effects with clustereround dummies. Dependent variables are the
volatility of trades, the volatility of purregressions overall R2
is reported, for xed effects regressions within R2. Coefcients are
signicant at 10%-level. Coefcients are signicant at 5%-level.
Coefcients are signicant at 1%-level.In columns 2a and 2b, we
reproduce the regression of portfoliovalue on expectations
including the inverse Mills ratio of the rststage. The inverse
Mills ratio is highly signicant, again suggestinga selection
effect. However, our main result regarding the inuenceof expected
return and expected risk on risk taking remains intact.It is also
robust to an inclusion of the set of variables from the
par-ticipation regression (column 2b). Not surprisingly, portfolio
valueand number of positions are strongly negatively related to
portfoliovolatility, as they come along with a diversication
effect. In con-trast, number of transactions has a positive effect
on volatility. Inthis specication, the signicance of the inverse
Mills ratio is muchreduced, as the additional variables capture
part of the selectioneffect.
We nd similar results for the other levels specications,
mean-ing that despite selection is present in our sample, our
results aremainly unaffected by it. The changes regressions, by
making useof the in-sample variation over time, are per se less
vulnerableagainst this type of selection.
Next, we analyze the participation in the panel over time
todetect any signs of systematic attrition. To make sure that this
type
8 In similar survey studies Graham and Harvey (2001) report a
response rate of 9%,Glaser and Weber (2007) of 7%, Dorn and
Sengmueller (2009) of 6%, compared to our3% for a repeated
survey.
9 The remaining demographic variables such as income and wealth
were self-reported survey items.of selection does not bias our main
results we again use a Heckmanselection model. We follow Wooldridge
(1995) in estimating theparticipation equation separately for each
round of the panel,including demographics and lagged survey
variables. Instead ofdisplaying these roundwise rst stage
regressions, Table 11 showsa panel probit version of the
participation regression (column 3). Itdemonstrates that wealthier
investors are more likely to partici-pate, while higher income
investors are less likely to participate.Intuitively, those with
higher income might be more time-con-straint. More importantly,
lagged expectations do not explain sub-sequent participation, which
means that it is not the case that e.g.,optimistic or more risk
tolerant investors are more likely to con-tinue the survey.
We then re-estimate in the second stage the panel regression
asbefore, including now inverse Mills ratios from the roundwise
par-ticipation regressions. This time,wendno signicance for
theMills
andard errors (columns 13) or xed effects (columns 46), all
regressions containses and the difference between volatility of
purchases and sales. For random effectsFixed effects model
l. diff. Trade volatility Buy volatility Buysell vol. diff.(4)
(5) (6)
0.127 0.514 2.367
0.201 0.199 0.4210.027 0.038 0.0510.035 0.037 0.0890.015 0.001
0.065
0.010 0.021 0.049ngratio, suggesting no strong evidence for
selection effects in the senseof systematic panel attrition. Our
main results are unchanged inboth specications, whether using
random effects (4a) or xedeffects (4b). We also nd no evidence that
the changes regressionof Table 8 is affectedby selection.We thus
conclude thatwhile selec-tion is present in our sample, it seems to
have little inuence on theeffect of expectations and preferences on
risk taking behavior.
5. Discussion
A main problem any research in beliefs and
expectationsencounters is whether responses in a survey are valid
representa-tions of the internal beliefs of participants. The
challenge is two-fold, questions need to be stated in a way that
participants areable to answer them in a sensible way, and
participants need tobe motivated to do so. For the latter we rely
on the intrinsic moti-vation of participants as they completed the
survey voluntarily,and many found it interesting enough to take
part multiple times.As in most large-scale surveys, monetary
incentives were not fea-sible, but we are in this case not aware of
any obvious reason toconceal or distort beliefs in their absence.10
Additionally, we build
10 For a discussion about when monetary incentives are useful
see Camerer andHogarth (1999). Other surveys that do not
incentivize participants include theMichigan Survey of Consumer
Finances, the German Socioeconomic Panel and mostsurveys on
investing behavior.
-
Table 11
(2b
0.130.0.000.000.00
0.0.110.0.0.0.0.0.04
0.35
151
the sll login s
C. Merkle, M. Weber / Journal of anking & Finance 46 (2014)
372386 383on the nding of Weber et al. (2013)who use the same
surveythat the elicited expectations are effective and consistent
predictorsof decisions, which should attenuate concerns about their
validity.
The other concern that participants might not be able to
expresstheir beliefs in the question format provided to them is
taken intoaccount by the use of both, numerical and qualitative
elicitation ofexpectations. While the numerical estimates are more
demanding,in particular with respect to condence intervals, they
have theadvantage of being comparable across participants. On the
other
Sample selection.
