Barth et al. (1999) document that firms sustaining a string of increasing earnings have higher price - earnings ratios and Myers et al. (2007) find such firms receive higher abnormal stock market returns during the string periods compared to firms not exhibiting this earnings pattern. The primary objective of the current study is to improve our understanding of how firms can maintain a consecutive string of increasing earnings. Most firms that have a string on increasing earnings do so by increasing revenues (Ghosh et al., 2005). Firms that maintain a string of earnings during periods of decreasing revenues must effectively manage costs to decrease their expenses sufficiently to increase earnings during those periods. Prior literature does not provide insights into the characteristics of firms and their market environments that allow them to maintain a string of consecutive earnings over periods that include both increasing and decreasing revenues. This paper contributes to filling that gap in the literature using large data and shows that cost flexibility is an important factor associated with a firm that can maintain a string of increasing earnings and finds that demand uncertainty for a firm’s products is inversely related to a firm’s ability to maintain a string of increasing earnings. In addition, an examination of the asymmetric cost behavior of the firms that experience at least one sales decrease during a consecutive string of increasing earnings indicates that these firms are associated with anti-sticky cost behavior during the string periods and exhibit sticky costs when the string ends.
Barth et al. (1999) document that firms sustaining a string of consecutive increasing earnings over five years or longer (hereafter often referred to as a “string”) have higher price-earnings multiples (i.e. P/E ratios) during the string than the firms not exhibiting this earnings pattern. Furthermore, the P/E ratios of firms experiencing a string have been found to increase with the number of years the firms have been able to sustain the string, with the largest increases occurring when the string gets to the fifth year. However, the P/E ratios of firms with strings decline significantly once the string breaks. Consistent with Barth et al.’s (1999) findings, Myers et al. (2007) find that firms sustaining a string of adjusted consecutive non-decreasing quarterly earnings per share (EPS) over at least twenty quarters (i.e. five years) have significantly higher abnormal stock market returns during the string periods than firms not exhibiting this earnings pattern1. The increases in P/E ratios and abnormal stock market returns provide managers with a strong incentive to report a string of increasing earnings or EPS, preferably for five years or longer.
Striving to maintain a string of consecutive increasing earnings or EPS over multiple periods is, of course, a subset of a larger body of literature that addresses issues related to meeting or beating an earnings-related target. The literature addressing issues related to meeting or beating earnings-related targets points out that there are many factors that enable and/or motivate firms to achieve such targets. These factors include revenue growth, management’s ability to manage costs, discretionary accounting choices, earnings management, firm size, slowing the growth of labor costs, and the pressure from investors or senior executives to meet or beat a specific target (e.g. see Beatty et al., 2002; Chu et al., 2019; Cohen & Zarowin, 2010; Ghosh et al., 2005; Dierynck et al., 2012; Kama & Weiss, 2013; Kao & Na, 2013). Due to a large number of these factors, as well as the interactions among them, it is impossible to develop a neatly defined model specifying the conditional expectations when earnings-related targets will or will not be achieved. This latter fact notwithstanding, one way or the other meeting or beating earnings-related targets is the result of meeting or beating targets with respect to revenues and/or costs (i.e. earnings equal the difference between revenues and costs)2.
Since a firm cannot have earnings without revenues, a prima facie argument can be made that revenue growth (i.e. a revenue target) is an important driver of sustained strings of increasing earnings over multiple consecutive periods. The importance of revenue growth in sustaining a firm’s earnings growth is clearly discussed in the business strategy literature (e.g. Porter, 1985). Based on a large sample of firms covering the period from 1980 to 2000, Ghosh et al. (2005) provide direct evidence supporting this argument. They find that roughly “…two-thirds of the firms with sustained increases in earnings also have concurrent sustained increases in revenues” (Ghosh et al., 2005: p. 34). The remaining one-third of firms in their study are considered to follow a “…cost-cutting strategy…to maintain sustained increases in earnings” (Ghosh et al., 2005: p. 34). The study by Ghosh et al. (2005) focuses on the subset of firms that generate a string of earnings via revenue growth. Their focus on revenue growth is premised, at least in part, on the argument that “…cost reductions are often ‘reactive’ while revenue growth strategies are typically ‘proactive’ (Ghosh et al., 2005: p. 36)”.
Of course, firms can and often do, take a proactive approach to cost reductions. In fact, a strong motivation for a proactive approach to cost reductions exists when a firm is striving to maintain a string of increasing earnings during periods in which revenues are forecasted to decrease. This fact notwithstanding, understanding a firm’s ability to maintain a consecutive string of increasing earnings via cost management has not been the focus of prior studies. The primary objective of the current study is to fill this gap by addressing the following basic research question: How can firms manage their costs to facilitate maintaining a string of increasing earnings, even during periods that include decreasing revenues (i.e. periods when revenue growth is clearly not the only important driver of a string of increasing earnings).
Based on a large contemporary data set covering the period from 1973 to 2018, the findings from the current study confirm the fact that revenue growth is an important driver facilitating a firm’s ability to maintain a string of consecutive increasing earnings. However, the current study also finds that firms with strings of consecutive increasing earnings, including strings that include at least one period of decreasing revenues, are associated with higher cost flexibility than firms without strings. In other words, cost flexibility places firms in a position to proactively manage their costs in a manner that allows them to facilitate maintaining a string of increasing earnings. In addition, an examination of the asymmetric cost behavior of the firms that experience at least one sales decrease during a consecutive string of increasing earnings shows that these firms are associated with anti-sticky costs during string years but exhibit sticky cost behavior in the year the string ends3. Furthermore, the current study finds that demand uncertainty for a firm’s products is inversely related to a firm’s ability to maintain a string of increasing earnings. The finding regarding demand uncertainty suggests that revenue predictability contributes to a firm’s ability to maintain a string of increasing earnings as more predictable revenues enable firms to maintain strings via the proactive application of cost management (e.g. by increasing the firm’s cost flexibility and applying anti-sticky cost behavior).
