DOES SKEWNESS MATTER? EVIDENCE FROM THE I NDEX OPTIONS MARKET Madhu Kalimipalli a School of Business and Economics Wilfrid Laurier University Waterloo, Ontario, Canada N2L 3C5 Tel: 519-884-0710 (ext. 2187) [email protected]Ranjini Sivakumar b Centre for Advanced Studies in Finance School of Accountancy University of Waterloo Waterloo, Ontario, Canada N2L 3G1 Tel: 519-888-4567 (ext. 5703) [email protected](This draft November 8, 2002) Key Words : conditional volatility and skewness, option pricing biases, at-the-money delta-neutral strips, straps and straddles JEL Classification: G10, G14 a The first author acknowledges support from a Wilfrid Laurier University post-doctoral grant. b Corresponding author
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DOES SKEWNESS MATTER? EVIDENCE FROM THE INDEX OPTIONS MARKET
Madhu Kalimipallia
School of Business and EconomicsWilfrid Laurier University
Key Words: conditional volatility and skewness, option pricing biases, at-the-moneydelta-neutral strips, straps and straddles
JEL Classification: G10, G14
a The first author acknowledges support from a Wilfrid Laurier University post-doctoral grant.b Corresponding author
Does Skewness Matter? Evidence from the Index Options Market
ABSTRACT
We model the temporal properties of the first three moments of asset returns and examinewhether incorporating time varying skewness in the underlying asset returns leads toprofitable strategies using at-the-money S&P 500 index options. We devise trading rulesthat incorporate the skewness forecast to trade at-the-money delta-neutral strips, strapsand straddles. We find that a simulated trading strategy using a model with bothconditional volatility and skewness outperforms the GARCH model before and afteradjusting for transaction costs. The results indicate that index option prices forat-the-money options do not reflect time varying skewness. The evidence suggests thatmispricing of options may cause the negative skewness in the implicit risk-neutraldistribution in option prices.
Does Skewness Matter? Evidence from the Index Options Market
1. INTRODUCTION:
Existing literature has documented significant time varying skewness in stock index
returns (Harvey and Siddique, 1999 and 2000 and Hansen, 1994). The natural
development of skewness persistence models is an extension of volatility persistence
models and a direct consequence of asset pricing equations that contain third central
return moments. Harvey and Siddique (1999) find strong evidence for time varying
variance and skewness in monthly and weekly stock index data. Inclusion of conditional
skewness is found to attenuate asymmetric variance and seasonality effects in conditional
moments and lead to lower persistence in the variance equation.
There is significant empirical evidence (see e.g. Bates, 1996b for a summary) that the
Black-Scholes valuation model exhibits pricing biases across moneyness and maturity.
Bates (1991) shows that out-of-the-money (OTM) puts became very expensive relative to
OTM money calls during the year preceding the stock market crash in October 1987 as
skewness premium implicit in OTM money options on S & P 500 futures became
significantly negative. The negative skewness premium results in a “smirk” pattern in
index volatilities. In addition, Bates (2000) documents significant time varying skewness
in stock index option data.
The interesting question is how does the conditional skewness in the asset returns
affect the underlying risk neutral pricing distribution used in option valuation? Jackwerth
and Rubinstein (1996) document that in the pre 1987 period, both the risk-neutral
distribution (option implied distribution) and the actual distribution of S&P 500 returns
are about lognormal. However in the post 1987 period, while the actual distribution
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looks about lognormal again, the risk-neutral distribution is left-skewed and leptokurtic.
Bates (2000) suggests three explanations for the negative skewness in the implicit
risk-neutral distribution. The first is that investors view the underlying stochastic process
for S&P 500 returns has changed, the second is a change in investor’s risk aversion and
the third reason being a mispricing of post-crash options. Bakshi, Cao and Chen (1997)
and Bates (2000) among others look at the first explanation and propose option valuation
models that incorporate the asymmetry in the risk neutral pricing distribution. Jackwerth
(2000) looks at the second explanation. He empirically derives risk aversion functions
implied by option prices and realized returns on the S&P500 index for the period 1986-
1995. In the post 1987 period, he finds negative risk aversion functions that are
inconsistent with economic theory and concludes that the market misprices the options.
Bakshi et al. (1997) examine options on the S&P 500 index during the period
1988-1991. They compare the Black-Scholes (BS) model, the stochastic volatility model
(SV), the stochastic volatility stochastic interest (SVSI) model and the stochastic
volatility random jump (SVJ) model. Their empirical evidence suggests that overall, a
model with stochastic volatility and random jumps is superior to the Black-Scholes
model. Interestingly they find that for at-the-money (ATM) options, the Black Scholes
model does as well as the other models. Their in-sample analysis suggests that for ATM
options, the pricing models have similar implied-volatility values. In the out-of-sample
cross-sectional performance, they find that ATM call options valued using the Black-
Scholes model do not show any maturity-related bias. Their analysis of hedging errors
suggests that except for in the money (ITM) options, hedging errors using the Black-
Scholes model are indistinguishable from those obtained using the other models.