Participation
Part. ln(Vol 1y)
(1) (2a)
Num. return 0.131
Num. risk 0.128Qual. return 0.005Qual. risk 0.004Risk tolerance
0.002
Age 0.000 0.006Gender (male = 1) 0.168 0.219
Income 0.014Wealth 0.031Fin. literacy 0.040Portfolio value
0.015Portfolio positions 0.062
Transactions 0.064
Inv. Mills ratio 0.594
n 19,609 1536
Notes: The table shows two-stage Heckman selection models for
participation inincluding age and gender, and portfolio value,
portfolio positions, and transactions (aMills ratio of the rst
stage. Column 3 shows a probit regression for participation
with(4a) and xed effects (4b). Coefcients are signicant at
10%-level. Coefcients are signicant at 5%-level. Coefcients are
signicant at 1%-level.hand, qualitative estimates may capture
aspects of value and risknot comprised in the rst two moments of a
distribution. Interest-ingly, we nd with rare exceptions that only
numerical expecta-tions are relevant for actual nancial risk taking
decisions, whichis in contrast to the results of Weber et al.
(2013) who establisha strong inuence of qualitative expectations on
allocations inthe hypothetical investment task. We test whether the
explanatorypower of numerical expectations changes over to
qualitativeexpectations if we drop numerical expectations from the
regres-sions. In general, this is not the case and the impact of
qualitativeexpectations remains weak. When in turn qualitative
expectationsare excluded, our results are unchanged.
An explanation for this nding has to consider the decision
pro-cess in the hypothetical investment task compared to
actuainvesting. First of all, our measures of nancial risk taking
are onlyweakly correlated with the proportion of risky investment
in thesurvey task, which already hints at the two being different.
In par-ticular, the changes of risk taking in the task and
investors portfo-lios are unrelated. We conjecture that the
qualitative expectationsare affective evaluations of the market
situation, while the numer-ical estimates draw more on cognitive
resources (cp. Kuhnen andKnutson, 2011). We would then expect these
evaluations to be pre-dictive for decisions that are made in the
same mode ofthinking.11 If the actual investment decisions of
investors are pre-ceded by a more deliberate thought process than
the allocations inthe hypothetical task, this would at least partly
explain the greater
11 Support for this dual-process theories of information
processing and decisionmaking can be found, e.g., in Kahneman
(2003).Blpredictive power of numerical expectations for these
decisions. Aswe cannot fully explore the underlying mechanisms,
this might bean interesting avenue for future research.
We also consider the time structure of expectations and
trading,and throughout the paper we opted for an approach that
tries toexplain changes in investing behavior by
contemporaneouschanges in expectations. Another possibility would
be that inves-tors need some time to react on changes in
expectations, for exam-ple because of inertia. When we use lagged
level variables many of
Panel attrition
Part. ln(Vol 1y)
) (3) (4a) (4b)
6 0.065 0.129 0.106136 0.315 0.152 0.1217 0.006 0.003 0.0042
0.010 0.001 0.0001 0.002 0.005 0.003004 0.004 0.004 7 0.192 0.098
015 0.122 0.007 016 0.115 0.042 033 0.043 0.022 046
109
4
4 0.001 0.0088 1825 1033 1033
urvey and panel attrition. Column 1 displays a probit regression
of participationarithmized). Columns 2a and 2b reproduce results of
Table 6 including the inversedurvey, columns 4a and 4b the
associated second stage estimated with random effectsthe described
relationships between expectations and investmentbehavior can still
be observed (cp. Table 7).12 However, the effectsare in general
about equal or weaker than for contemporaneousexpectations. We thus
conclude that investors tend to implementtheir beliefs in a timely
manner.
Instead of studying return and risk expectations separately,
Eq(4) can also be interpreted in terms of Sharpe ratios. A
higherexpected Sharpe ratio then implies a higher share in the
riskyinvestment. We calculate expected Sharpe ratios using
investorsmarket return expectations, the three-month risk-free rate
(repre-sented by the LIBOR), and the expected market volatility
frominvestors condence intervals.13 We nd that higher levels
ofSharpe ratios are related to higher portfolio risk, supporting
ourresults from Tables 6 and 7. However, there are in general no
signif-icant results for changes in Sharpe ratios. We attribute
this to the factthat Sharpe ratios are a combination of several
survey items, eachsubject to noise and measurement error. In
particular for changessuch constructs may become unreliable.
