Abstract
Using large reductions in import tariffs as an exogenous shock to the competitive environment, this paper examines how an increase in foreign competition affects the importance of corporate governance. Consistent with prior studies, weak governance is associated with lower firm value, lower operating performance, lower labor productivity, higher capital expenditures, higher non-production expenses, and higher wages in the absence of increased competition. However, the differences between weak and strong governance firms along each of these dimensions are reduced or eliminated after a tariff cut. The effects are concentrated among firms in previously noncompetitive industries, defined as having sales concentration above the median or import penetration below the median in the year before the tariff cut. These conclusions are supported through the use of multiple alternative measures of operating performance and corporate governance. Altogether, the evidence indicates that an increase in competition can mitigate agency costs and serve as a substitute for traditional corporate governance mechanisms.
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Notes
By combining data from Compustat, the U.S. Department of Commerce, and the U.S. Bureau of Labor Statistics, the fitted HHI improves upon the traditional HHI measured using only Compustat sales data in that it captures the influence of both public and private firms.
The tariff data are available on the websites of Laurent Frésard and Philip Valta.
The choice of matching on 2-digit SIC code rather than 3-digit SIC code allows for a larger pool of potential control firms while reducing the likelihood that matched control firms in closely related industries are also affected by an import tariff reduction.
Before winsorization, the maximum and minimum values of ROE are 5.07 and \(-790.61\). For comparison, the median value is 0.14. After winsorization at the 2.5% level in each tail, the maximum and minimum values of ROE are 1.00 and \(-1.70\). Before winsorization, the maximum and minimum values of NPM are 0.54 and \(-5.09\). For comparison, the median value is 0.15. After winsorization at the 2.5% level in each tail, the maximum and minimum values of NPM are 0.40 and \(-0.46\).
A correlation matrix is presented in Table IA1 in the Internet Appendix.
These observations are consistent with other findings in related papers. Figure 2 in Frésard and Valta (2016) presents average tariffs over a seven year window around a tariff cut for treated and matched industries during the 1974 to 2005. The average tariff rate for control industries declines gradually over the seven year window, while the average tariff rate for treated industries drops by almost half in the event year and continues to decline in the subsequent years. Figure 1b of Dasgupta et al. (2018) illustrates an upward trend in average import penetration in control industries during a five year window around a tariff cut, while average import penetration for treated industries begins to trend up starting in the event year.
Following Gompers et al. (2003), firm fixed effects are not used due to insufficient variation in the G-Index within a firm over time.
Dasgupta et al. (2018) use a tariff cut dummy variable to identify the three years following a tariff cut, but they exclude the tariff cut event year from their analysis.
For robustness, Sect. 5.1 presents results using alternative clustering methods (SIC-3 industry, SIC-4 industry, or SIC-4 industry and year) and definitions for industry fixed effects (SIC-3 or SIC-4).
Since all non-dummy explanatory variables are standardized within each year to a mean of zero and standard deviation of one, this conclusion only applies to a firm with an average G-Index (i.e., standardized G-Index equal to zero). The overall impact of a tariff cut would be calculated as the sum of the coefficient on the tariff cut dummy and the product of the standardized G-Index value times the coefficient on the G-Index and tariff cut interaction term.
This procedure results in an equal number of tariff cuts classified as occurring in competitive industries and noncompetitive industries. However, because the number of firm-year observations associated with each tariff cut is not necessarily equal, the number of observations in competitive and noncompetitive industries in Tables 4 and 5 are not exactly equal.
See Table IA2 in the Internet Appendix for a listing of these states as well as the timing of the legislation.
Unlike the G-Index and the E-Index, the passage of BC laws represents plausibly exogenous variation in the strength of corporate governance. However, because anti-takeover legislation was implemented at the state of incorporation level, it may be a noisier measure of the strength of corporate governance compared to firm-level measures such as the G-Index and E-Index.
Since the data for the Hoberg and Phillips (2010) fitted HHI begin in 1984, the industry HHI in these regressions is calculated based on Compustat sales data. Results are qualitatively similar if the fitted HHI is used and the sample period is restricted to 1984–1995, or if the Compustat HHI is used to fill in missing values for the fitted HHI over the full sample period of 1976–1995.
The choice to match on 3-digit SIC code rather than 2-digit SIC code (as in the primary analysis) follows Amore and Žaldokas (2015), but the results using each method are qualitatively similar.
Amore and Žaldokas (2015) define the period of increased competition as all years after the passage of the Canada-U.S. Free Trade Agreement in 1989.
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Gempesaw, D. Corporate governance and product market competition: evidence from import tariff reductions. Rev Quant Finan Acc 56, 1437–1473 (2021). https://doi.org/10.1007/s11156-020-00931-8
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DOI: https://doi.org/10.1007/s11156-020-00931-8
Keywords
- Corporate governance
- Product market competition
- Agency cost
- Firm value
- Operating performance
- Import tariff reductions