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In this paper, we investigate whether it is mispricing that causes the negative
skewness in the implicit risk-neutral distribution. Specifically, we examine if options are
mispriced because they ignore the embedded skewness in the underlying asset’s returns.
We model the temporal properties of the first three moments of asset returns following
Hansen (1994) and Harvey and Siddique (1999) and examine if incorporating time
varying skewness in underlying asset returns leads to profitable option based strategies.
We examine S&P500 index options data during the period November 1998 to December
2001. For this study, it appears that the hedging yardstick would be most appropriate.
Based on hedging errors, Bakshi et al. (1997) suggests that the Black-Scholes model
would work as well as the other models for pricing ATM options. Hence, we assume that
the Black-Scholes model is the appropriate option valuation model and assess whether
trading rules that incorporate the skewness forecasts of asset returns lead to profitable
strategies using ATM options.
We use a framework proposed by Noh, Engle and Kane (1994) to estimate the profits
from the options trading strategies. Noh et al. (1994) show that simple GARCH models
(that incorporate time varying volatility) outperform implied volatility models for
investors trading in at-the-money straddles, after accounting for transaction costs. We
use the GARCHS (GARCH with conditional skewness) model as in Hansen (1994) and
obtain the latent volatility and skewness from spot data. The GARCHS trading strategy
leads to trading in a strip or a strap. When conditional skewness is indeed constant, the
GARCHS reduces to a GARCH model and both models should yield similar returns.
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We find that a simulated trading strategy using the GARCHS model outperforms the
GARCH model before and after adjusting for transaction costs. The empirical evidence
indicates that index option prices for ATM options do not reflect time varying skewness..
This paper is organized as follows. In section 2, we provide a brief literature review.
In section 3, we describe the data and provide the sample description statistics. In section
4, we discuss the empirical methodology and present the results on the volatility models.
In the next section we discuss the trading strategies. In section 6, we present the results
on the trading strategies. Section 7 concludes.
2. BACKGROUND AND LITERATURE REVIEW:
What causes skewness or asymmetry in returns? There are at least four possible
explanations in the literature. The first explanation is the “leverage effect” whereby a
drop in stock price leads to higher operating and financial leverage and hence high
volatility in subsequent returns (Black, 1976). The second is based on the “volatility
feedback mechanism” whereby the direct effect of a positive shock on volatility is
mitigated by an increase in risk premium, while in the presence of a negative shock both
direct and indirect effects work to increase the risk premium. Negative dividend shocks
leads to higher firm volatility, which in turn leads to higher required rates of return on
equity and hence lower stock prices (Campbell and Hentschel, 1992). The third
explanation is based on a possible bursting of a “bubble”, a low probability scenario with
large negative consequences (Blanchard and Watson, 1982). Finally investor
heterogeneity and short sale constraints of investors explain skewness. When trading
volume is high, differences of opinion are also high and bearish investors with short-sale
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constraints are forced to a corner solution. When bad news hits the market, the hidden
information of the bearish investors is released to the market and this in turn induces
negative skewness in the subsequent periods (Chen, Hong and Stein, 1999).
Hansen (1994) provides a model of skewness evolution in the context of conditional
density estimation using a skewed Student-t distribution. He proposes a model of
skewness that evolves much like a GARCH process in squares of residuals and applies
the approach to the estimation of US Treasury securities and the US dollar/Swiss Franc
exchange rate. He finds evidence of skewness persistence. Harvey and Siddique (1999)
adapt Hansen's approach to a wide number of daily and monthly equity return series.
Harvey and Siddique (2000) introduce skewness in the CAPM framework by expressing
the stochastic discount factor or inter-temporal marginal rate of substitution as a quadratic
function of the market return. They find that the coskewness factor (defined as that part
of an asset’s skewness that is related to market portfolio’s skewness) has value in cross-
sectional CAPM regressions across assets. This is in addition to size and book-to-market
factors that were proposed by Fama and French (1992). The momentum effect in
portfolios is found to be related to the systematic skewness factor. The question that
follows is what does a negatively skewed empirical distribution imply for the implicit
risk-neutral distribution in option prices. We next review some of the options related
literature that looks at this issue.
Bates (1991) shows that the out-of-the money puts became very expensive during the
latter half of 1986, remained so until early 1987 and again during August of 1987 as
skewness premium implicit in out-of-the money options on S & P 500 futures became
significantly negative. No such effects were found during the months immediately
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preceding the October 1987 crash. Following the 1987 crash, the negative skewness
premium continued to be significant till the end of 1987. Citing the specification of the
underlying stochastic process as a possible reason for the skewness premium, the paper
introduces a diffusion model with systemic jump risk to capture the time varying
skewness in the data.