The current study contributes to the literature in the following ways. First, the current study confirms the prima facie argument, as well as previous empirical evidence (e.g. see Ghosh et al., 2005), that revenue growth is an important driver for maintaining a string of increasing earnings. Second, the current study provides new evidence regarding the way demand uncertainty impacts management’s decisions on cost flexibility. More specifically, whereas Banker et al. (2014b) find a negative association between demand uncertainty and cost flexibility, Holzhacker et al. (2015) find a positive association between demand uncertainty and cost flexibility. Our findings, in a different setting (i.e. firms striving to maintain a string of increasing earnings), are consistent with those of Banker et al. (2014b)4. Third, the current study extends the sticky cost literature by identifying a group of firms with asymmetric cost behavior that experienced at least one sales decrease during a consecutive string of increasing earnings, indicating that these firms are associated with anti-sticky cost behavior during the string periods and exhibit sticky costs when the string ends. Fourth, the current study provides insight into the role that being able to predict the demand for a firm’s products plays in facilitating a firm’s ability to maintain a string of increasing earnings via cost management.
The remainder of the paper will proceed as follows. Section II reviews prior literature and develops our hypotheses. We describe our research design and methodology in Section III. Section IV summarizes our sample selection and main empirical results. As a check on the robustness of our empirical results, Section V discusses several additional robustness tests. Section VI provides a discussion of the implications of the findings from our study. The last section, Section VII, provides concluding comments.
Using annual earnings, Barth et al. (1999) demonstrate that firms with strings of increasing earnings over five years or longer have higher P/E ratios during the string periods compared to firms without strings. They also find that the P/E ratios of these firms increase with the number of years that a firm has been able to sustain the string and decline significantly once a string of increasing earnings breaks5. Using adjusted non-decreasing quarterly EPS over twenty quarters or longer to capture a string, Myers et al. (2007) measure abnormal stock market returns during the string periods and observe phenomena consistent with the findings by Barth et al. (1999). Given the significantly higher market premia, firms clearly have an incentive to report strings of increasing earnings whenever possible. As Myers et al. (2007: p. 249) state, “These market premia, and the rapidity with which they disappear once the strings end, provide managers with incentives to maintain and extend the strings”. Barth et al. (1999: p. 388) make a similar point when they note that their inquiry about strings “... is motivated by the observation that many managers seem focused on maintaining steadily increasing earnings”.
The earnings management literature contains studies that have investigated issues related to the way firms are able to maintain strings of increasing earnings. Beatty et al. (2002), for example, allude to the matter of maintaining strings of increasing earnings by examining the small earnings increases reported by publicly held banks vs. privately held banks. They found that publicly held banks are more likely to use discretionary accounting choices to avoid small earnings decreases and report longer strings of increasing earnings. Using cross-sectional data excluding financial and regulated industries, Kao & Na (2013) study accruals and real earnings management during strings of increasing earnings and find both activities intensify towards the end of the strings. In a study that focuses on beating analysts’ forecasts of EPS, using a sample of firms that were subject to SEC (Securities and Exchange Commission) enforcement actions, Chu et al. (2019: p. 1969) find that “…pressure to maintain a reputation for beating analysts’ expectations can encourage aggressive accounting and, ultimately, earnings manipulation”6.
In their study that focuses on how increasing earnings via increasing revenues affect the quality of earnings and the earnings response coefficient (ERC), Ghosh et al. (2005: p. 54) find that “…earnings quality and ERCs are the highest when sustained increases in earnings are supported by sustained increases in both revenues and operating earnings.” Although Ghosh et al. (2005) focus on sustained earnings via sustained increases in revenues, they also point out that one-third of the firms in their study used a cost-cutting strategy to maintain a string of sustained earnings.
As noted in the Introduction, a prima facie argument can be made that revenue growth is an important driver of sustained strings of increasing earnings over multiple consecutive periods7. In fact, if a firm has a positive and stable contribution margin, as well as no increases in fixed costs, increasing revenues would obviously increase a firm’s earnings. Evidence supporting the importance of revenue growth to a string of consecutive increasing earnings was provided by Ghosh et al. (2005). The current study employs a much larger and more recent sample than that in the Ghosh et al. (2005) study in confirming the importance of revenue growth to the attainment of a string of consecutive increasing earnings.
To establish a baseline for considering the importance of cost management relative to revenue growth for maintaining strings of increasing earnings, we test that revenue growth is indeed an important driver of strings of increasing earnings. Thus, we formally state our Hypothesis 1 (H1), in the alternative form as:
Hypothesis 1. Consecutive revenue growth is an important driver of strings of increasing earnings.
Much of the early literature on cost management focuses on operating leverage, emphasizing the trade-off between fixed and variable costs. In his seminal paper, Lev (1974: p. 637) links higher operating leverage to higher asset intensity (total assets divided by sales revenue), arguing that managers may increase the operating leverage (i.e. increasing fixed costs relative to variable costs) of firms by increasing capital investments. A concept closely related to operating leverage is cost flexibility, which refers to a firm’s ability to adjust its costs. Cost flexibility is affected by the composition of discretionary costs and non-discretionary costs in a firm’s cost structure. A cost structure with a higher (lower) ratio of discretionary costs to non-discretionary costs is associated with higher (lower) cost flexibility. Recognizing that non-discretionary costs tend to be fixed and discretionary costs tend to be variable, Balakrishnan et al. (2008: p. 171) make the connection between operating leverage and cost flexibility, stating that “…a cost structure with less operating leverage (i.e. a lower proportion of fixed costs) offers companies flexibility because it involves fewer upfront cost commitments (i.e. fewer fixed costs).” Holzhacker et al. (2015: p. 2331) also note the value of having a cost structure with less operating leverage and “…provide empirical evidence that firms respond to a risky environment by altering their resource procurement choices to increase cost elasticity”.
Firms may choose to commit to higher operating leverage (lower cost flexibility) to increase their activity capacity and reduce unit cost, though higher operating leverage exposes firms to greater risk. In this regard, conventional wisdom in managerial accounting textbooks (e.g. Balakrishnan et al., 2008) suggest that firms should move to a higher operating leverage when sales are anticipated to be high and switch to a lower operating leverage when sales are anticipated to be low—a cost management strategy that allows firms to achieve higher profits for a single year. However, firms rarely (if ever) can easily switch back and forth between high and low operating leverage to adjust to anticipated periodic sales levels. Thus, to sustain a string of increasing earnings over consecutive periods of five years or longer, it seems logical for firms to focus on maintaining cost flexibility (i.e. avoiding being locked into an excessive amount of non-discretionary costs).
