Online Appendix When There is No Place to Hide: Correlation Risk and the Cross-Section of Hedge Fund Returns A. Benchmark factor summary statistics The BKT model is an 8-factor model that consists of the FH-seven factor model augmented by the correlation risk factor. 1 Table A1 shows diagnostic statistics for the di/erent factors that we use. [Insert Table A1 here] B. Date base and fund return summary statistics There are two main reasons why we use the BarclayHedge data base for our analysis. First, the Barclayhedge data base contains information about fundsaggregate net long and short exposures based on market value, which is necessary to test the relationship between correla- tion risk and net exposure. The TASS/Lipper database, another high quality and frequently used hedge fund database, does not contain this information. Second, the BarclayHedge data base is the highest quality commercial hedge fund data base. A recent comprehensive study of the main commercial hedge fund data bases by Joen- vaara, Kosowski and Tolonen (2012, abbreviated JKT (2012)) nds that the BarclayHedge data base is the most high quality data base in many respects. The authors compare 5 data bases (the BarclayHedge, TASS, HFR, Eurekahedge and Morningstar data bases) and nd that Barclayhedge has the largest number of funds (10520), compared to 8788 funds in the TASS data base. Moreover, BarclayHedge has one of the highest percentages of dead/defunct funds (66 percent), thus making it least likely to su/er from survivorship bias. Out of these data bases, only Barclayhedge has information on net exposure. The BarclayHedge data base accounts for the largest contribution to the aggregate database that JKT(2012) create. The 1 The Fung and Hsieh (2001) model has been extended to consider other potential attributes. Fung and Hsieh (1997, 2000, 2001), Mitchell and Pulvino (2001) and Agarwal and Naik (2004) discuss the non-linearity of hedge fund strategies and show that a passive rolling strategy based on options helps to explain hedge fund returns. Other papers that investigate hedge fund performance relative to the Fung and Hsieh (2001) model include Bondarenko (2004), Kosowski, Naik, and Teo (2007) and Fung, Hsieh, Ramadorai, and Naik (2008). Results available from the authors upon request show that our ndings are robust to the eight factor specication of the Fung-Hsieh model, which includes the return of a stock index lookback straddle (PTFSSTK).
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Online Appendix’When There is No Place to Hide: Correlation Risk and
the Cross-Section of Hedge Fund Returns’
A. Benchmark factor summary statistics
The BKT model is an 8-factor model that consists of the FH-seven factor model augmented
by the correlation risk factor.1 Table A1 shows diagnostic statistics for the different factors
that we use.
[Insert Table A1 here]
B. Date base and fund return summary statistics
There are two main reasons why we use the BarclayHedge data base for our analysis. First,
the Barclayhedge data base contains information about funds’aggregate net long and short
exposures based on market value, which is necessary to test the relationship between correla-
tion risk and net exposure. The TASS/Lipper database, another high quality and frequently
used hedge fund database, does not contain this information.
Second, the BarclayHedge data base is the highest quality commercial hedge fund data
base. A recent comprehensive study of the main commercial hedge fund data bases by Joen-
vaara, Kosowski and Tolonen (2012, abbreviated JKT (2012)) finds that the BarclayHedge
data base is the most high quality data base in many respects. The authors compare 5 data
bases (the BarclayHedge, TASS, HFR, Eurekahedge and Morningstar data bases) and find
that Barclayhedge has the largest number of funds (10520), compared to 8788 funds in the
TASS data base. Moreover, BarclayHedge has one of the highest percentages of dead/defunct
funds (66 percent), thus making it least likely to suffer from survivorship bias. Out of these
data bases, only Barclayhedge has information on net exposure. The BarclayHedge data base
accounts for the largest contribution to the aggregate database that JKT(2012) create. The
1The Fung and Hsieh (2001) model has been extended to consider other potential attributes. Fung andHsieh (1997, 2000, 2001), Mitchell and Pulvino (2001) and Agarwal and Naik (2004) discuss the non-linearityof hedge fund strategies and show that a passive rolling strategy based on options helps to explain hedgefund returns. Other papers that investigate hedge fund performance relative to the Fung and Hsieh (2001)model include Bondarenko (2004), Kosowski, Naik, and Teo (2007) and Fung, Hsieh, Ramadorai, and Naik(2008). Results available from the authors upon request show that our findings are robust to the eightfactor specification of the Fung-Hsieh model, which includes the return of a stock index lookback straddle(PTFSSTK).