Using a jump-diffusion model, Bates (1996a) finds a significant positive implicit
skewness in currency options on Deutsche mark during the period 1984-1987, but not
from 1988-1991. The author shows that a SV model with jumps can explain high
kurtosis and skewness across different option maturities. Bakshi et al. (1997) propose an
option pricing model with stochastic volatility, stochastic interest rates and random
jumps. Their empirical evidence suggests that a model with stochastic volatility and
random jumps is superior to the Black-Scholes model. Bates (2000) again considers a
SV model now with time varying jumps to explain the skewness implicit in the S & P
500 futures option markets. The paper shows that models with SV or a negative
correlation between returns and volatility alone are not sufficient to generate the high
negative skewness or high volatility of volatility in the data.
In related research on the underlying stochastic process, Heston and Nandi (2000)
point out that a GARCH option valuation model that captures the negative correlation of
spot returns with volatility and the historical information in volatility model results in
reduced moneyness and maturity biases in option valuation. They also show that the
GARCH option valuation model is superior to an ad-hoc (smoothed) Black-Scholes
model proposed by Dumas, Fleming and Whaley (1998).
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Chen, Hong and Stein (1999) using a panel data of U.S firms, find that negative
skewness is most pronounced in stocks with high past trading volume and returns and for
larger sized stocks. Bakshi, Kapadia and Madan (2000) show that risk-neutral
distributions for individual stocks differ from that of the market index by being far less
negatively skewed and substantially more volatile. Jackwerth (2000) rules out changes in
investor risk aversion as a reason for the negative skewness and suggests mispricing as a
possible reason. We explore the mispricing explanation in this paper.
3. DATA AND SAMPLING PROCEDURE:
In this study, we use S&P 500 daily options data and daily index levels from October
1998 to December 2001. We examine the S&P500 index options data because these
options are widely traded. For each day, we use the closing option price and the closing
index level as reported in the Datastream International database. We assume that the
S&P 500 daily dividend yield interpolated to match the maturity of the option contract is
a reasonable proxy for the dividends paid on each option contract. We use the six-month
Treasury-bill rate as a proxy for the risk-free rate in the Black-Scholes valuation model.
Following Bakshi et al. (1997), options with moneyness (strike price/index level) in
the range 0.97 to 1.03 are deemed as at-the-money options and are included. Options
with maturity less than fifteen days and greater than 180 days are excluded. Only options
with daily volumes greater than 100 are retained. For a given exercise price and
maturity, options that have both put and call prices are retained. Options that violate the
put-call parity relationship are excluded. Since the option market closes after the stock
market, the option holder has a wildcard option. As in Noh et al. (1994), we ignore the
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wildcard option, understating the profits from the trading rules. Based on these criteria,
our sample consists of 2,279 call-put options pairs on 522 trading days.
Figure 1 presents the weekly S & P 500 price index and returns for the period
1970-2001. We see that the index surged from mid 90’s onwards and peaked in the year
2000 followed by a decline.
Table 1 presents the summary statistics of the weekly S & P 500 index data for the
period 1970-2001. In general we see that volatility, skewness and kurtosis have been
varying over time and have been high during the periods of oil shocks in the 1970s, the
1987 crash period and more recently since the year 2000. The sample period for our
index options (Nov 1998-December 2001) seems to be characterized by particularly high
volatility compared to the historical average. Figure 2 reveals that (unconditional)
market volatility has been steadily growing since mid 90s. Negative skewness has
become more prominent after the 1987 crash and more so during 2001. The kurtosis has
remained steady except for the crash year.
Table 2 presents the summary statistics of the daily S & P 500 index data for the
period 1970-2001 and the sub-period 1990-2001. In general for the full sample period,
we see that volatility, skewness and kurtosis vary over the week and are usually high on
Mondays compared to the rest of the week. From, Panel B we observe that for the period
1990-2001, a period following the October 1987 crash, the skewness and kurtosis are
high on Mondays, while the volatility is similar to the volatility on other days of the
week. Similar patterns are visible in Figure 3.
Figure 4 presents the density functions of the weekly and daily time series index data.
We see large negative skewness and fat tails in the data. In particular, we observe high
9
negative skewness in weekly data and high kurtosis in daily data. This is also confirmed
by Tables 1 and 2.
Panel A in Table 3 presents the augmented Dickey-Fuller unit root tests for the daily
and weekly price index data. We cannot reject the unit root null hypothesis for the index
data at both the daily and weekly frequencies. The first differencing however seems to
gives us the stationary return series. Panel B presents the Ljung-Box statistics for the
squared AR(1) return residuals. They indicate high auto-correlations in the daily and
weekly data that imply time dependence in higher order moments such as GARCH
effects.
4. RESULTS FROM CONDITIONAL VOLATILITY MODELS:
In this section we describe the conditional volatility and skewness models and their
results based on the time series index data. We use the GARCH (1,1)-in-mean model
with leverage and Monday effects and time varying conditional skewness and degrees of
freedom – referred to as GARCHS (1,1) model as the omnibus specification. Hansen
(1994) obtains a density function for a random variable driven by its skewness and
degrees of freedom (df) in addition to the first two moments. The details are provided in
Appendix 1. This specification is very general and it reduces to several known
specifications as special cases. The GARCHS(1,1) specification (denoted as Model 4 in
our tables ) is described below.