As a complement to our research, the investor survey ofHoffmann
et al. (2013) has an overlap of seven month with ourdata. Elicited
expectations and portfolio characteristics show somesimilarities:
For instance return expectations of Dutch investorsalso rise from
September to December 2008 and further to March2009, and trading
and buying activity initially increases inresponse to the crisis.
Similarly to us, Hoffmann et al. (2013) nd
12 A similar analysis for changes is precluded by the fact, that
a change Dt1;t ismechanically (negatively) correlated with Dt;t1
over the shared observation in t.13 As negative Sharpe ratios are
not well-dened, we have to exclude observationswhere Ers < rf
..
,
-
that median portfolio volatility is higher than market
volatility andclosely tracks the market index. However, there are
some differ-ences as well, e.g., risk perceptions fall gradually
after a peak inSeptember 2008, while in our data they rise and then
stay on a highlevel until March 2009. This might be due to the
different wordingof the question, which in Hoffmann et al. (2013)
refers to currentrisk perception, while our approach is more
forward looking. Nev-ertheless, taken together the ndings suggest
that there exist somemore general properties in expectations of
private investors thatare not limited to a particular dataset.
In a regression of buysell ratios on beliefs and
preferences,Hoffmann et al. (2013) use qualitative measures of
expectations asexplanatory variables (which in our case remained
insignicant).They demonstrate a signicantly positive inuence of
risk toleranceon buying activity, but nd little effect of return
and risk expecta-tions (levels and changes). This contributes to
our impression that
6. Conclusion
relative to the market. In general, the best t of our model
isachieved for long-term portfolio volatility. Changes in
short-termportfolio volatility and changes in portfolio beta are
less well ornot at all predicted by changes in expectations. This
relates directlyto the question how private investors manage their
portfolio riskand which risk measure is closest to their subjective
experienceof risk. As long-term volatility measures react strongest
to investorexpectations, we take this as tentative evidence that
they are agood proxy for experienced risk.
Expectations have less predictive power for immediate
tradingactivity of investors. We nd a positive effect of return
expecta-tions on equity buying activity, which proxies for an
adjustmentof the (unobserved) risky share. However, trading is
often noisy,inuenced by liquidity and other exogenous trading
motives,which might be a reason why we nd no inuence of risk
expecta-tions and preferences. Investors also engage in risk
shifting within
uesthe
cen endalcomqu
384 C. Merkle, M. Weber / Journal of Banking & Finance 46
(2014) 372386We investigate the functional relationship between
beliefs andpreferences of investors and their trading behavior.
While we arestill far from suggesting a denite functional form in
the spirit ofEq. (4), our ndings are a rst step to improve the
understandingof this complicated but fundamental relationship. We
provide evi-dence that expectations are relevant for risk taking of
investors,and that they areused in apredominantly rational and
intuitiveway.
Higher return expectations lead to increased risk taking interms
of portfolio volatility among investors, while higher
riskexpectations have the opposite effect. Even more, changes in
port-folio risk are predicted by contemporaneous changes in return
andrisk expectations. We nd evidence that investors
counteractchanges in market volatility by adjusting their portfolio
volatility
Appendix A
Description of variables
Variable Origin Description
Num. return Survey Return in % in response to survey qUK stock
market (FTSE all-share) byguess
Num. risk Survey Volatility calculated from condenusing
responses to survey questiostock market (FTSE all-share) by thethan
the actual outcome of the FTSErarely be higher than the actual
out
Qual. return Survey Rating on scale 17 in response toimmediate
trading behavior is hard to predict from elicited beliefs.For
portfolio volatility, both datasets share the intuitive
positiveresult for risk tolerance and the insignicant result for
qualitativereturn expectations. However,Hoffmann et al. (2013)
identify a posi-tive effect of risk perception on portfolio
volatility. They explain thisresult by investors being aware of the
risk of their investment port-folio, which suggests a reverse
causality from portfolio risk to riskperception. Our ndings for
numerical risk expectations stronglypoint in an opposite direction,
i.e., investors taking less risk whenthey perceive risk to be
higher. This discrepancy might again be aresult of different
measurement, as we strictly distinguish betweenportfolio and market
expectations, and use the latter in our regres-sions to avoid
reverse causality. Risk perception in Hoffmann et al.(2013) refers
more general to riskiness of investing.investment in the UK stock
market (FTtheir portfolio, replacing less volatile securities by
more volatileones. We infer that contrary to two-fund separation
investors useseveral channels to adjust their risky position. They
not onlyincrease or decrease a xed risky portfolio, but also change
thisrisky portfolio according to their expectations.