authors also note that BarclayHedge is superior in the terms of Assets under Management
(AuM) coverage, since it has the longest AuM time-series (58 percent), suggesting different
behavior when aggregate returns are calculated on a value-weighted basis. The amount of
missing AuM observations varies significantly across data vendors, being lowest for Barclay-
Hedge (12 percent) and HFR (20%) and significantly higher for EurekaHedge (36%), TASS
(35%), and Morningstar (34%). JKT (2012) do find, however, that economic inferences based
on the Barclayhedge and TASS data bases are similar in a number of dimensions. For instance,
BarclayHedge, HFR and TASS show economically significant performance persistence for the
equal-weighted portfolios at semi-annual horizons.
We use US Dollar denominated hedge fund share classes and require funds to have at least
24 monthly observations.
B.1. Correlation Swap Time-Series Data
A correlation swap is a contract that pays the difference between a standard estimate of the
realized correlation and the fixed correlation swap rate. Since these contracts cost zero to
enter, the correlation swap rate is the arbitrage free price, i.e., the risk-adjusted expected
value, of the realized correlation. Our data consists of daily implied and realized correlation
quotes of one month (three month) maturity correlation swaps for the S&P500 from April
2000 until December 2008 (from January 2009 until June 2012). A positive (long) position in
a correlation swap is a claim to a payoff proportional to the difference between the realized
correlation during the tenor of the contract and the correlation swap rate fixed at the beginning
of the month.2
Since correlation swap quotes are only available after March 2000, we create a synthetic
correlation swap time series for the time period from January 1996 to March 2000, using
the model-free approaches discussed in Carr and Madan (1998), Britten-Jones and Neuberger
(2000) and DMV (2006). For the period from April 2000 to December 2008, we find that
the correlation between the synthetic correlation proxy and the correlation quotes time series
is 92 percent, which supports the use of the synthetic time series in the 1996-2000 period.
In order to synthesize correlation swap prices before April 2000, we use options data from
2The reason for the use of three month correlation swaps from January 2009 onwards is due to dataavailability. Our data sources provided us with 3 month correlation swaps data for the second part of thesample (2009-2012). The correlation between the three month and one month correlation swaps is close to 80percent during the 2000-2008 period. Given this high correlation between the time series and the fact thatour results remain qualitatively unchanged when we compare the sample ending in 2008 and 2012, this choicedoes not qualitatively affect our conclusions.
1
Optionmetrics, for S&P500 index options and all individual stock options in the S&P500 list,
as well as index and individual stock data. Since this database covers option prices backwards
only until January 1996, we focus in our study on hedge fund returns in the sample period
from January 1996 to June 2012.
From the OptionMetrics database, we select all put and call options on the index and
on the index components. We work with best bid and ask closing quotes, rather than the
interpolated volatility surfaces provided by OptionMetrics, and use the midquotes for these
option data (average of bid and ask). We retain options that have time-to-maturities up
to one year and have at least three strike prices at each of the two nearest maturities. We
discard options with zero open interest, with zero bid prices, with negative bid-ask spread,
and with missing implied volatility or delta. Finally, we use the T-bill rate with 1-month
constant maturity to approximate the 30-days risk-free rate. The T-bill rate is obtained from
the Federal Reserve database.
To provide further background on the empirical features of the correlation risk premium,
Figure A1 shows that the six-month moving average of our correlation risk proxy is highly
time varying. During the early part of the period, the returns for selling correlation were quite
large. Similar to other markets, such as credit markets, risk capital has flowed into strategies
attempting to exploit the negative correlation risk premium, thus reducing the spread between
implied and realized correlation over time. Moreover, while during the periods 2002-2005 and
2009-2012 selling correlation was highly profitable, the opposite was true in the period 2007-
2008.
[Insert Figure A1 here]
Figure A2 plots a moving average of the implied and realized correlation over our sample.
[Insert Figure A2 here].