10
Model 4:
The distribution g(-) for the standardized residual error term is described in the appendix.
Other models (with the exception of the EGARCH model) can be obtained as special
cases of Model 4. The details of these models are provided in Appendix II. Model 1 is
the GARCH (1,1)-M model with leverage and Monday effects and is obtained by setting
df in Model 4 to a high number above 30 and by constraining skewness to zero. Model 2
is the EGARCH (1,1)-M with Monday effect. Model 3 is obtained by constraining the
conditional df and skewness equations in Model 4 to only have intercepts.
Table 4 presents the results for weekly index returns for the period 1970-2001. From
panel A in table 4 we see that variables in the mean equation are generally insignificant
for all models except for model 3 where the lag of returns is significant. In particular,
there is weak evidence of risk premium in the mean equation. However we find high
persistence in the variance equation and a strong evidence for leverage in the data. In
model 3, the intercept in the df equation denoting the average fatness in tails is not very
prominent, while the skewness intercept is highly significant.. In model 4, fat tails seem
to be driven by large (perhaps negative) shocks to the returns as evidenced by the
otherwise 0
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11
significant coefficient on lagged squared residual in the df. Conditional skewness effects
are significant. There is a large negative skewness and it is time varying.
From the last row in panel A, we note that Model 4 outperforms the other models in
terms of the highest likelihood. From panel B, we observe that Model 4 is the best
specification based on the AIC and SBC criteria. Models 1 and 2 come out as winners in
terms of normality of standardized residuals captured in the Jarque-Bera metric.
Conditional skewness and constant skewness models do not seem to be particularly
successful in correcting for non-normality in the standardized residuals. The likelihood
ratio metric for nested specifications confirms that Model 4 is a definite improvement
over Model 1. However there is not much improvement over Model 3. The last result
implies that time varying df and skewness in terms of lagged residuals do not add much
information beyond what is already contained in their respective intercepts. The Ljung-
Box statistic for squared standardized residuals is insignificant for all models indicating
that autocorrelation is insignificant. In particular, Ljung-Box statistics show that Model 2
with embedded leverage effect has the least correlation in higher moments. Model 4
seems to perform better at higher lags. This implies that conditional skewness and df
effects resulting in higher-order return correlations are less prominent in the weekly data.
Table 5 presents the results for daily index data for the period 1990-2001. From
panel A in table 5, we see that lagged returns are highly significant in all models. As
observed in weekly data there is weak evidence of risk premium in the mean equation.
Compared to the weekly data there is even a high persistence in the variance equation and
strong evidence for the leverage effect. The coefficient on lagged squared residuals in
the variance equation is insignificant indicating that mainly large negative shocks, as
12
captured in the leverage effect drive the volatility. In Models 3 and 4, the intercept in the
df equation is now highly significant. Unlike the weekly data, daily data has very
significant fatness in tails. However, there is not much evidence of time varying kurtosis
as the residual terms are insignificant. As in weekly data, conditional skewness effects
are also very significant. The main difference is in the size of the intercept term in the
skewness equation; skewness in the daily data is much less negative and significant
compared to the weekly data. Higher kurtosis and lower negative skewness in daily
index series relative to the weekly data is consistent with what we observe in tables 1-2
and figure 1. Monday effects are generally insignificant.
Panels A and B (table 5) indicate that Model 4 again outperforms the other models in
terms of the highest likelihood, AIC and SBC values. Model 2 is the best model in terms
of the Jarque-Bera metrics as before. The likelihood ratio test for nested specifications
shows that Model 4 is a definite improvement over models 1 and 3. There seems to be
incremental information in conditional skewness in daily data, in contrast to the results in
the weekly data. Just as in weekly data, the Ljung-Box statistic for squared standardized
residuals is insignificant for all models indicating that autocorrelation is insignificant. In
particular, Ljung-Box statistics show that Model 4 has the least correlation among higher-
order moments for lags up to 18. This implies that conditional skewness and df effects
that lead to return correlations are more prominent in the daily data. Model 1 seems to
perform better at lags beyond 18.
Figure 5 plots returns, latent conditional volatility, skewness and inverse degrees of
freedom from the conditional skewness model (Model 4) for the S & P 500 index weekly
series 1970-2001 and Figure 6 has a similar plot for the daily index data for the period
13
1990-2001. The lower the df the greater is the fatness in the tails of return distributions.