Taken together, our results suggest that nancial theory in
gen-eral correctly predicts the role of return and risk
expectations foractual trading behavior. Private investors take
their expectationsinto account to determine whether to buy or sell
and whether toincrease or decrease portfolio risk. But at the same
time investorsreaction to expectations and preferences is more
nuanced andmore ambiguous than in the theoretical model. Not only
do indi-vidual investors use different ways to alter their
investment risk,but also some nancial risk measures such as equity
beta seemto bear little relevance for them. Instead, we conjecture
that a mul-titude of other factors, which to describe and identify
is beyond thescope of this paper, play a role in investment
decisions.
Acknowledgements
We are grateful to Barclays Stockbrokers for providing access
totheir online investor client base, and to Barclays
BehaviouralFinance team for joint design and execution of the
survey. Wethank Daniel Egan, Christian Ehm, Greg Davies, Victor
Fleisher,Alen Nosic, participants of the 2011 Boulder Summer
Conferenceon Consumer Financial Decision Making and the 2011 SPUDM
Con-ference, and seminar participants in Mannheim and Luxemburg.For
research assistance we thank Robin Cindori. Research reportedin
this article was supported by the Observatoire de lEpargneEuropenne
(OEE) and Deutsche Forschungsgemeinschaft (DFG,Grant We993).
tion We would like you to make three estimates of the return of
theend of the next three month. Your best estimate should be your
best
intervals using the methodology of Keefer and Bodily (1983)We
would like you to make three estimates of the return of the UKof
the next 3 month. Your high estimate should very rarely be
lower
l-share (about once in 20 occasions). Your low estimate should
verye of the FTSE all-share (about once in 20 occasions)estion How
would you rate the returns you expect from an
SE all-share) over the next 3 months?
IfftatHighlight
IfftatHighlight
-
que
sta
1)
1)
(t
ankiAppendix A (continued)
Description of variables
Variable Origin Description
Qual. risk Survey Rating on scale 17 in response tomarket (FTSE
all-share) is?
Risk tolerance Survey Agreement on Likert scale 17
toinvestment
D num. return Survey Num. return (t) num. return (t D num. risk
Survey Num. risk (t) num. risk (t 1)D qual. return Survey Qual.
return (t) qual. return (t D qual. risk Survey Qual. risk (t) qual.
risk (t 1)D risk tolerance Survey Risk tolerance (t) risk
toleranceAge Bank data Age of participants in years
C. Merkle, M. Weber / Journal of BReferences
Amromin, G., Sharpe, S.A., 2009. Expectations of Risk and Return
among HouseholdInvestors: Are their Sharpe Ratios Countercyclical?
Working Paper.
Barber, B.M., Odean, T., 2000. Trading is hazardous to your
wealth: the commonstock investment performance of individual
investors. The Journal of Finance 55(2), 773806.
Barber, B.M., Odean, T., 2001. Boys will be boys: gender,
overcondence, andcommon stock investment. Quarterly Journal of
Economics 116 (1), 261292.
Bhattacharya, U., Holden, C.W., Jacobsen, S., 2012. Penny wise,
dollar foolish:buysell imbalances on and around round numbers.
Management Science 58 (2),413431.
Calvet, L.E., Campbell, J.Y., Sodini, P., 2007. Down or out:
assessing the welfare costsof household investment mistakes.
Journal of Political Economy 115 (5), 707747.
Calvet, L.E., Campbell, J.Y., Sodini, P., 2009. Fight or ight?
Portfolio rebalancing byindividual investors. The Quarterly Journal
of Economics 124 (1), 301348.
Camerer, C.F., Hogarth, R.M., 1999. The effects of nancial
incentives inexperiments: a review and capitallaborproduction
framework. Journal ofRisk and Uncertainty 19 (13), 742.
Campbell, J.Y., Viceira, L.M., 2002. Portfolio Choice for
Long-Term Investors. OxfordUniversity Press, New York, NY.
Gender Bank data Gender of participants, dummy variaWealth
Survey Self-reported wealth using nine categ
50,001100,000; 100,001150,000600,0011,000,000; >1,000,000.