C. Synthesizing Correlation Risk and Variance Risk Proxies
Implied Correlation and Correlation Risk Proxy. Correlation swap rates can be approximated
using a cross-section of market index and individual stock variance swaps, which in turn can
be synthesized from the cross-section of market index and individual stock options using well-
known techniques. As an approximation to the correlation swap rate, we make use of the
2
concept of implied correlation (see, for instance, DMV, 2006), defined by:
ICt,T :=EQt [RV I
t,T ]−∑n
i=1w2iE
Qt [RV i
t,T ]∑i 6=j wiwj
√EQt [RV i
t,T ]EQt [RV it,T ]
=SV I
t,T −∑n
i=1w2i SV
it,T∑
i 6=j wiwj
√SV i
t,TSVjt,T
, (1)
where RV It,T (SV
It,T ) andRV
it,T (SV
it,T ) are the S&P500 index and single stock realized variances
(variance swap rates) over time span [t, T ], and wi is the market capitalization weight of stock
i. Our synthetic correlation risk proxy for the time period from January 1996 to March 2000
is given by:
CRt,T = L · (RCt,T − ICt,T ) , (2)
where L is the given notional value. Note that ICt,T can be computed using only information
about index and single stock variance swap rates. The intuition is as follows. The numerator
is the risk-neutral expectation of a payoff given by:
RV It,T −
n∑i=1
w2iRVit,T =
∑i 6=j
wiwj
∫ T
t
visvjsρijs ds (3)
where vis is the individual instantaneous volatility of stock i and ρijs is the instantaneous pair-
wise correlation between stock i and j, assuming a pure-diffusion return process. Therefore,
the implied correlation can be interpreted as the risk-neutral expected average correlation,
i.e., ICt,T = EQt [∫ Ttρsds] for some appropriate average correlation process ρt, say, such that:∑
i 6=j
wiwjICt,T
√SV i
t,TSVjt,T =
∑i 6=j
wiwjICt,T
√EQt [RV i
t,T ]EQt [RV it,T ] (4)
= EQt
[∑i 6=j
wiwj
∫ T
t
visvjsρijs ds
].
A concrete verification of the quality of proxy (2) as a correlation risk proxy can be gauged
by comparing the statistical behaviour of definitions (1) and (2) for the sample period after
April 2000, where quoted correlation swaps are available. For that period, we find a remarkable
coincidence of these two time series, with a correlation between proxies of 0.92, which supports
the use of (2) as a market proxy for correlation risk before April 2000. For comparison, the
correlation between the correlation risk proxy and a proxy for index variance risk is only about
0.25 in the same time period.
Variance Swap Rates and Proxies of Variance Risk. In order to compute the implied
correlation (1), it is necessary to compute the index and single stock variance swap rates
3
SV It,T and SV i
t,T , i = 1, . . . , N . Variance swap rates are also necessary to compute direct
proxies of variance risk. Similar to correlation swaps, a variance swap is a contract that pays
at the contract’s maturity a payoff given by the difference between realized variance RVt,Tand variance swap rate SVt,T , multiplied by the notional amount invested:
(RVt,T − SVt,T )L . (5)
By construction, since the initial price of a variance swap is zero, the variance swap rate is
the arbitrage-free price of the future realized variance:
SVt,T = EQt [RVt,T ] . (6)
In particular, the variance risk premium of an asset with realized variance RVt,T is given by:
Empirically, the average variance swap payofffor the index variance is negative, which indicates
the existence of a negative risk premium for market variance risk. However, the market
variance risk premium is not a pure indicator of ex-ante excess returns deriving from exposure
to pure variance risk, because the index variance is a weighted sum of single stock variances
and covariances. Therefore, in order to proxy for aggregate variance risk, we use the market
weighted sum of the payoffs of individual stock variance swaps, defined by:
V Rt =n∑i=1
wi(RVit,T − SV i
t,T )Li . (8)
Synthetic Variance Swap Rates. In order to compute index and single stock variance swap
rates, we use the standard industry approach and synthesize them from plain (listed) vanilla
option prices. This approach also avoids to a good extent the liquidity problems related to
the variance swap quotes of individual stocks. In an arbitrage-free market and under the
assumption of a continuous swap rate process, the following relation holds (see, e.g., Carr and
Madan, 1998, Britten-Jones and Neuberger, 2000 and Carr and Wu, 2009):
SVt,T = EQt [RVt,T ] =2
(T − t)B(t, T )
∫ ∞
0
Θt(K,T )
K2dK, (9)
where B(t, T ) is the price of a zero coupon bond with maturity T and Θt(K,T ) denotes the
price of call and put option with strike K and maturity T on an underlying asset with realized
4
variance RVt,T .3 We use this relation to compute index and single stock variance swap rates.