In general we find that periods of high volatility are also periods of high negative
skewness and fatness in the return distributions. The 1970s oil shocks, 1987 crash, 1990
Gulf war, 1997-98 Asian crisis, 1998-99 Russian crisis and the 2001 burst of the
technology bubble are all periods of high return shocks and also of high volatility and
skewness. Negative skewness became more pronounced i.e. underlying markets became
more pessimistic in these shock periods. These were also the periods when the return
distributions became very fat tailed. Comparing the latent skewness from weekly and
daily data we find that negative skewness is more pronounced in weekly data. This
follows from the fact that the skewness intercept for weekly data is more negative and
significant than for daily data (see Tables 4-5).
5. TRADING STRATEGIES:
We use the framework proposed by Noh, Engle and Kane (1994) to estimate the
profits from the options trading strategies. These strategies involve trading in
delta-neutral at-the-money straddles, strips and straps. Figure 7 depicts the profit patterns
in these strategies. In this paper, we argue that the investor can use the forecast of
skewness to formulate profitable trading strategies in strips or straps or straddles.
We forecast the volatility using the conditional volatility models. The GARCHS
model provides a forecast of skewness as well. While the GARCH model leads to
trading in a straddle, the GARCHS trading strategy leads to trading in strips or straps as
well. When conditional skewness is indeed constant, the GARCHS reduces to a GARCH
model and both models should yield similar returns. We use the volatility forecasts to
14
price the straddles, strips and straps using the Black-Scholes model. We use at-the-
money options because Bakshi et al.’s (1997) paper suggests that the Black-Scholes
model works well for pricing ATM options. Since we use delta neutral positions, we also
do not need to delta-hedge. We next describe the strategies and the trading rules.
A. Trading only in straddles:
1. First estimate each time series model (models 1 to 4) and obtain the average
volatility forecast for each model at time t for the remaining period to maturity
of an option.
2. Using the in-sample daily volatility forecasts from step 1, obtain the delta-
neutral (DN) straddle for each trading day.
3. Next plug the time t in-sample daily volatility forecasts from step 1 into the
BS option model and obtain the ATM DN straddle prices as in Noh, Engle
and Kane (1994).
4. Finally buy or sell the straddle depending on whether it is under or over-
priced. When the straddle is sold, the agent invests the proceeds in a risk-free
asset. Figure 8a illustrates this straddle trading strategy.
5. This strategy is implemented each day.
6. For all trades, we apply a filter as in Noh et al. (1994). The agent trades only
when the absolute price difference between model and market price is
expected to exceed $0.25 or $0.50.
7. We also evaluate the strategies after imposing trading costs of 0.5% of the
price of the straddle. We assume that an investor would trade for an amount
15
exceeding $10,000 and would pay a commission amounting to $120 + 0.0025
of the dollar amount as per a standard commission schedule (see Hull (2000)
p. 160).
8. The rate of returns are calculated as follows:
Return on buying a straddle = 1t1t
1t1tttPC
PCPC
−−
−−+
−−+
Return on selling a straddle = f1t1t
1t1ttt rPC
)PCPC(+
+−−+−
−−
−−
B. Trading in strips, straps and straddles:
Next we turn to delta-neutral strips, straps and straddles. Figure 8b shows the
differences between the straddles only strategy and that based on strips, straps and
straddles. With strips and straps we need estimates of the next period skewness. We
have a much larger set of trading opportunities now. These are described below (all
strips, straps and straddles are delta neutral ):
1. First estimate skewness time series model (models 3 and 4) and obtain the
average volatility forecast for each model at time t for the remaining period to
maturity of an option.
2. Using the in-sample daily volatility forecasts from step 1 obtain the delta-neutral
(DN) strip, strap and straddle for each trading day.
3. Next plug the time t in-sample daily volatility forecasts from step 1 into BS option
model and obtain the ATM DN strip, strap and straddle prices.
16
4. Finally buy or sell the strips, straps and straddles following the trading strategy
outlined below
• If skewness is likely to go down and the strip is under priced, buy the strip
• If skewness is likely to go up and the strap is under priced, buy the strap.
• If skewness is likely to go down and the strip is overpriced, buy the straddle if
it is under priced. If the straddle is not under priced, sell the strap.
• If skewness is likely to go up and strap is overpriced, buy the straddle if it is
under priced. If the straddle is not under priced, sell the strip.
• If skewness is likely to stay unchanged and the straddle is under priced, buy
the straddle.
In all the above trades, we apply the skewness filter in that we trade in strips an straps
only if skewness changes by more than plus (or minus) one standard deviation around the
mean, where mean and standard deviation refer to those of first differences in skewness.
While straddles traders have only the last trading strategy; traders using strips, straps and
straddles on the other hand have access to an added list of strategies from 1-4. We follow
the procedure below to compute returns from ATM delta-neutral strips, straps and
straddles :
5. The rate of returns are calculated as follows:
Return on buying a strip = 1t1t
1t1tttP2C
P2CP2C
−−
−−+
−−+
Return on selling a strip = f1t1t
1t1ttt rP2C
)P2CP2C(+
+−−+−
−−
−−
Return on buying a strip = 1t1t
1t1tttPC2
PC2PC2
−−
−−+
−−+
17
Return on selling a strip = f1t1t
1t1ttt rPC2
)PC2PC2(+
+−−+−
−−
−−
6. The returns are calculated after imposing the filters and before and after
transaction costs.