The above discussion leads us to our second hypothesis, which concerns the role of cost flexibility in facilitating strings of consecutive increasing earnings. We formally state this hypothesis as Hypothesis 2 (H2), in the alternative form below:
Hypothesis 2. Firms with strings of increasing earnings have more cost flexibility compared to firms without such strings.
While our second hypothesis is concerned with the role of cost flexibility in managing costs to maintain strings of increasing earnings, our next hypothesis is concerned with asymmetric cost behavior. The seminal paper by Anderson et al. (2003) documents that cost changes are asymmetrical in sales increases as compared to sales decreases. They argue that cutting costs often requires additional resource adjustments and managers are reluctant to cut resources when sales decrease. This argument has led to what has become known as the sticky cost phenomenon, which means costs increase more rapidly when sales increase than they decrease when sales decrease8. The asymmetric cost behavior literature focuses on managers’ decisions related to cost management. In their review of the asymmetric cost behavior literature, Banker & Byzalov (2014: p. 43) note that “While the traditional view of cost behavior envisions a mechanistic symmetric relation between costs and concurrent activity, modeled as fixed and variable costs, this new way of thinking is rooted in an explicit recognition of the role of deliberate managerial decisions in short-run cost behavior”9.
Studies on asymmetric cost behavior have found that several factors, such as capacity utilization, empire building, earnings targets, strategic orientation, sales forecasts, level of intangible assets, and risk management, moderate the asymmetric cost behavior of firms (e.g. Balakrishnan et al., 2004; Chen et al., 2012; Dierynck et al., 2012; Kama & Weiss, 2013; Banker et al., 2013; Banker et al., 2014a; Holzhacker et al., 2015; Venieris et al., 2015; Banker et al., 2016; Hall, 2016; Ballas et al., 2022). Among these studies, Dierynck et al. (2012) and Kama & Weiss (2013) examine how firms manage costs when managers face incentives to meet a single period earnings target10.
Dierynck et al. (2012) analyze whether decisions related to labor costs in private Belgian firms have been motivated by management’s desire to avoid losses. They find that when these firms report small earnings, labor costs increase at a slower rate when activity increases than they decrease when activity decreases (i.e. labor costs behave in an anti-sticky fashion when firms try to avoid losses). Using a large sample of U.S. firms, Kama & Weiss (2013) also find costs become anti-sticky (i.e. costs decrease more rapidly when sales decrease than they increase when sales increase), when firms are trying to meet a single period earnings target. Kama & Weiss (2013: p. 219), however, note that it is hard for firms to meet earnings targets over multiple periods via accelerating cost reductions.
As discussed above in connection with our first hypothesis, consecutive revenue growth is an important driver of sustained strings of increasing earnings over multiple consecutive periods. We know, however, that many firms maintain strings of increasing earnings over periods that include at least one period of sales decrease (e.g. Ghosh et al., 2005). Maintaining an increase in earnings during a period of declining revenues means that the magnitude of the cost decrease is greater than that of the revenue decrease in a particular year11. Such cost behavior is consistent with the notion of anti-sticky costs. Once firms are no longer able to cut costs sufficiently to maintain the strings, we would expect the anti-sticky cost behavior to end.
The above discussion leads us to our third hypothesis concerning the asymmetric cost behavior of firms that experience at least one sales decrease during strings of consecutive increasing earnings. We formally state this hypothesis as Hypothesis 3 (H3), in the alternative form below:
Hypothesis 3. Firms that experience at least one sales decrease during a string of consecutive increasing earnings are associated with anti-sticky costs during the string period but exhibit sticky cost behavior when the string ends.
The second and third hypotheses relate to cost management strategies that firms can employ to maintain strings of consecutive increasing earnings. However, implementing these strategies is clearly a function of a firm’s ability to plan for future costs and revenues. A fundamental aspect of being able to plan for future costs and revenues is the demand uncertainty confronting a firm. When the demand uncertainty for a firm’s products is high, actual revenues and costs may deviate significantly from anticipated revenues and costs (i.e. profits are highly volatile). This makes maintaining a string of increasing earnings via cost management difficult for two reasons. First, when demand uncertainty is high, forecasts of future sales and costs are less accurate, which limits the ability of firms to prepare accurate budgets. Second, when demand uncertainty is high, unexpected large revenue decreases are likely to occur more frequently. With unexpected large revenue decreases, it is difficult for firms to sustain a string of increasing earnings by managing discretionary costs. Hence, higher demand uncertainty is expected to impede the ability of a firm to maintain strings of increasing earnings via cost management. In this regard, Holzhacker et al. (2015: p. 2328) find that firms can hedge against risks from demand uncertainty by “substituting away from committed resources and toward more flexible resources to allow for higher cost elasticity…”. In discussing the optimal cost structure in a different setting, Banker et al. (2014b) find “…that firms will choose a higher capacity of fixed inputs when uncertainty increases in order to reduce congestion costs”12.
Based on the observations discussed above, we hypothesize that the demand for the products of firms with strings of consecutive increasing earnings are more predictable (i.e. lower demand uncertainty) compared to firms without strings13. We formally state this hypothesis as Hypothesis 4 (H4), in the alternative form below:
Hypothesis 4. Firms with consecutive strings of increasing earnings confront lower demand uncertainty compared to firms without such strings.
Following Barth et al. (1999), we define a string of increasing earnings as consecutive increases in annual earnings for five years or longer. We identify firms that had reported strings of increasing earnings (i.e. string firms subsample) and firms that had never reported strings of increasing earnings (i.e. non-string firms subsample) between 1973 and 2018. For the string firms subsample and non-string firm subsample, we measure the frequency of consecutive revenue growth, cost flexibility, asymmetric cost behavior, and demand uncertainty separately. These measures are compared between the string firms and non-string firms to test our hypotheses.