The return of the correlation risk factor can be interpreted as the return on a correlation swap
with a $1 notional amount, abstracting from margin payments.
D. Benchmark factor summary statistics
As mentioned, see Section II.A of the paper, the BKT model is an 8-factor model that consists
of the FH-seven factor model augmented by the correlation risk factor.
Similarities and Differences Between Volatility and Correlation Risk. What are empirical
differences of correlation and index variance risk premia? Table A1 reports summary statistics
of our monthly risk factors for index variance risk and for correlation risk, which correspond
to the returns of long positions in index variance and correlation swaps, respectively. The
average excess return on the S&P500 index in our sample is 0.42 percent per month. The
average index variance risk and correlation risk proxies are -17.77 (in percent squared permonth) and -10.70 percent per month, respectively.
As a preliminary step, we report the unconditional correlation between the correlation risk
factor and value-weighted hedge fund index returns.
[Insert Table A2 here]
E. Ranking Funds by Full-sample versus rolling betas
In Table 3 and 4 of the paper we are careful to rank funds by rolling betas following the
methodology described in Pastor and Stambaugh (2003). As a robustness check in Table
A3 below we also report results for the case when funds are ranked based on full-sample
betas. Panel A of Table A3 reports the betas and t-statistics of betas. Panel B of Table A3
reports the alphas and the return contribution of the different beta exposures. The overall
conclusion from the two approaches is qualitatively the same. Funds in the bottom decile have
a significantly higher lower alpha than funds in the top decile once correlation risk is taken
into account.
[Insert Table A3 here]
3For a variance swap such that T − t = 30 days, we compute the realized (annualized) variance as:
RVt,t+30 =365
30
30∑i=1
R2t+i,
where Rt+i is the daily return of the underlying asset at the end of day i = 1, . . . , 30.
5
F. The Cross-Sectoin of Hedge Fund Correlation Risk Exposures:
Two Hedge Fund Strategies Under the Magnifying Glass
Option Trader. In recent years, equity and credit derivative hedge funds have sprung up, which
explicitly trade alternative asset classes, such as variance and correlation. Some of these funds
directly use options, variance swaps or correlation swaps.4 Other funds use structured credit
products and take long-short positions in different tranches of asset-backed securities, such
as CDOs and CLOs, thus taking explicit bets on changes in the default correlations of the
underlying reference entities.5 Panel A and B of Table A4 presents our findings for Option
Trader strategies. It is interesting to note that in this category all deciles have a negative
correlation risk beta. The results in this table are based on rolling regressions and therefore
it is not guaranteed that the correlation risk betas of the funds in the bottom decile would be
lower than those in the top decile. Nevertheless, we find that this is the case, which suggests
that the risk properties of funds are relatively stable over time. We find that this group
of funds differs from Long/Short Equity and Low Net Exposure funds, to the extent that
the average return of funds with the largest positive correlation risk exposure in the Option
Trader group is smaller than the average return of funds with the most negative correlation
risk exposure in the LNE and LSE classes. The portfolio of Option Trader funds in the
bottom decile has a return of 6.63 percent per year, which is lower than the average return
of 11.47 percent per year of the portfolio in the highest correlation risk beta decile. However,
correlation risk exposure explains about 7 percent of the difference of average returns between
the highest and lowest decile groups. BKT model alphas are −4.68 and 5.89 percent per
year for the highest and lowest correlation risk beta deciles, respectively, which shows that
Options Trader funds performance is dependent on the latent correlation risk exposure, which
generates economically significant differences in excess returns as a result. Correcting for
exposure to correlation risk, the risk-adjusted performance of Option Trader strategies can
change dramatically: The alpha of the lowest (highest) correlation risk beta quintile according
to FH model is about 0.89 (7.96) percent per year, but the alpha according to BKT model
is about minus 4.68 (plus 5.89) percent per year! These features might derive from the fact
that Option Trader Funds explicitly try to model their risk exposures to correlation risk:
While Long/Short Equity funds might inadvertently expose themselves to correlation risk
shocks, Options Trader funds are likely to be more aware of the importance of measuring and
4See, e.g., Granger and Allen (2005) JPMorgan report ’Correlation Vehicles’.5’We have hedge fund clients who are very active traders of volatility, correlation and dispersion. Trading
correlation and dispersion as an asset class can have a diversification effect,...’ (Denis Frances, Global Headof Equity Derivatives Flow Sales at BNP Paribas, FTfm, 28/1/2008).