6. RESULTS FOR OPTION TRADING STRATEGIES:
Table 6 presents the summary statistics of S & P 500 index options data for the period
Nov 1998-December 2001. In general puts are cheaper relative to calls and trade more
heavily. At-the-money options (ATMs) also seem to have a shorter maturity compared to
out-of the money options (OTMs).
Figure 9 plots the Black-Scholes volatility inputs and skewness from competing
models for all the option trades in the sample. We find that Black-Scholes volatility
inputs are similar across models with EGARCH giving lower volatility inputs than other
models. The Model 4 skewness forecast are more sensitive to shocks than Model 3. The
Model 4 skewness forecast closely tracks the cubed residuals. .
Table 7 presents the results for delta-neutral straddles based on competing models
based on the above procedure. We use the S & P 500 index options data for the period
Nov 1998-December 2001. Panel A shows us that the average moneyness (X/S) is
1.0144, hence put prices are much higher relative to the call prices. Model 1
(GARCH (1,1)-M with normal distribution for the error term) comes closest to the actual
market prices of calls and put and straddles, while the EGARCH (1,1)-M gives us the
lower bounds. In general the model prices are much lower compared to the option prices
implying that options are over priced. Panel B gives us the number of buys and sells of
the delta-neutral straddles for competing models. We find that in general straddles are
18
sold in about 75% of the trades. Model 4 with time-varying volatility and skewness
involves the least short positions in straddles.
Panel C (table 7) presents percentage returns on trading in the delta-neutral straddles
for competing models using a $0.25 filter for stock price changes. Trading takes place
only if the absolute price deviation is greater than $0.25. We find that Model 1(GARCH)
performs best both before and after-transaction costs followed by the models that
incorporate skewness. Panels D and E (table 7) replicate Panels B and C results using a $
0.50-filter rule for stock price changes. We find that the numbers of trades are now lower
because of attrition due to the filter rule; the straddles are still sold more often than they
are bought. As before, Model 1 outperforms all others before and after 0.25% transaction
costs. In both panels, the median returns indicate that the EGARCH model performs
best.
Table 8 presents the results for delta-neutral strips and straps and straddles based on
competing models for S & P 500 index options data. Panel A shows that in general the
model prices are much lower compared to the option prices implying that options are
over priced. Panel B (table 8) gives us the number of buys and sells of the delta- neutral
strategies for competing models. In general we find that strips, straps and straddles are
sold more often than purchased. The buys and sells are now spread over strips, straps and
straddles unlike straddles only in table 7. Since we imposed a skewness filter, we find
that less than 20% of the trades are in straps and straps.
Panel C (table 8) presents percentage returns on trading in the delta-neutral strategies
for the competing models. We find that mean returns from both conditional skewness
models, are higher than those reported in table 7 both before and after transaction costs.
19
The t-statistics indicate that the returns from the strategy are significantly different from
zero.
Panels D and E (table 8) replicate panels B and C results using a $ 0.50-filter rule for
stock price changes. We find that the numbers of trades are now lower because of
attrition due to the filter rule; the number of sells still overwhelms the number of buys.
Returns from both skewness models still outperform all others reported in table 7
particularly after transaction costs.
6. SUMMARY AND CONCLUSIONS:
We investigate whether it is mispricing that causes the negative skewness in the
implicit risk-neutral distribution in S&P 500 index option prices. We model the temporal
properties of the first three moments of asset returns following Hansen (1994) and
Harvey and Siddique (1999) and examine if incorporating time varying skewness in
underlying asset returns leads to profitable strategies using at-the-money options. We
find that a simulated trading strategy using the GARCHS (skewness) model outperforms
the GARCH model both before and after adjusting for transaction costs. The empirical
evidence indicates that index option prices for ATM options do not reflect time varying
skewness. Our results suggest that mispricing of options may cause the negative
skewness in the implicit risk-neutral distribution in option prices.
20
Appendix I: Conditional Skewness Model:
The GARCHS (1,1) specification for the conditional mean, conditional variance andconditional skewness, where the error term in the mean has a skewed conditional studentt distribution with changing degrees of freedom, is as follows:
Conditional mean: t1t21t10t uhˆrˆˆr +++= −− ααα
where, ttt hu ε= and ( )ληΩε ,|zg~| 1tt −
where g ( ) is as described below.
Conditional variance: 21t1t3
21t21t10t uduhh −−−− +++= ββββ
where,
<
≥=
−
−− 0uif1
0uif0d
1t
1t1t
Conditional skewness 21t21t10t uSk −− ++= δεδδ
Degrees of freedom: 21t21t10t udf −− ++= γεγγ where ∞<< df2
The likelihood function for the skewed t distribution (Hansen 1994) is:
−≥
++
−+×
−<
−+
−+×
= +−
+−
ba
z1
abz2
11cb
ba
z1
abz2
11cb
),|z(g
2
12
21
2
η
η
λη
ληλη
where ηstands for degrees of freedom and is bounded as ∞<< η2 and λ is the skewness
parameter and is bounded as 11 <<− λ . Further the constants a, b and c are as defined
below.
