Abstract
This paper studies the effectiveness of comment letters by exploring the relationship between comment letters and stock price synchronicity. Using a unique dataset from China, we find that the issuance of comment letters is negatively correlated with stock price synchronicity. The results are robust to a battery of tests. Further analysis indicates that the negative relationship between comment letters and stock price synchronicity is more prominent for non-state-owned enterprises (non-SOEs) than SOEs. Then, we explore what channels comment letters affect the stock price synchronicity. Our evidence shows that firms receiving comment letters (1) have a high negative skewness indicating more negative information released, and (2) are more likely to amend their annual financial reports, leading to less stock price synchronicity. Overall, the evidence indicates that the comment letter process can help increase the firm information incorporated in the stock price.
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Notes
There is a hot debate about the measurement of stock price informativeness. Using three exogenous events, Li et al. (2020) find that the stock price synchronicity is negatively associated with information impounded in stock price. They manifest that the traditional measurement of stock price synchronicity is effective in China.
Source (in Chinese): http://kuaixun.stcn.com/2018/0401/14080666.shtml.
The official websites of Shanghai Stock Exchange (SSE) and Shenzhen Stock Exchange (SZSE) are respectively http://www.sse.com.cn/disclosure/credibility/supervision/inquiries/ and http://www.szse.cn/disclosure/supervision/inquire/index.html.
Because the disclosure requirements and accounting rules of the financial services firms are significantly different for this regulated industry, we drop the financial services firms.
Thanks for the suggestion from one anonymous reviewer. We use the sample without the winsorize process to study the relationship between comment letters and stock price synchronicity and find robust results. The results are shown in Appendix C.
We use the industry category based on the Guidance on the Industry Category of Listed Companies issued by the CSRC in 2012.
Thanks for the comments from the anonymous reviewer. We also cluster the standard errors at the firm-year level, and the results remain robust and are shown in Appendix C.
These five factors are gained from CSMAR database, and calculated based on Chinese stock market.
The yearly stock turnovers for each stock are obtained from the CSMAR database. In the database, the yearly stock turnovers are the sum of daily stock turnovers based on tradeable shares.
Firm-specific weekly return of firm $$i$$ in week τ is the natural log of one plus the residual return from the expanded market model regression, i.e.$${r}_{i,\tau }={\alpha }_{i}+{\beta }_{1,i}{r}_{I,\tau -1}+{\beta }_{2,i}{r}_{m,\tau -1}+{\beta }_{3,i}{r}_{I,\tau }+{\beta }_{4,i}{r}_{m,\tau }+{\beta }_{5,i}{r}_{I,\tau +1}+{\beta }_{6,i}{r}_{m,\tau +1}+{\varepsilon }_{i,\tau }$$. The detail of the construction NCSKEW is shown in Appendix B.
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The authors have no relevant financial or non-financial interests to disclose. This work was supported by the National Natural Science Foundation of China (Nos.72131011, 71873146, 71873147).
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All authors contributed to the study conception and design. Material preparation, data collection and analysis were performed by LX, Z (James) H and FW. The first draft of the manuscript was written by LX, and all authors commented on previous versions of the manuscript. FW added lots of new empirical tests and analyses according to the comments from the two anonymous reviewers. All authors read and approved the final manuscript.
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Appendices
Appendix A: Variable definitions
Variables measured on firm-level information | |
\({Synch1}_{t}\) | The first measure of stock return synchronicity. Logarithmic transformation of R2, which is the coefficient of determination from the estimation of Eq. (1) |
\({Synch2}_{t}\) | The second measure of stock return synchronicity. Logarithmic transformation of R2, which is the coefficient of determination from this estimation: \({r}_{i,\tau }={\alpha }_{i}+{\beta }_{1,i}{r}_{m,\tau }+{\varepsilon }_{i,\tau }\) |
\({Synch3}_{t}\) | The third measure of stock return synchronicity. Logarithmic transformation of R2, which is the coefficient of determination from the Fama and French five-factor model |
\({Synch4}_{t}\) | The fourth measure of stock price synchronicity. To avoid the weekend effect, we calculate weekly returns from Wednesday closing prices and follow Eq. (1) and (2) to calculate the fourth measure of stock price synchronicity \({Synch4}_{i,t}\) |
Comment letters | |
\({CL1}_{t}\) | A dummy variable equals one if firm \(i\) in year \(t\) receives at least one comment letter from Shanghai Stock Exchange or Shenzhen Stock Exchange, zero otherwise |