6
managing this particular source of risk; see, e.g., Granger and Allen (2005). They might even
want to bet on it.
[Insert Table A4 here]
Funds of Funds. Funds of Funds are an interesting subcategory that consists of portfolios of
individual hedge funds. They differ from individual hedge funds in several respects including
an additional fee layer on top of the fees related to the underlying individual funds. As Table
2 in the paper shows they generate the lowest alpha among all investment styles. Funds of
funds are typically treated separately in hedge fund studies since they affect performance
persistence results as they consistently generate among the lowest average returns compared
to individual hedge fund styles. Since they consist of a portfolio of individual hedge fund
styles, their negative correlation risk exposure documented in Table 2 can be interpreted as
contain the risk that in crisis times these strategies become correlated. This is indeed what
was observed in 2008 when many funds of funds suffered large losses. Panels C and D of Table
A4 shows that sorting funds of funds on rolling betas leads to portfolios that have relatively
low Fung and Hsieh alphas and even lower BKT alphas with several deciles of the post-ranking
returns showing statistically significant exposure to correlation risk.
Managed Futures Funds. The Managed Futures fund category consists of quite a diverse
set of funds that predominantly use liquid futures and derivatives markets to implement
their strategies. This category includes discretionary and systematic Managed Futures funds,
including trend-following funds. We make use of our performance attribution approach based
on the 8-factor BKT model (see Equation (1) in the main paper) to split the impact of index
variance risk on hedge fund returns into its two main components: Correlation risk and average
variance risk of the index constituents. Panel C of Table 2 in paper shows that correlation
risk exposure, rather than variance risk exposure, is the main driver of the risk-return profile
of Managed futures funds. In Panel E and F of Table A4 we examine these funds further and
find that Managed futures funds in the decile with the most negative correlation risk exposure
have the highest return (11.17 percent per year) and the highest FH model alpha (8 percent
per year). In contrast, the portfolio of funds in decile 10 produces an average return of 8.88
percent per year. However, 5.4 percent per year of the apparently superior performance of
the portfolio in decile 1 is explained by a significant negative correlation risk exposure. While
managed futures funds may invest in hundreds of derivatives, based on historical covariance
matrices, the managed futures category is exposed to unexpected changes in correlation of
risky assets.
7
G. Robustness Checks
In this section, we document the extent to which our results are robust to: (i) inclusion of
leverage; (ii) inclusion of liquidity risk factors; (iii) the use of TASS data; (iv) controlling
for variance risk premia in Fama-Macbeth regressions; (v) using equal-weighted, instead of
value-weighted, indices.
G.1. Leverage
In this section we document that our results are robust to the inclusion of a leverage variable.
In standard hedge fund data, “leverage” is not explicitly defined in a standardized way, for
instance, whether it should be computed in dollar notionals or delta equivalents. Hedge funds
simply receive from the data provider a field label "leverage" to fill in. Thus, those numbers
are likely affected by self-reporting problems. We compute two measures of leverage using
the data download in June 2012: (a) self-reported leverage; (b) gross exposure, i.e. longs +
shorts. We find that the correlation between net exposure and gross exposure is 0.27; the
correlation between net exposure and (self-reported) leverage is essentially zero; and the one
between leverage and gross exposure is about 0.42.
Moreover, while in the data some no-arb funds carry large leverage and low net exposure,
we also see funds that use leverage in portfolios with positive net exposure. Long-short equity
funds for example have on average a leverage of 1.53, but a relatively low net exposure of
28.9. In contrast, Fixed-Income relative value funds have an average leverage of 2.1, but a net
exposure of 72.0.
The analysis suggests that leverage and net exposure are distinct concepts in the data.