To test our first hypothesis regarding the argument that consecutive revenue growth is an important driver of strings of consecutive increases in earnings, we define a firm-level Consecutive Revenue Growth Ratio measure. This measure is calculated as the ratio of the number of years in consecutive revenue growth of five years or longer to the total number of years of observations for each firm. This ratio provides a measure of frequency of consecutive revenue growth each firm experienced. We then compare the average Consecutive Revenue Growth Ratio of the string firms to that of the non-string firms. Based on our first hypothesis (H1), we expect that the string firms have a significantly higher Consecutive Revenue Growth Ratio than the non-string firms.
To test our second hypothesis regarding the level of cost flexibility of firms with strings versus firms without strings, we assume a log-linear relationship between cost changes and sales changes. We choose the log-linear model over a linear model because the log transformation mitigates the skewedness issue, making variables more comparable across firms and industries. In addition, the coefficients from the log-linear model can be conveniently interpreted as the percentage change of the dependent variable corresponding to one percent change in the independent variable (Banker et al., 2014b: p. 848). Formally, we state our Model (1), as shown below:
ln ( O C i , t O C i , t − 1 ) = β 0 + β 1 ln ( S a l e s i , t S a l e s i , t − 1 ) + ∑ s = 1 4 γ 1 , s × E c o n V a r s , i , t + ε i , t , (1)
where OCi,t is firm i’s operating costs in year t, and Salesi,t is firm i’s sales revenue in year t.
Following Anderson et al. (2003), Chen et al. (2012), Dierynck et al. (2012), and Banker et al. (2014b), we use EconVars to control for the following economic variables: Employee Intensity, Asset Intensity, Successive Decrease, and Stock Performance. We control for employee intensity and asset intensity because they both influence the cost commitments in expenditure decisions. Employee Intensity is calculated as the ratio of the number of employees to sales revenue. Asset Intensity is measured as the ratio of total assets to sales revenue. We follow Chen et al. (2012) and Dierynck et al. (2012) to control for the successive pattern of sales decreases because managers may consider sales decreases in a successive pattern to be a permanent decline when making cost commitment decisions. Successive Decrease is an indicator variable that equals 1 if S a l e s i , t − 1 < S a l e s i , t − 2 and 0 otherwise. Chen et al. (2012) also point out that good stock performance reflects the market’s positive expectation about a firm’s future earnings and this may also affect the firm’s cost commitments. Hence, we control for Stock Performance, which is calculated as the raw stock return in the prior fiscal year14.
When estimating the models, we include industry fixed effects to control for the impact of an industry on a firm’s cost structure. In addition, following Petersen (2009), we use pooled cross-sectional regressions, including year effects, and cluster observations by firms to provide standard errors that are robust to autocorrelation and heteroscedasticity.
Our proxy for cost flexibility (i.e. a firm’s ability to adjust its costs) is β1, the coefficient of ln ( S a l e s i , t S a l e s i , t − 1 ) in Model (1). The coefficient β1 is expected to be positive and represents roughly the percentage change in costs corresponding to a one percentage change in sales. In other words, β1 captures the sensitivity of costs changes to sales changes. A high β1 means costs are highly responsive to sales changes, hence suggesting a highly flexible cost structure. Our second hypothesis (H2) will be supported if β1 is significantly greater for string firms than for non-string firms.
To test our third hypothesis (H3) regarding asymmetric cost behavior for firms that experience at least one sales decrease during a string of increasing earnings, we use a modified version of the Anderson et al. (2003) model. Our model is different from the Anderson et al. (2003) model in two ways. First, while Anderson et al. (2003) focus on SG&A expenses, we examine operating costs (OC) (i.e. annual sales revenue minus income from operations). Our definition of operating costs, which is consistent with that of Balakrishnan et al. (2004), Balakrishnan & Gruca (2008), Weiss (2010), and Kama & Weiss (2013), captures managerial choices affecting the costs of manufacturing goods, the costs of providing services, and the costs of marketing and distribution. We believe that operating costs are a better measure for our study because it is unlikely that managers who are motivated to achieve a specified earnings level would limit their cost management activities to only SG&A costs. Second, in order to examine the asymmetric cost behavior for string firms when the string ends, we add a dummy variable Break to indicate the year when earnings stop increasing. We also include all economic control variables identified earlier in Model (1). Formally, we state our Model (2), as shown below:
ln ( O C i , t O C i , t − 1 ) = β 0 + β 1 ln ( S a l e s i , t S a l e s i , t − 1 ) + β 2 D e c i , t × ln ( S a l e s i , t S a l e s i , t − 1 ) + β 3 B r e a k i , t + β 4 ln ( S a l e s i , t S a l e s i , t − 1 ) × B r e a k i , t + β 5 D e c i , t + β 6 ln ( S a l e s i , t S a l e s i , t − 1 ) × D e c i , t × B r e a k i , t + ∑ s = 1 4 γ 1 , s × E c o n V a r s , i , t + ∑ s = 1 4 γ 2 , s ln ( S a l e s i , t S a l e s i , t − 1 ) D e c i , t × E c o n V a r s , i , t + ε i , t , (2)
where Deci,t is a dummy variable that equals 1 if Salesi,t < Salesi,t−1 and 0 otherwise. Breaki,t is an indicator variable that is set to 1 if earnings in year t is less than earnings in year t − 1 but earnings in year t − 1 is more than earnings in year t − 2. Hence, for firm years associated with a string of increasing earnings, Breaki,t is 1 for the year immediately after the string of increasing earnings and 0 otherwise. All other variables are as previously defined. Based on the sticky cost phenomenon documented in prior cost behavior literature (e.g. Anderson et al., 2003), we measure asymmetric cost behavior using β2, the coefficient of D e c i , t ln ( S a l e s i , t S a l e s i , t − 1 ) in Model (2). We expect β2 to be negative for all firm years in our sample.
Our third hypothesis (H3) proposes that costs of firms that experience at least one sales decrease during strings are anti-sticky over the string periods, which will be supported if β2 is significantly positive for the string firm years for these firms. We also expect costs to become sticky again once the string breaks, which suggests that β6, the coefficient of ln ( S a l e s i , t S a l e s i , t − 1 ) × D e c i , t × B r e a k i , t , to be negative.