21
−
+
=
−+=
−−
=
2)2(
21
c
a31b
12
c4a
222
ηΓηπ
ηΓ
λ
ηη
λ
Hansen (1994) show that this density function has a zero mean and unit variance.
Setting λ to zero gives us a regular t-distribution and setting η to a high number over 30
and λ to zero gives us a regular standard normal distribution.
22
Appendix II: Volatility and Skewness Models Tested
1. GARCH(1,1)-M with leverage and Monday effect:
2. E-GARCH(1,1) with Monday effect:
3. GARCHS(1,1) – M with leverage and Monday effects with constant skewness:
=
=
<
≥=
++++=
Ω=
+++=
−
−−
−−−−
−
−−
otherwise 0
Monday if 1
0 1
0 0
),|(~)|( ,
ˆˆ
1
11
42
1132
12110
1
12110
tMon
uif
uifd
Monu duhh
Zghu
uhrr
tt
tt
tttttt
ttttt
tttt
βββββ
ληεε
ααα
otherwise 0
Monday if 1
2
)ln()ln(
),|(~)|( ,
ˆˆ
41312110
1
12110
=
=
++
−++=
Ω=
+++=
−−−
−
−−
tMon
Monhh
Zghu
uhrr
t
ttttt
ttttt
tttt
βεβπ
εββα
ληεε
ααα
otherwise 0
Monday if 1
0 10 0
),|(~)|( ,
ˆˆ
1
11
0
0
42
1132
12110
1
12110
=
=
<≥
=
==
++++=
Ω=
+++=
−
−−
−−−−
−
−−
tMon
uifuif
d
Skdf
Monu duhh
Zghu
uhrr
tt
tt
t
t
tttttt
ttttt
tttt
δγ
βββββ
ληεε
ααα
23
4. GARCHS(1,1) – M with leverage and Monday effects with conditional skewness:
otherwise 0
Monday if 1
0 10 0
),|(~)|( ,
ˆˆ
1
11
212110
212110
42
1132
12110
1
12110
=
=
<≥
=
++=
++=
++++=
Ω=
+++=
−
−−
−−
−−
−−−−
−
−−
tMon
uifuif
d
uuSk
uudf
Monu duhh
Zghu
uhrr
tt
tt
ttt
ttt
tttttt
ttttt
tttt
δδδ
γγγ
βββββ
ληεε
ααα
24
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25
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26
Table 1
Summary statistics based on weekly S & P 500 index returns 1970-2001
Table 3Unit root and GARCH tests based on the weekly S & P 500 index data 1970-2001and daily S & P 500 index data 1990-2001
Panel A: ADF tests based on regressions with intercept
weekly data daily dataIndex 0.7743 -0.6908
Returns -23.2768 -21.9143We report the ADF test statistics for the gamma coefficient for the following regression. The null of unitroot is represented as γ=0. The critical value is –2.86 at a 95% confidence level.
Panel B: Ljung-Box test statistic value for the squared AR(1) residuals from returnseries
We report the Ljung-Box statistic for the squared residuals from the AR(1) return process at different lags.The Ljung-Box statistic for squared residuals is significant for daily data and weekly data up to lag 10.
ti
ititt yyy εβγα +∆++=∆ ∑=
+−−
8
2110
29
Table 4Estimates of competing conditional volatility and skewness models based on weekly S & P500 index data 1970-2001
Panel A: Model estimatesModel 1GARCH(1,1) - M
Model 2EGARCH(1,1) - M
Model 3GARCHS (1,1) -Mwith constant skewness
Model 4GARCHS (1,1) Mwith changingskewness
Mean- Equationintercept 0.099
(1.094)0.030
(0.409)0.107
(1.215)0.119
(0.748)rt-1 -0.020
(0.750)-0.011(0.541)
-0.035(2.106)
-0.029(1.010)
ht-1 0.014(0.642)
0.026(1.353)
0.013(0.602)
0.010(0.352)
Variance EquationIntercept 0.312
(3.808)0.095
(4.395)0.226
(2.925)0.236
(2.929)ht-1 0.812
(26.30)0.935
(63.15)0.850
(27.20)0.838
(27.70)Ut-1
2 0.024(1.39)
0.033(2.025)
0.038(1.957)
dt-1*Ut-12 0.193
(4.965)0.131
(3.573)0.146
(3.015)|εt-1|-sqrt(2/π) 0.199
(7.390)εt-1 -0.126
(6.131)
Degrees of freedom Equationintercept -0.163
(1.137)0.431
(0.441)Ut-1 -0.055
(0.570)Ut-1
2 -0.047(5.777)
DF: 14.917Skewness Equation
intercept -0.389(8.720)
-0.327(3.499)
Ut-1 0.021(0.203)
Ut-12 -0.012
(2.055)SK -0.173
# of parameters 7 7 9 13Log likelihood -3571.982 -3565.945 -3551.099 -3547.920T : 1669. (T-statistics reported in parentheses).