This is true both when we use self-reported measures of leverage and when we manually
compute the gross exposure.
We also sort hedge funds into leverage and net exposure deciles. We find that while
correlation risk betas are increasing in net exposure (see Figure 1 in the main paper and
Table A5), they tend not to any clearly increasing or decreasing relationship with leverage
(see Table A6).
[Insert Table A5 here]
Moreover, we find that different leverage deciles have similar correlation risk beta (−0.011
for the 9th decile vs, −0.012 for the 1st decile). Thus, differences in leverage are largely
unrelated to economically relevant differences in correlation risk beta, once all other factors
8
are controlled for. Overall, this evidence implies that in the data leverage is a different concept
than correlation risk exposure.
[Insert Table A6 here]
We also apply a double sort. We sort funds into four quartiles according to their leverage
and into four quartiles according to their correlation risk beta. In Table A7 we find that
even for the low leverage quartile, the dispersion in correlation betas is very substantial and
explains an important fraction of the cross-section in expected returns. For the high leverage
quartile, the spread is still very significant, but only marginally higher than for the low quartile
leverage bin. This is final support that, in the data, leverage and correlation risk exposure
are different concepts.
[Insert Table A7 here]
G.2. Robustness to Liquidity Risk Factor
Recent work by Aragon (2007) documents that hedge funds alphas are linked to hedge fund
lock-up periods, which suggests a potential relation between hedge funds alpha and asset liq-
uidity. Sadka (2010) shows that a (non-tradable) equity market liquidity factor explains cross-
sectional differences in hedge fund returns. Although liquidity and correlation are sometimes
interpreted as related economic phenomena, we find that they capture different characteristics
of hedge fund returns. We consider liquidity proxies that have tradable factor interpretations,
as the other factors in the BKT model. Then, we augment the BKT model with two liquidity
proxies: (a) the Fontaine and Garcia (2012) liquidity factor, for the fixed income market, and
(b) the Pastor and Stambaugh (2003) liquidity factor, for the equity market.6 The advantage
of this approach, with respect to a projection on non-tradable factors, is that the intercept
of a performance attribution regression can be interpreted as risk-adjusted performance or
"alpha". Table A8 shows that a significant component of correlation risk is not related to
liquidity risk. Even after controlling for these two factors, correlation risk is not subsumed by
liquidity risk and it remains a significant explanatory factor in hedge fund returns.
[Insert Table A8 here]
We find that value-weighted indices of all funds and Low Net Exposure funds, for example,
continue to have a statistically and economically significant negative beta with respect to
correlation risk, even after augmenting the BKT model by the two liquidity proxies.
6We thank Jean-Sebastien Fontaine and Rene Garcia for kindly providing us with their data.
9
G.3. Robustness to use of TASS Data base
The hypothesis that funds with low net exposure have high correlation risk beta cannot be
directly tested within the TASS database since it does not contain information about funds’
net exposure. We can test indirectly whether our results are robust when using TASS data
by focusing on certain investment objectives. We focus on Long/Short Equity funds, which
we expect to have statistically and economically significant exposure to the correlation risk
factor. We estimate the model, and run regressions using our risk factors to compare the
slope coeffi cients. Table A8 shows that Long/Short Equity funds have a correlation risk beta
t-statistics of -2.55 which is significant at the 1 percent level. In the baseline BarclayHedge
data results, the Long/Short Equity funds have a correlation risk beta t-statistic of -2.06 which
is very close to the finding in the TASS data. The TASS data also confirms the findings based
on the BarclayHedge data that the average fund has a negative and statistically significant
correlation risk beta (the t-statistic of the correlation risk beta of All funds in the TASS
data is −1.67). Although we cannot test for it directly, it is reasonable to assume that
within these Long/Short Equity funds those TASS funds with low net exposure are likely
to have even higher correlation risk beta than the average Long-Short Equity fund. Funds
of Funds are another hedge fund style that we found to have high correlation risk, since
these funds pursue different strategies at the same time, which may generate diversification
in normal times, but in bad times when correlations increase may lead to losses. We find
that Funds of Funds have statistically significant negative loadings on the correlation risk
factor in the BarclayHedge data base (Table II, Panel B, t-statistic of −1.81). These results
are confirmed by the results using the TASS data base which also contains a group of funds
that are Multi-Strategy funds (Table A9). The t-statistic (−2.18) in the TASS data is also
statistically significant and negative.