Demand uncertainty refers the variability in the sales of a firm’s products. Following Banker et al. (2014b), we measure the demand uncertainty for a firm in a particular year using the standard deviation of log changes in revenues for the past five years (i.e. Δ ln S a l e s i , t , or ln S a l e s i , t S a l e s i , t − 1 )15. Our fourth hypothesis (H4) will be supported if the demand uncertainty of string firms is significantly lower than that of the non-string firms16.
We construct a sample by first examining a population of all firm years in Compustat from 1973 to 201817. Financial institutions and public utilities (four-digit SIC codes 6000 - 6999 and 4900 - 4999) were excluded from our sample because the structure of their financial statements is difficult to compare with that of firms in other industries (Fama & French, 1992; Dechow et al., 2012). Prior studies on earnings patterns have defined strings of increasing earnings as either consecutive increases in annual earnings (e.g. Barth et al., 1999; Ghosh et al., 2005; Kao & Na, 2013) or consecutive increases in quarterly earnings (e.g. Chu et al., 2019; Ke et al., 2003; Ke & Petroni, 2004; Myers et al., 2007; Shanthikumar, 2012). We follow the former definition (i.e. consecutive increases in annual earnings) so that our results are comparable to prior cost management studies (e.g. Anderson et al., 2003; Kama & Weiss, 2013; Balakrishnan et al., 2014; Banker et al., 2014a, 2014b). Following Ke & Petroni (2004), we omit the left-truncated and right-truncated strings to avoid the truncation problem. We also eliminate outliers that are in the top one percent and the bottom one percent of all continuous variables in the model. In addition, firm years with missing data for regression analysis are excluded from the sample. These results in a final sample of 14,694 firms associated with 157,325 firm years.
Among the 157,325 firm years, we identify 59,557 firm years associated with 2760 firms that have reported at least one string over the entire sample period (hereafter often referred to as the string firms), and 97,768 firm years associated with 11,934 firms that have never reported a string of increasing earnings over the entire sample period (hereafter often referred to as the non-string firms). In total, the string firms have reported 3259 strings associated with 22,189 firm years (hereafter often referred to as the string firm years).
As summarized in
| Panel A: Distribution of String Length | ||||
|---|---|---|---|---|
| Strings without any sales decreases during the string periods | Strings with at least one sales decrease during the string periods | All strings | ||
| Mean of Length | 7.20 | 7.70 | 7.31 | |
| Std Dev of Length | 3.35 | 3.97 | 3.51 | |
| Minimum Length | 5 | 5 | 5 | |
| Maximum Length | 40 | 37 | 40 | |
| Number of Strings | 2431 | 828 | 3259 | |
| Number of Firms | 2027 | 774 | 276018 | |
| Number of Firm Years | 16,141 | 6048 | 22,189 | |
| Panel B: Industry Distribution | |||
|---|---|---|---|
| Industry | String firms | All firms | Concentration of string firms |
| Consumer Durables | 127 | 461 | 27.55% |
| Wholesale, Retail, and Some Services | 480 | 1776 | 27.03% |
| Consumer NonDurables | 255 | 987 | 25.84% |
| Manufacturing | 467 | 1867 | 25.01% |
| Chemicals and Allied Products | 97 | 392 | 24.74% |
| Other | 430 | 2456 | 17.51% |
| Telephone and Television Transmission | 99 | 602 | 16.45% |
| Business Equipment | 466 | 3441 | 13.54% |
| Oil, Gas, and Coal Extraction and Products | 126 | 935 | 13.48% |
| Healthcare, Medical Equipment, and Drugs | 213 | 1777 | 11.99% |
| Total | 2760 | 14,694 | 18.78% |
earnings strings. The length of the strings varies from 5 to 40 years, with an average length of 7.31 years for all strings. For the strings without any sales decrease during the string period, the length varies from 5 to 40 years with an average length of 7.20 years, whereas for the strings with at least one sales decrease during the string period, the length of strings varies from 5 to 37 years with an average length of 7.70 years.
Panel B of
Panel A of
The average Asset Intensity is significantly lower for string firms (1.09) than for non-string firms (1.91). Given that lower asset intensity is typically associated with lower investment in non-discretionary costs, this result is consistent with our expectation. The average Employee Intensity is significantly higher for the string firms (0.0107) than for the non-string firms (0.0105). This is also consistent with our expectation since employee-related costs are typically considered to be discretionary.
Consistent with Barth et al. (1999), we find that the average annual earnings per share (EPS) of the string firms (1.71) are significantly higher than that of the non-string firms (0.55). In addition, for the string firms, the average EPS of the string years are significantly higher than that from the non-string years. The raw stock return (Stock Performance) of the string firms (0.11) is significantly lower than that of the non-string firms (0.15), which can be explained by the fact that the string firms tend to be larger and more mature firms with lower risk. We
| Panel A: Descriptive Statistics of Key Variables | |||||
|---|---|---|---|---|---|
| Variables | Number of Observations | Mean | Standard Deviation | Min | Max |
| Sales | 157,325 | 2567.53 | 13113.82 | 0.01 | 511729.00 |
| OC | 157,325 | 2431.79 | 12437.76 | 0.02 | 505059.00 |
| Dec | 157,325 | 0.30 | 0.46 | 0.00 | 1.00 |
| Break | 157,325 | 0.17 | 0.37 | 0.00 | 1.00 |
| Employee Intensity | 157,325 | 0.01 | 0.01 | 0.00 | 0.19 |
| Asset Intensity | 157,325 | 1.60 | 3.38 | 0.19 | 81.45 |
| Successive Decrease | 157,325 | 0.28 | 0.45 | 0.00 | 1.00 |
| Stock Performance | 157,325 | 0.13 | 0.78 | −0.91 | 8.38 |
| Abnormal Return20 | 157,325 | 0.00 | 0.19 | −0.97 | 6.32 |
| EPS | 157,325 | 0.99 | 82.33 | −83.40 | 98.11 |
| Consecutive Revenue Growth Ratio | 157,325 | 0.22 | 0.20 | 0.00 | 0.89 |
Definition of variables: Sales are firms’ sales revenues; OCis a firm’s operating costs; Decis a dummy variable that equals to 1 if a firm’s current year sales are less than last year, and 0 otherwise; Break is an indicator variable for earnings decrease and is set to 1 if a firm’s current earnings are less than last year; Employee Intensity is the ratio of the number of employees to sales revenue; Asset Intensity is the ratio of total assets to sales revenue; Successive Decrease is an indicator variable that equals to 1 if a firm’s last year sales are greater than the year before last year, and 0 otherwise; Stock Performance is the raw stock return in the prior fiscal year; EPS is earnings per share.
