Abstract
We hypothesize and test an inverse relation between liquidity and price volatility derived from microstructure theory. Two important facets of liquidity trading are examined: volume and noisiness. As represented by the expected turnover rate (volume) and realized average commission cost per share (noisiness) of NYSE equity trading, both facets are found negatively associated with the ex post and ex ante return volatilities of the NYSE stock portfolios and the NYSE composite index futures. Furthermore, the inverse association between noisiness and volatility is amplified in times of market crisis. The negative noisiness–volatility relation is also supported by our analysis on the effects of trade size on price volatility. The overall results demonstrate that volatility increases as noise trading declines.
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Notes
Noise in the sense of a large number of small events is often a causal factor much more powerful than a small number of large events can be (Black 1986). The terms “noise trading” and “liquidity trading” are used interchangeably in the market microstructure literature. We use “noise trading” to emphasize the nosiness and “liquidity trading” to emphasize the volume of liquidity.
This view is consistent with the work of Huang and Wang (2009), which postulates that endogenous illiquidity can lead to market crashes in the absence of any aggregate shocks.
Shleifer and Summers (1990) discuss arbitrage limits and conclude that “news alone does not move stock prices; uninformed changes in demand move them too.” Irrational noise traders with erroneous stochastic beliefs may affect prices and earn higher expected returns (De Long et al. 1990). In the presence of heterogeneous beliefs, Daigler and Wiley (1999) and Shalen (1993) have found that uninformed trading may cause price volatility.
Brennan and Subrahmanyam (1996) combine diverse empirical techniques from asset pricing and market microstructure research to study this relation. They find the microstructure parameters of market depth and illiquidity to be related to stock return premia. They relate illiquidity to adverse selection costs, which are costs associated with the discovery of private information that are paid by liquidity traders.
Johnson (2008) provides a model in which the equilibrium price-response measure of liquidity reflects the average risk-bearing capacity of the economy and volume reflects the changing contribution of individuals to that average. In that model, volume and liquidity are unrelated but jointly determined.
By AIC and BIC, an AR(1) process with a time drift is adequate to fit the logarithm quarterly turnover rate.
French et al. (1987) use one lagged cross-variance in Eq. (2) and make no adjustment for the mean return. We also estimate the quarterly volatility following their method. The estimates following French et al. (1987) are all positive and very close to the estimates in Eq. (2). The empirical analysis using the French et al. estimates of quarterly volatility is consistent with the analysis using the estimates in Eq. (2). For brevity, we do not report the analysis using the French et al. estimates.
According to Eq. (3), the association between \(\widetilde{{\Delta {\text{ACR}}_{\text{t}} }}\) and quarterly volatility (variance) can be written as \(\sigma_{\text{t}}^{2} = \exp \left( {2\varphi_{1} \cdot \widetilde{{\Delta {\text{ACR}}_{\text{t}} }} } \right) \cdot \exp \left[ {2\left( {\mu + \sum\nolimits_{{{\text{m}} = 2}}^{\text{M}} {\varphi_{\text{m}} \cdot {\text{f}}_{{{\text{m}},{\text{t}}}} + \frac{{1 - \theta {\text{L}}}}{{1 - \rho {\text{L}}}}\varepsilon_{\text{t}} } } \right)} \right]\), where \({\text{f}}_{{{\text{m}},{\text{t}}}}\) refers to the explanatory variables in addition to \(\widetilde{{\Delta {\text{ACR}}_{\text{t}} }}\). The marginal proportion of the volatility that is explained by \(\widetilde{{\Delta {\text{ACR}}_{\text{t}} }}\) is \(\exp \left( {2\varphi_{1} \cdot \widetilde{{\Delta {\text{ACR}}_{\text{t}} }} } \right) - 1\).
We also run the regressions with restrictions of the GARCH parameters and yield essentially identical results.
In the following reported GARCH regressions, we include the MA term. We also run the GARCH regressions without this MA term, and yield qualitatively similar results.
It is well known that the residual series in the GARCH process is strictly stationary with finite second moment provided α + β < 1 (see Tsay 2005: page 14). Engle and Rangel (2008: page 1191) explicitly point out that when α+β<1 , the conditional variance reverts to its mean value at a geometric rate of α + β.
\(\widetilde{{\Delta {\text{ACR}}_{\text{t}} }}\) is related to the variance of daily stock price returns in the following way: \(\sigma_{i,t}^{2} = \exp \left( {\varphi_{1} \cdot \widetilde{{\Delta {\text{ACR}}_{\text{t}} }} } \right) \cdot \exp \left( {m + \sum\nolimits_{n = 2}^{N} {\varphi_{n} \cdot f_{n,t} } } \right) \cdot h_{i,t}\), where \(\varphi_{n}\) (n = 1 to N) denotes the coefficient of \(\widetilde{{\Delta {\text{ACR}}_{\text{t}} }}\) or other corresponding liquidity variables in the regressions. The marginal (proportional) effect of \(\widetilde{{\Delta {\text{ACR}}_{\text{t}} }}\) on return variance is thus \({ \exp }(\varphi_{1} \cdot \widetilde{{\Delta {\text{ACR}}_{\text{t}} }}) - 1\).
This paper focuses on “micro” liquidity (trading volume and transaction costs), while the government often refers to “macro” liquidity (money supply in general or fund flows between asset sectors).
Jones (2002) reports a similar estimate.