[Insert Table A9 here]
When using the TASS data base to examine the cross-sectional pricing tests in Table 5
of the paper we also find that our results are robust. Similar to the specification using the
BarclayHedge data we find that correlation risk is also priced in the cross-section of hedge
fund when using the TASS data.
G.4. Variance and Correlation Risk Premia
Table 2 Panel C of the paper shows that correlation risk remains statistically significant when
a variance risk residual is added to the BKT model in a time series specification. Table
10
A10 tests whether the same holds true also in Fama-Macbeth regressions. We find that the
correlation risk premium is indeed statistically significant, while the variance risk proxy is not,
thus lending further support to the BKT model.
[Insert Table A10 here]
G.5. Equal-Weighted Versus Value-Weighted Indices
Our findings that value-weighted indices of Low Net Exposure and Long Short Equity funds
have statistically significant correlation risk exposures are corroborated by the evidence for
equal-weighted indices presented in Table A11, which is based on the BarclayHedge data.
[Insert Table A11 here]
An equal-weighted average of all individual hedge funds has a correlation risk beta of -
0.01, with a t-statistic of -1.84 (p−value=0.07). Using equal-weighted indices of All Low NetExposure funds, leads to a statistically significant negative correlation risk beta (tβCR = −1.61,
p-value=0.09). An equally-weighted index of Long-Short Equity funds also has a statistically
significant exposure to correlation risk (tβCR = −3.1, p-value=0.01). Similar results hold for
equally-weighted indices of Merger Arbitrage and Option Trader funds. The same is not true
for Managed Futures funds, suggesting that some of the previous results might partly be
driven by Managed Futures funds that are larger, in terms of assets under management, than
the average fund.
G.6. Robustness to Use of Dispersion Trade Returns
Index-Level Results As described above we use data on correlation swaps as a cor-
relation risk proxy. The source of the correlation swap data also provided us with data on
implied correlations from dispersion trades which are an alternative approach to trading cor-
relation in equity markets. Instead of using the implied correlation from correlation swaps,
we use the implied correlation from dispersion trades to construct the time series of returns
for a correlation swap. In this subsection we show the robustness of our results to the use of
dispersion trade data. Table A12 reports results from regressing index level fund returns on
the dispersion trade return. The results are consistent with our earlier findings from Table 2 in
the paper. As Panel B of Table A12 shows, All funds have a statistically significant exposure
to the correlation risk factor (t-statitstic of −1.89). All Low Net Exposure funds and Long
11
Short Equity funds have an even higher exposure to to correlation risk exposure (t-statitstic
of −2.89 and −2.81, respectively). The table also confirms earlier results that Option Trader
funds, Funds of Funds and Managed Futures funds have statistically significant correlation
risk exposure in the BarclayHedge data base.
[Insert Table A12 here]
Our results are also robust to the use of the dispersion trade data for benchmarking index
level returns based on the TASS data. Table A13 reproduces the analysis from Table A9
using TASS data and a correlation risk factor based on dispersion trade data. It shows that
All Funds and Long Short Equity funds are statistically significantly exposed to correlation
risk. The t-statistics of −1.99 and −3.20 are even higher than in Table A9. In this sense our
baseline results in the paper that use the correlation swap implied correlations are conservative
as we obtain even stronger results using the dispersion trade implied correlation in tables A12
and A13.
[Insert Table A13 here]
Cross-sectional results In tables A14 and A15 we find that our conclusions also remain
qualitatively unchanged when using the dispersion trade implied correlation for the cross-
sectional pricing tests. Table A14 reproduces the analysis in Table 4 using dispersion trade
data and we find that the correlation risk premium is statistically significant and negative
using the Barclayhedge data.
[Insert Table A14 here]
Table A15 confirms the robustness of our results for the TASS data. It shows that the
correlation risk premium is also negative and statistically significant when using the TASS
data and data on implied correlations from the dispersion trades.
[Insert Table A15 here]
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14
Table A1: Summary Statistics for Benchmark Factors
Panel A: Summary Statistics
Mean Std Skew. Kurt. Min. Med. Max. Alpha Beta SR TM Msq