Abstract
This paper examines systematic differences in earnings persistence between high-tech (HT) and non-high-tech (NHT) firms in the presence of economic- and accounting-driven factors. We document that (1) HT firms, relative to NHT firms, show lower levels of earnings persistence, even after economic and accounting factors identified in prior research are controlled; (2) the type of HT products (durables) increases earnings persistence; and (3) the association between earnings persistence and discretionary accruals is higher in HT firms, possibly because HT mangers use discretionary accruals to convey private information about future cash flows.
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Notes
The pharmaceutical industry may seem incongruous with the rest of the industries in the high-tech group, other than the high cost of R&D. The pharmaceuticals are selected into the high-tech group because the extent to which accounting practices in this industry would generate unrecorded intangible assets is very high.
Improvements to software, hardware and IT processes can provide Securities brokers and dealers and other investing firms with a competitive advantage, and therefore these firms invest substantially in improving technology. Trading activities and services provided in these firms are influenced to a great extent by uncertainties in the markets. During periods of volatile markets, in uncertain regulatory or economic environment, there is a greater degree of variance between revenues and expenses in these firms.
Chang and Su (2010) recently demonstrate that R&D intensity in the electronics industry has a positive (negative) impact on sales growth when the level of such R&D intensity is below (above) the threshold value. Their evidence implies that the level of R&D intensity, relative to a threshold value, matters to the financial health of high-tech firms.
For the sample period, the average total assets and sales of NHT firms are approximately four times greater than those for HT firms. The average total assets (sales) of NHT firms is $3,706.88 million ($3,269.5 million), compared with $926.9 million ($844.59 million) for HT firms.
Givoly and Hayn (2000) also use assets and sales to control for inflation. In this study, since we compare accumulated nonoperating accruals between high-tech firms and low-tech firms year-by-year, the difference cannot be attributed to inflation.
TACCRi,t = ΔCAi,t − ΔCLi,t − ΔCashi,t + ΔSTDi,t − Depi,t, where, for firm i at time t, ΔCAi,t = change in current assets (item #4); ΔCLi,t = change in current liabilities (item #5); ΔCashi,t = change in cash and cash equivalents (item #1); ΔSTDi,t = change in debt included in current liabilities (item #34); and Depi,t = depreciation and amortization expense (item #14). We also calculate total accruals as the difference between net income and operating cash flows and results are similar.
In 2006 the FASB issued FAS 123(R) requiring companies that grant stock options to expense them. Since investment projects in high-tech firms usually are long-term, and new products take years to develop, HT firms are more likely to issue options to increase the horizon of managerial action and encourage managers to take on positive net projects that improve the future prospects. In addition, because HT firms require greater cash flow availability to develop new products and services, they are likely to substitute cash compensation with stock options. High option expense may affect the barrier to entry. We do not examine the use of stock options in this paper because before 2006 there was no requirement for firms to expense stock options.
A number of statistical programs are available to perform the principal component analysis. In this study, we use the Statistical Analysis System (SAS) to calculate the IOS index. Procedures of the principal component analysis are discussed in detail in Sharma (1996, 67–71).
In this paper, we find that (1 − Θ) = 0.914 (0.941) for HT (NHT) firms during the sample period of 1993–2005, which implies that Θ = 0.086 (0.059). Baber et al (1998, p. 176) use earnings per share data from 1974 to 1993 and find that mean value of the IMA parameter (1 − Θ) is 0.857 and hence Θ = 0.143. The difference between their results and our results possibly reflects differences in the sample period, sample size, and the data availability requirement. This study also reports the results based on an alternative time-series model, Integrated Autoregressive Process [ARI (1,1,0)].
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Acknowledgments
We thank Sharad Asthana, Jeff Boone, Jim Groff, Gordian Ndubizu, Emeka Nwaeze, April Poe, Inho Suk, two anonymous reviewers, as well as participants at the 2012 SWAAA Conference, the 2011 American Accounting Association Conference, the 2011 Canadian Academic Accounting Association Conference, and the University of Texas at San Antonio workshop for their helpful comments.
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Appendix: Earnings persistence proxies
Appendix: Earnings persistence proxies
Earnings persistence is defined as the degree to which future earnings are induced by a $1.00 innovation in current earnings. Valuation theory suggests that analysts and investors should put greater emphasis on forecasting high-persistence earnings than low-persistence earnings, because changes in high-persistence earnings have a greater valuation impact than the same changes in low-persistence earnings. This time series properties of earnings (earnings persistence) are positively related to ERC, the magnitude of relation between earnings and returns (Kormendi and Lipe, 1987; Easton and Zmijewski 1989; Collins and Kothari, 1989).
Comparing values of an unexpected dollar of permanent earnings and transitory earnings explains the role of persistence. Empirical studies predict that transitory earnings surprises have an ERC of one and that the ERC of permanent earnings is one plus the inverse of the discount rate. Therefore, analysts and investors are relatively uninterested in transitory earnings because the trading profits that could be earned from private foreknowledge of a dollar of transitory earnings are smaller than the profits earned from private foreknowledge of a dollar of permanent earnings (Freeman and Tse 1992).
Since earnings follow a non-stationary process, earnings persistence can be measured better with a first differenced time-series model. In order to estimate firm-specific persistence levels, we adopt an ARIMA (1,1, 0) or ARI (1,1,0) (Kormendi and Lipe 1987; Easton and Zmijewski 1989) and an IMAMA (0,1,1) or IMA (0,1,1) (Collins and Kothari 1989; Ali and Zarowin 1992; Baber et al. 1998) time-series characterization of quarterly earnings. These consider seasonality of quarterly earnings and facilitate parsimonious empirical specifications of both earnings innovations and earnings persistence.
The ARI (1,1,0) model, or the first differenced AR(1) model with seasonality. Can be expressed as follows:
where X is quarterly actual earnings, ϕ is persistence parameter, B is backshift operator and a t is white noise. This also can be represented as
where ϕ is a firm-specific persistence level estimate measured by the autocorrelations of seasonally differenced earnings over the 32 quarters that end in each year of the sample period 1993–2005.
If ϕ is low, then current-earnings innovation would be more transitory. On the other hand if ϕ is high, then current-earnings innovation would be more permanent. Thus, ϕ measures the extent to which earnings innovations are permanent or transitory and quantifies the notion of earnings persistence.
The IMA (0,1,1) model with seasonality also can be expressed as:
If θ = 1, then earnings follow a mean reverting process, and earnings innovations are expected to be transitory. In contrast, when θ = 0, earnings follow a random walk process, and earnings innovations are expected to be permanent. Thus parameter (1 − θ) measures the extent of the persistence level.Footnote 12
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Kwon, S.S., Yin, J. A comparison of earnings persistence in high-tech and non-high-tech firms. Rev Quant Finan Acc 44, 645–668 (2015). https://doi.org/10.1007/s11156-013-0421-5
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DOI: https://doi.org/10.1007/s11156-013-0421-5