Mi
Income Survey Self-reported income using eight cate30,00150,000;
50,00175,000; 7>200,000. Missing values were impu
Fin. literacy Survey Number of correct responses in a
4-i(2011)
Buysell ratio Bank data Number of purchases divided by
numBuysell
volume ratioBank data Volume of purchases divided by tota
Volatility 1y Bank data One-year historical portfolio
volatilitVolatility 3m Bank data Three-month historical portfolio
volaRel. Volatility Bank data One-year historical portfolio
volatilitPortfolio beta Bank data One-year historical portfolio
beta fro
corresponding market index and theACV Bank data Average
component volatility calcula
portfolio components owned at timeTrade volatility Bank data
Weighted average of volatility deciles
over total survey period and sorted inBuy volatility Bank data
Weighted average of volatility decile
calculated over total survey period anBuysell vol.
diff.Bank data Difference of volatility for securities
Volatility is calculated over total survPortfolio value Bank
data Portfolio value before the start of the
round (only participants)Portfolio
positionsBank data Number of holdings before the start
survey round (only participants)Transactions Bank data
Transactions in the year before the su
survey round (only participants)stion Over the next 3-months,
how risky do you think the UK stock
tement It is likely I would invest a signicant sum in a high
risk
1)
ng & Finance 46 (2014) 372386 385Dave, C., Eckel, C.C.,
Johnson, C.A., Rojas, C., 2010. Eliciting risk preferences: when
issimple better? Journal of Risk and Uncertainty 41 (3),
219243.
Dorn, D., Huberman, G., 2005. Talk and action: what individual
investors say andwhat they do. Review of Finance 9 (4), 437481.
Dorn, D., Huberman, G., 2010. Preferred risk habitat of
individual investors. Journalof Financial Economics 97 (1),
155173.
Dorn, D., Sengmueller, P., 2009. Trading as entertainment?
Management Science 55(4), 591603.
Egan, D., Davies, G.B., Brooks, P., 2010. Comparisons of risk
attitudes acrossindividuals. In: Cochran, J. (Ed.), Wiley
Encyclopedia of Operations Research andManagement Science. John
Wiley and Sons, Hoboken, NJ.
Ehm, C., Kaufmann, C., Weber, M., 2014. Volatility
inadaptability: investors careabout risk, but cant cope with
volatility. Review of Finance (in press).
Glaser, M., Langer, T., Weber, M., 2013. True overcondence in
interval estimates:evidence based on a new measure of
miscalibration. Journal of BehavioralDecision Making 26 (5),
405417.
Glaser, M., Weber, M., 2005. September 11 and stock return
expectations ofindividual investors. Review of Finance 9 (2),
243279.
Glaser, M., Weber, M., 2007. Overcondence and trading volume.
The GENEVA Riskand Insurance Review 32 (1), 136.
Goetzmann, W.N., Kumar, A., 2008. Equity portfolio
diversication. Review ofFinance 12 (3), 433463.
ble 1 if male, 0 if femaleories provided in the survey: 010,000;
10,00150,000;; 150,001250,000; 250,001400,000; 400,001600,000;ssing
values were imputedgories provided in the survey: 020,000;
20,00130,000;5,001100,000; 100,001150,000; 150,001200,000;tedtem
nancial literacy test using questions by van Rooij et al.
ber of total trades (range 01)l trading volume (range 01)
y at time ttility at time ty divided by one-year historical
market volatility at time tm a one factor model using the FTSE
all-share index asLIBOR as riskfree rateted using a weighted
average of one-year historical volatility oftfor all securities
traded between t an t + 1. Volatility is calculatedto deciles
s for all securities purchased between t an t + 1. Volatility
isd sorted into deciles
purchased and volatility for securities sold between t and t +
1.ey period and sorted into decilessurvey (participants and
non-participants), and at each survey
of the survey (participants and non-participants), and at
each
rvey start (participants and non-participants), and between
-
Graham, J.R., Harvey, C.R., 2001. The theory and practice of
corporate nance:evidence from the eld. Journal of Financial
Economics 60 (23), 187243.
Grinblatt, M., Keloharju, M., 2000. The investment behavior and
performance ofvarious investor types: a study of Finlands unique
data set. Journal of FinancialEconomics 55 (1), 4367.
Guiso, L., Sapienza, P., Zingales, L., 2011. Time Varying Risk
Aversion. WorkingPaper.
Hoffmann, A.O.I., Post, T., Pennings, J.M.E., 2013. Individual
investor perceptions andbehavior during the nancial crisis. Journal
of Banking and Finance 37 (1), 6074.
Kahneman, D., 2003. Maps of bounded rationality: a perspective
on intuitivejudgement and choice. The American Economic Review 93
(5), 14491475.
Kapteyn, A., Teppa, F., 2011. Subjective measures of risk
aversion, xed costs, andportfolio choice. Journal of Economic
Psychology 32 (4), 564580.
Keefer, D.L., Bodily, S.E., 1983. Three-point approximations for
continuous randomvariables. Management Science 29 (5), 595609.
Kempf, A., Merkle, C., Niessen, A., 2014. Low risk and high
return affectiveattitudes and stock ma