We report the Ljung-Box statistic for the squared standardized residuals. The Ljung-Box statistic for squaredstandardized residuals is insignificant for all models at different lags indicating that autocorrelation isinsignificant. *** indicates significant at 1% level .
31
Table 5
Estimates of competing conditional volatility and skewness models based on daily S & P 500 index data 1990-2001
We report the Ljung-Box statistic for the squared standardized residuals. The Ljung-Box statistic for squaredstandardized residuals is insignificant for all models at different lags indicating that autocorrelation is insignificant.
*** indicates significant at 1% level.
33
Table 6Summary statistics of S & P 500 index option data Nov 1998-Mar 2000
Number of observations 521. Average moneyness and maturity of the delta-neutral straddles are 1.0144,and 36.07 days respectively
Panel B: Number of buys and sells of delta-neutral strips, straps and straddles with $0.25 filterfor the competing models
trading in straddles trading in straps trading in stripstotal trades buys sells buys sells buys sells
Model 3:GARCH(1,1) – M(constant skewness)
521 91 338 12 32 9 31
Model 4:GARCH(1,1)-M(changing skewness)
521 100 330 34 107 11 25
Panel C: % Returns on trading in the delta-neutral strips, straps and straddles with $0.25 filter forcompeting models
Before transaction costs After transaction costs of 0.5%% daily return % daily return
# ofobs
mean median std.Dev
t-stat mean median std. dev t-stat
Model 1:GARCH(1,1)-M
511 2.49 1.10 24.11 2.35 2.00 0.60 24.11 1.90
Model 3:GARCH(1,1)-M(constant skewness)
521 2.60 0.80 24.19 2.46 2.55 0.58 24.56 2.37
Model 4:GARCH(1,1)-M(changing skewness)
521 2.13 0.80 23.64 2.06 2.08 0.57 24.02 1.98
37
Panel D: Number of buys and sells of delta-neutral strips, straps and straddles for the competingmodels with $0.50 filter for stock prices
trading in straddles trading in straps trading in stripstotal trades buys sells buys sells buys sells
Model 3:GARCH(1,1)-M
(constant skewness)
521 86 334 11 31 9 31
Model 4:GARCH(1,1)-M
(changing skewness)
521 92 326 10 34 11 25
Panel E: % Returns on trading in the delta-neutral strips, straps and straddles for competingmodels with $0.50 filter for stock prices
Before transaction costs After transaction costs of 0.5%% daily return % daily return
# ofobs
mean median std.dev
t-stat mean median std. dev t-stat
Model 1:GARCH(1,1)-M
506 2.36 0.83 24.05 2.24 1.89 0.33 24.05 1.79
Model 3:GARCH(1,1)-M(constant skewness)
521 2.52 0.69 24.09 2.39 2.47 0.46 24.46 2.31
Model 4:GARCH(1,1)-M(changing skewness)
521 2.12 0.69 23.32 2.07 2.08 0.46 23.71 2.00
38
Figure 1
S & P 500 index weekly series 1970-2001
39
Figure 2S & P 500 index weekly data by year (1970-2002)
Notes:Sigma refers to annualized standard deviation of weekly percentage returns, Skewness refers to skewnessof weekly percentage returns and Kurtosis refers to kurtosis of weekly percentage returns.
40
Figure 3
S & P 500 index daily return data by day of the week (1990-2001)
Notes:Sigma refers to annualized standard deviation of daily percentage returns, Skewness refers to skewness ofdaily percentage returns and Kurtosis refers to kurtosis of daily percentage returns. Index 2-6 refers to dayof the week i.e. 2-Mon, 3-Tue, 4-Wed, 5-Thur, 6-Fri.
41
Figure 4Density function for the S & P 500 index returns
42
Figure 5Plots of returns, latent conditional volatility, skewness and degrees of freedom from theconditional skewness model for the S & P 500 index weekly series 1970-2001
43
Figure 6Plots of returns, latent conditional volatility, skewness and degrees of freedom from theconditional skewness model for the S & P 500 index daily series 1994-2001
44
Figure 7:Option Trading Strategies and Profit Patterns:STRADDLE: Buy a call and a put with the same strike price and expiration dateProfit
Stock Price X
STRIP: Buy a call and two puts with the same strike price and expiration dateProfit
Stock Price X
STRAP: Buy two calls and a put with the same strike price and expiration dateProfit
Stock Price X
45
Figure 8Trading strategies involving options
46
Figure 9Plots of the Black-Scholes volatility inputs and skewness from competing models forall the option trades in the sample Nov 1998-Dec 2001