***represents significance level of 0.01.
*, **, and *** represent significance levels of 0.10, 0.05, and 0.01, respectively.
calculate the abnormal stock returns (Abnormal Return) using Fama & French (1993) three-factor model. The results show that the average abnormal return of the string firms (0.04) is significantly higher than that of the non-string firms (0.01). For the string firms, the average abnormal return of the string years (0.10) is also significantly higher than that of the non-string years (0.01). Overall, our statistics regarding stock returns are consistent with those documented by Myers et al. (2007).
Panel C of
An examination of the data from the current study, which covers the period from 1973 to 2018, reveals that out of the 74,604 firm years exhibiting consecutive revenue growth over at least five years, only 20,162 firm years (27.03 percent) are associated with strings of increasing earnings. Furthermore, out of the 22,189 firm years associated with strings of increasing earnings, 6048 firm years (27.26 percent) are associated with strings of increasing earnings over periods with at least one revenue decrease. The above findings point out that a pattern of consecutive revenue growth, although clearly an important driver of strings of increasing earnings, is neither a sufficient condition nor a necessary condition for a firm to maintain a string of increasing earnings. That is, besides consecutive revenue growth, cost management obviously plays an important role in a firm’s ability to report strings of increasing earnings22. As already noted in the Introduction of this paper, Ghosh et al. (2005: p. 34) also point out that a large percentage (i.e. 33.33 percent) of strings in their study were the result of a cost-cutting strategy by firms23.
We computed a firm-level Consecutive Revenue Growth Ratio measure. This measure is calculated as the ratio of the number of years in consecutive revenue growth of five years or longer to the total number of years of observation for each firm. As shown in
We tested our second hypothesis (H2) by estimating Model (1) using the string firm sample and the non-string firm sample separately. The results are reported in Columns (1) and (2) of
| Independent Variables | (1) | (2) | (3) | (4) | (5) | |||||
|---|---|---|---|---|---|---|---|---|---|---|
| String firms | Non-string firms | String years of string firms | Non-string years of string firms | All firm years | ||||||
| Coef. (t-value) | Coef. (t-value) | Coef. (t-value) | Coef. (t-value) | Coef. (t-value) | ||||||
| Intercept | −0.007 | ** | 0.050 | *** | −0.013 | *** | −0.008 | * | 0.066 | *** |
| (−2.18) | (8.51) | (−5.11) | (−1.68) | (26.81) | ||||||
| ∆lnS | 0.905 | *** | 0.594 | *** | 0.990 | *** | 0.867 | *** | 0.646 | *** |
| (126.59) | (89.67) | (193.64) | (87.59) | (109.99) | ||||||
| Employee Intensity | 0.133 | *** | 0.467 | *** | 0.051 | * | 0.189 | *** | ||
| (3.70) | (3.78) | (1.93) | (2.83) | |||||||
| Asset Intensity | 0.010 | *** | 0.006 | *** | 0.004 | ** | 0.011 | *** | ||
| (6.47) | (10.78) | (2.36) | (6.15) | |||||||
| Successive Decrease | −0.018 | *** | −0.069 | *** | −0.001 | −0.021 | *** | |||
| (−10.49) | (−33.19) | (−0.44) | (−10.46) | |||||||
| Stock Performance | −0.028 | *** | −0.015 | *** | −0.016 | *** | −0.035 | *** | ||
| (−18.30) | (−10.84) | (−16.70) | (−15.41) | |||||||
| Industry Fixed Effects Included | Yes | Yes | Yes | Yes | Yes | |||||
| Adj-R2 | 0.75 | 0.42 | 0.92 | 0.66 | 0.46 | |||||
| N | 59,557 | 97,768 | 22,189 | 37,368 | 157,325 | |||||
| Number of firms | 2760 | 11,934 | 2760 | 2760 | 14,694 | |||||
Tests for Difference in Coefficients between Groups
Regression model: ln ( O C i , t O C i , t − 1 ) = β 0 + β 1 ln ( S a l e s i , t S a l e s i , t − 1 ) + ∑ s = 1 4 γ 1 , s E c o n V a r s , i , t + ε i , t . Δ ln S = ln ( S a l e s i , t S a l e s i , t − 1 ) . *, **, and *** represent significance levels of 0.10, 0.05, and 0.01, respectively. See Appendix B for variable definition. Source of data: All financial statement data and number of employees are obtained from Compustat. Stock price data are obtained from CRSP.
in sales would only lead to an average 0.594 percent change in operating costs. In other words, operating costs of the string firms are more sensitive to sales changes than operating costs of the non-string firms. This finding supports our second hypothesis (H2) that firms with strings have more cost flexibility than firms without strings.