\({CL2}_{t}\) | The number of comment letters that firm \(i\) receives from the Shanghai Stock Exchange or Shenzhen Stock Exchange in year \(t\) |
Control variables | |
\({MB}_{t}\) | The market-to-book ratio of firm \(i\) at the end of year t |
\({Lev}_{t}\) | Total liabilities scaled by the book value of total assets at the end of year t |
\({ROA}_{t}\) | The ratio of income before extraordinary items to total assets at the end of year t |
\({Volume}_{t}\) | The trading volume of firm \(i\) in year t, i.e., the natural log of the Chinese yuan renminbi trading volume in year t |
\({Size}_{t}\) | The natural logarithm of total assets of a firm at the end of year t |
\({Big4}_{t}\) | A dummy variable that equals one if the firm is audited by one of the joint ventures of the four largest international accounting firms and domestic audit firms (the Big4 auditor) and zero otherwise |
\({Foreign}_{t}\) | The average percentage of foreign institutional investors hold on firm \(i\) in year t |
\({IndSize}_{t}\) | The logarithm of total assets of the industry to which firm \(i\) belongs in year t |
\({IndNum}_{t}\) | The number of firms in the industry to which firm \(i\) belongs in year t |
\({IndSpill}_{t}\) | A dummy variable that equals one if the industry that the firm belongs to receives any comment letter in year t, otherwise zero |
State-owned enterprises | |
\({SOE}_{t}\) | A dummy variable that equals one if the firm is a State-Owned Enterprise (SOE) and zero otherwise |
Other variables of interest | |
\({NCSKEW}_{t}\) | The negative coefficient of skewness, calculated by taking the negative of the third moment of firm-specific weekly returns for each sample year and dividing it by the standard deviation of firm-specific weekly returns raised to the third power. The details of the calculation can be seen in Appendix B |
\({Restate}_{t}\) | A dummy variable that equals one if the firm amends its annual reports in year \(t\) and zero otherwise |
Appendix B: Procedures for negative information release
Following Hutton et al. (2009), Kim et al. (2011a, 2011b), Baloria and Heese (2018), and Wen et al. (2019), we first estimate firm-specific weekly returns for each firm in each year on the following regression:
where \({r}_{i,\tau }\) is the week-τ return in year t of stock \(i\), and \({r}_{m,\tau }\) is the week-τ return in year t of the value-weighted A-share market index. \({r}_{I,\tau }\) is the week-τ return in year t of the industry to which the firm belongs, which is the value-weighted return of all the firms within the same industry in the sample, omitting the weekly return of firm \(i\). Then we measure the week-τ firm-specific return of firm \(i\) as \({W}_{i,\tau }=\mathrm{ln}(1+{\widehat{\varepsilon }}_{i,\tau })\) where \({\widehat{\varepsilon }}_{i,\tau }\) is the week-τ residual of regression (B.1).
We take the “negative coefficient of skewness” (NCSKEW) as the first measure of the negative information release:
where n is the number of observations of stock i’s specific weekly returns in year t.
Appendix C: Other robustness tests
We run two tests: one uses the sample without the winsorization of variables shown in Column (1), and the other is to cluster the standard errors at the firm-year level shown in Column (2). The coefficients on \(CL{1}_{t}\) are negative and significant, indicating the relation between comment letters and stock price synchronicity is unchanged under these two robustness tests.
3.1 Other robustness tests
Column (1) reports the regression results of the sample without the winsorization of variables, and Column (2) shows the results of clustering the standard errors at the firm-year level. *, **, and *** indicate statistical significance at the 10, 5, and 1% levels, respectively. The descriptions of these variables are provided in Appendix A
(1) | (2) | |
---|---|---|
\({Synch1}_{t}\) | \({Synch1}_{t}\) | |
\({CL1}_{t}\) | − 0.2625*** | − 0.2625* |
(0.0322) | (0.0961) | |
\({MB}_{t}\) | − 0.0088* | − 0.0088 |
(0.0051) | (0.0092) | |
\({Lev}_{t}\) | − 0.2819*** | − 0.2819* |
(0.0470) | (0.1149) | |
\({ROA}_{t}\) | − 0.0444 | − 0.0444 |
(0.0736) | (0.0756) | |
\({Volume}_{t}\) | − 0.1789*** | − 0.1789** |
(0.0123) | (0.0555) | |
\({Size}_{t}\) | 0.1229*** | 0.1229 |
(0.0115) | (0.0582) | |
\({Big4}_{t}\) | − 0.0883* | − 0.0883 |
(0.0457) | (0.0498) | |
\({Foreign}_{t}\) | 0.0102** | 0.0102 |
(0.0040) | (0.0068) | |
\({IndSize}_{t}\) | 0.1068 | 0.1068 |
(0.1170) | (0.1236) | |
\({IndNum}_{t}\) | − 0.0235 | − 0.0235 |
(0.1717) | (0.4340) | |
\({IndSpill}_{t}\) | 0.3530*** | 0.3530*** |
(0.1265) | (0.0383) | |
Constant | − 1.8311 | − 1.8311 |
(3.5513) | (1.8955) | |
Industry | Yes | Yes |
Year | Yes | Yes |
N | 9997 | 9997 |
Adj. R2 | 0.2947 | 0.2946 |
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Xu, L., Huang, Z.J. & Wen, F. Comment letters and stock price synchronicity: evidence from China. Rev Quant Finan Acc 59, 1387–1421 (2022). https://doi.org/10.1007/s11156-022-01078-4
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DOI: https://doi.org/10.1007/s11156-022-01078-4