Report that brokers charge a per-share commission to institutional traders as a convenient way of charging a predetermined fixed fee for broker services.
We use the 30 DJIA component companies as of the beginning of 2004. They are 3 M, Alcoa, Altria Group, American Express, AT&T, Boeing, Caterpillar, Citigroup, Du Pont, Eastman Kodak, EXXON Mobil, General Electric, General Motors, Hewlett–Packard, Home Depot, Honeywell International, Intel, IBM, International Paper, Johnson & Johnson, J. P. Morgan Chase, Coca-Cola, McDonald’s, Merck, Microsoft Corporation, Proctor & Gamble, SBC Communications, United Technologies, Wal-Mart Stores, and Walt Disney. AT&T, International Paper, and Eastman Kodak were subsequently replaced by AIG, Pfizer, and Verizon on April 8, 2004. However, AIG was later removed from the index on September 22, 2008.
NYSE TAQ databank traces back to the beginning of 1993.
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Acknowledgments
The author wishes to thank C.F. Lee (Editor) and two anonymous referees for helpful comments, M. Nimalendran, Jeffrey Pontiff, and Jiang Wang for helpful discussions, and Charles Bartlett from SIFMA for providing and explaining part of the data. The financial support from National Science Foundation of China for research project#71,273,150 is gratefully acknowledged.
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Appendices
Appendix 1: Average commission rate
SIFMA derives the exchange commission revenues of NYSE member brokers from the Security Exchange Commissions’ Financial and Operational Combined Uniform Single (FOCUS) Report regulatory filings. Initiated in 1980, the SIFMA databank is the sole source for quarterly reporting on the US securities industry financials. We track the time-series data of exchange commission revenues, which is the total quarterly commission income of all NYSE member brokers resulting from exchange equity transactions.
Our primary interest is in the average commission rate of NYSE trading. To derive this rate, we need to identify the trading volume that contributes to this commission revenue. Because NYSE members trade for their own accounts, not all NYSE share volume contributes to the exchange commission. On a monthly basis, NYSE discloses share and dollar volumes on the exchange, and total member purchases and sales. Total member volume consists of specialists’ purchases and sales, purchases and sales of non-specialists originating on the floor, and purchases and sales of non-specialists originating off the floor. We aggregate the NYSE member purchases and sales into a quarterly measure. We then subtract the sum of quarterly member purchases and sales from two times the quarterly NYSE share volume. This contributing volume is then used to scale the quarterly equity commission revenue to obtain the one-way average commission rate per share as follows:
Since some previous studies report commission costs relative to price, we estimate the percentage ACRt by scaling ACRt with the average trade price:
The average trade price is calculated as the ratio of dollar volume and share volume, which are reported by the NYSE on a quarterly basis.
Appendix 2: Validity check of ACR
Several prior studies have estimated institutional commission rates for sporadic time spots, and these estimates are consistent with ours for matched time spots. For instance, Berkowitz et al. (1988) estimate the institutional commission costs of NYSE trading in 1985 to be 0.18 %, as compared to our average commission rate estimate of 0.31 %. Keim and Madhavan (1997) find an average institutional commission rate of 0.20 % of trades during the period of January 1991 through March 1993, as compared to our estimate of the average commission rate of 0.24 % for the same period. Jones and Lipson (2001) find the average institutional commission rate of NYSE trades to be 0.119 % in the second and third quarters of 1997, which coincides with our estimate of the average commission rate of 0.119 % for the same period.Footnote 14 Note that the aforementioned researchers’ estimates of commission costs are based on their samples of NYSE institutional trades in different time spans, while our estimate of the average commission rate is for all NYSE trades. The above studies together with our research suggest that retail commission rates have declined more than institutional commission rates and that by 1997 both rates became similar in size.
Commissions vary over time and are not a constant proportion of stock price (see Jones 2002 for a complete survey of the history of commission regulation in the US). Per-share commissions are the dominant form of payment between brokers and their institutional clients. The negotiated rate per share charged to institutional investors depends on trade size and the research provided by the broker.Footnote 15 Commission rates charged to retail traders differ across brokers, while discount brokerages allow lower commission with less research service. For instance, per-trade commission is charged for Internet trades by online discount brokers. For both institutional and retail traders, trade size is inversely related to the realized commission rate. The latter reflects the composition of small trades in total trading volume. A higher realized commission per share reflects the presence of more small trades.
In order to check this contention, we estimate the proportion of small trades in total trades of the Dow Jones Industrial Average (DIJA) stocks using trade data from NYSE TAQ (Trade and Quote) databank. We follow the approach of Barclay and Warner (1993) and Chan and Fong (2000) in defining orders with less than 500 shares as small trades. We then calculate the ratio of the number of small trades to total trades for each day. The daily result is aggregated into a quarterly measure for each stock, and then the cross-sectional average of all 30 Dow stocks is estimated.Footnote 16 For the period 1993–2005,Footnote 17 the quarterly average small trade ratio is 0.608 with a standard deviation of 0.034. Its correlation with ACR is 71.8 %, and 50.3 % with the logarithmic ACR. Both correlations are significant at the 1 % level. This strong correlation lends support to our notion of ACR as a proxy of trading noisiness.
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Li, J. When noise trading fades, volatility rises. Rev Quant Finan Acc 47, 475–512 (2016). https://doi.org/10.1007/s11156-015-0508-2
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DOI: https://doi.org/10.1007/s11156-015-0508-2