For the string firms, we run Model (1) separately for the string years and the non-string years. The results are reported in Column (3) and Column (4) of
Before testing our third hypothesis (H3) regarding asymmetric cost behavior, we compute the regression results based on our full sample using the original Anderson et al. (2003) model. As shown in Column (5) of
We then estimate Model (2) using the string firm sample and the non-string firm sample separately. The results are reported in Columns (1) and (2) of
We formally test H3 by estimating Model (2) separately using the string years of the firms that experience at least one sales decrease during the strings and all non-string years of string firms26. The results are reported in Columns (3) and (4) of
| Independent Variables | (1) | (2) | (3) | (4) | (5) | |||||
|---|---|---|---|---|---|---|---|---|---|---|
| String firms | Non-string firms | String years of firms that experience sales decrease(s) during string periods | Non-string years of string firms | All firm years | ||||||
| Coef. (t-value) | Coef. (t-value) | Coef. (t-value) | Coef. (t-value) | Coef. (t-value) | ||||||
| Intercept | −0.013 | *** | 0.059 | *** | −0.009 | ** | −0.013 | ** | 0.053 | *** |
| (−3.58) | (10.10) | (−2.40) | (−2.24) | (20.30) | ||||||
| ∆lnS | 0.953 | *** | 0.595 | *** | 1.039 | *** | 0.888 | *** | 0.701 | *** |
| (99.88) | (61.18) | (123.95) | (54.08) | (91.43) | ||||||
| ∆lnS*Dec | −0.063 | −0.063 | *** | 0.213 | *** | −0.017 | −0.157 | *** | ||
| (−1.64) | (−3.66) | (4.71) | (−0.42) | (−14.00) | ||||||
| ∆lnS*Dec*Break | −0.238 | *** | −0.468 | *** | −0.566 | *** | −0.290 | *** | ||
| (−6.63) | (−15.64) | (−4.93) | (−6.59) | |||||||
| ∆lnS*Break | 0.200 | *** | 0.513 | *** | 0.244 | *** | 0.265 | *** | ||
| (10.67) | (35.00) | (2.97) | (10.54) | |||||||
| Break | 0.036 | *** | 0.030 | *** | 0.038 | *** | 0.036 | *** | ||
| (17.26) | (11.23) | (6.07) | (13.44) | |||||||
| Dec | −0.002 | −0.044 | *** | 0.001 | −0.005 | ** | ||||
| (−1.06) | (−17.02) | (0.53) | (−1.99) | |||||||
| ∆lnS*Dec* Employee Intensity | 0.182 | −2.706 | *** | −2.129 | * | −0.541 | ||||
| (0.15) | (−5.12) | (−1.72) | (−0.39) | |||||||
| ∆lnS*Dec* Asset Intensity | −0.043 | ** | −0.014 | *** | −0.050 | * | −0.037 | ** | ||
| (−2.52) | (−9.96) | (−1.87) | (−2.16) | |||||||
| ∆lnS*Dec* Successive Decrease | −0.036 | 0.041 | ** | −0.035 | −0.018 | |||||
| (−1.31) | (2.52) | (−0.58) | (−0.64) | |||||||
| ∆lnS*Dec* Stock Performance | 0.134 | *** | 0.013 | −0.059 | 0.117 | *** | ||||
| (6.32) | (1.53) | (−1.63) | (5.30) | |||||||
| Employee Intensity | 0.118 | *** | −0.132 | 0.059 | 0.139 | ** | ||||
| (3.30) | (−1.15) | (1.01) | (1.99) | |||||||
| Asset Intensity | 0.002 | 0.001 | −0.003 | 0.004 | * | |||||
| (1.20) | (1.50) | (−0.95) | (1.73) | |||||||
| Successive Decrease | −0.015 | *** | −0.050 | *** | 0.003 | −0.014 | *** | |||
| (−8.24) | (−22.60) | (1.43) | (−6.71) | |||||||
| Stock Performance | −0.019 | *** | −0.013 | *** | −0.009 | *** | −0.024 | *** | ||
| (−13.16) | (−9.87) | (−4.94) | (−11.26) | |||||||
| Industry Fixed Effects Included | Yes | Yes | Yes | Yes | ||||||
| Adj-R2 | 0.76 | 0.45 | 0.93 | 0.68 | 0.46 | |||||
| N | 59,557 | 97,768 | 6048 | 37,368 | 157,325 | |||||
| Number of firms | 2760 | 11,934 | 774 | 2760 | 14,694 | |||||
Regression model: ln ( O C i , t O C i , t − 1 ) = β 0 + β 1 ln ( S a l e s i , t S a l e s i , t − 1 ) + β 2 D e c i , t × ln ( S a l e s i , t S a l e s i , t − 1 ) + β 3 B r e a k i , t + β 4 ln ( S a l e s i , t S a l e s i , t − 1 ) × B r e a k i , t + β 5 D e c i , t + β 6 ln ( S a l e s i , t S a l e s i , t − 1 ) × D e c i , t × B r e a k i , t + ∑ s = 1 4 γ 1 , s × E c o n V a r s , i , t + ∑ s = 1 4 γ 2 , s ln ( S a l e s i , t S a l e s i , t − 1 ) × D e c i , t × E c o n V a r s , i , t + ε i , t . Δ ln S = ln ( S a l e s i , t S a l e s i , t − 1 ) . *, **, and *** represent significance levels of 0.10, 0.05, and 0.01, respectively. See Appendix B for variable definition. Source of data: All financial statement data and number of employees are obtained from Compustat. Stock price data are obtained from CRSP.
these firms during the string periods (i.e. costs decrease more rapidly when revenues decrease then they increase when revenues increase). For non-string years of all string firms, the coefficient of D e c i , t × ln ( S a l e s i , t S a l e s i , t − 1 ) is statistically insignificant (−0.017). The coefficients of ln ( S a l e s i , t S a l e s i , t − 1 ) × D e c i , t × B r e a k i , t are −0.566 for the string years of firms that experience at least one sales decrease during the string periods and −0.290 for the non-string years, which are both significant at the one percent level. These results are consistent with our expectation that costs of string firms become sticky when the strings end. As predicted in hypothesis H3, our findings show that, compared to non-string firms, the string firms that experience sales decreases during the string periods exhibit different asymmetric cost behavior, i.e. anti-sticky cost behavior during the string periods and sticky cost behavior when string ends.
To test our fourth hypothesis (H4), we calculate the average demand uncertainty for the string firms and the non-string firms. The results are reported in Column (1) and Column (2) of
| Variable | (1) | (2) | (1) vs (2) | (3) | (4) | (3) vs (4) | ||||
|---|---|---|---|---|---|---|---|---|---|---|
| String firms | Non-string firms | Difference in means | t-stat for difference in means | String years of string firms | Non-string years of string firms | Difference in means | t-stat for difference in means | |||
| Demand Uncertainty | 0.15 | 0.31 | −0.16 | −131.47 | *** | 0.13 | 0.16 | −0.03 | −28.29 | *** |
| N | 59,557 | 97,768 | 22,189 | 37,368 | ||||||
| Number of firms | 2760 | 11,934 | 2760 | 2760 | ||||||
Demand Uncertainty is the standard deviation of ln ( S a l e s i , t S a l e s i , t − 1 ) for the past five years. ***represents significance level of 0.01. Source of data: All financial statement data and number of employees are obtained from Compustat. Stock price data are obtained from CRSP.
In our sample, some firms managed to report more than one string of increasing earnings. In this subsection, we investigate whether higher cost flexibility and lower demand uncertainty contribute to more strings reported by the same firm. We begin by breaking our 2760 string firms into the following three groups: 1) 2051 firms that have reported only one string, 2) 520 firms that have reported two strings, and 3) 189 firms that have reported at least three strings. We then conduct our tests of cost flexibility for the three groups of string firms separately. The results from estimating Model (1) are reported in Panel A of
Our next step was to calculate the demand uncertainty for each group separately. The results of this analysis are presented in Panel B of
| Panel A: Number of Strings and Cost Flexibility | ||||||
|---|---|---|---|---|---|---|
| Independent Variables | Group (1) | Group (2) | Group (3) | |||
| Firms with one string | Firms with two strings | Firms with at least three strings | ||||
| Coef. (t-value) | Coef. (t-value) | Coef. (t-value) | ||||
| Intercept | −0.007 | * | −0.005 | −0.012 | ||
| (−1.86) | (−1.12) | (−1.18) | ||||
| ∆lnS | 0.889 | *** | 0.934 | *** | 0.995 | *** |
| (98.32) | (94.88) | (73.36) | ||||
| Control Variables Included | Yes | Yes | Yes | |||
| Industry Fixed Effects Included | Yes | Yes | Yes | |||
| Adj-R2 | 0.72 | 0.80 | 0.84 | |||
| N | 37,374 | 15,079 | 7104 | |||
| Number of firms | 2051 | 520 | 189 | |||
Tests for Difference in Coefficients between Groups
Regression model: ln ( O C i , t O C i , t − 1 ) = β 0 + β 1 ln ( S a l e s i , t S a l e s i , t − 1 ) + ∑ s = 1 4 γ 1 , s E c o n V a r s , i , t + ε i , t . Δ ln S = ln ( S a l e s i , t S a l e s i , t − 1 ) .
*, **, and *** represent significance levels of 0.10, 0.05, and 0.01, respectively. See Appendix B for variable definition. Source of data: All financial statement data and number of employees are obtained from Compustat. Stock price data are obtained from CRSP.
Strings of increasing earnings vary significantly in length27. Thus, we examine whether higher cost flexibility and lower demand uncertainty contribute to the length of the strings. We group the strings based on their length into the following three groups: 1) 2857 strings that are shorter than 10 years, 2) 359 strings that are 10 to 20 years long, and 3) 43 strings that lasted longer than 20 years.
As noted earlier and shown in Panel B of
driving factor of strings of increasing earnings. The above notwithstanding, there may be some differences in cost flexibility and demand uncertainty among industries. Thus, to examine this issue more closely, we calculate measures for cost flexibility and demand uncertainty at the industry level (see
For all industries, the differences in average cost flexibility between the string firms and the industry are positive. The differences in average cost flexibility between the non-string firms and the industry are negative across all industries. These results show that the degree of cost flexibility for string firms (non-string firms) is higher (lower) than the industry average. For all industries, the differences in average demand uncertainty between the string firms and the industry are negative. Similarly, the differences in average demand uncertainty between the non-string firms and the industry are positive across all industries. In other words, the average demand uncertainty for string firms (non-string firms) is always lower (higher) than the industry average. In addition, the differences between the string firms and the non-string firms are all significant at the one percent level for both cost flexibility and demand uncertainty. Hence, these results regarding cost flexibility and demand uncertainty show that our findings persist after controlling for industry factors.
As noted in the descriptive statistics section and shown in
The cost flexibility for string firms (non-string firms) in the big firm group is 0.93 (0.83), and the cost flexibility for string firms (non-string firms) in the small firm group is 0.84 (0.56). The differences in cost flexibility for string firms versus non-string firms are significant at the one percent level for both the big firm
| Panel A: Industry Average Level of Cost Flexibility and Demand Uncertainty | |||
|---|---|---|---|
| Industry | Concentration of string firms | Cost flexibility (β1) | Demand uncertainty |
| Consumer Durables | 27.55% | 0.78 | 0.2 |
| Wholesale, Retail, and Some Services | 27.03% | 0.89 | 0.17 |
| Consumer NonDurables | 25.84% | 0.86 | 0.17 |
| Manufacturing | 25.01% | 0.81 | 0.21 |
| Chemicals and Allied Products | 24.74% | 0.72 | 0.2 |
| Other | 17.51% | 0.75 | 0.26 |
| Telephone and Television Transmission | 16.45% | 0.85 | 0.22 |
| Business Equipment | 13.54% | 0.69 | 0.28 |
| Oil, Gas, and Coal Extraction and Products | 13.48% | 0.71 | 0.37 |
| Healthcare, Medical Equipment, and Drugs | 11.99% | 0.58 | 0.38 |
| Panel B: Industry Adjusted Cost Flexibility and Demand Uncertainty | ||||||||
|---|---|---|---|---|---|---|---|---|
| Industry adjusted cost flexibility (β1)† | Industry adjusted demand uncertainty† | |||||||
| Industry | String firms | Non- string firms | Difference | String firms | Non- string firms | Difference | ||
| Consumer Durables | 0.17 | −0.03 | 0.20 | *** | −0.05 | 0.05 | −0.10 | *** |
| Wholesale, Retail, and Some Services | 0.08 | −0.03 | 0.11 | *** | −0.05 | 0.05 | −0.10 | *** |
| Consumer NonDurables | 0.13 | −0.03 | 0.17 | *** | −0.05 | 0.05 | −0.10 | *** |
| Manufacturing | 0.12 | −0.04 | 0.16 | *** | −0.05 | 0.04 | −0.10 | *** |
| Chemicals and Allied Products | 0.22 | −0.04 | 0.26 | *** | −0.07 | 0.06 | −0.13 | *** |
| Other | 0.20 | −0.04 | 0.24 | *** | −0.10 | 0.05 | −0.15 | *** |
| Telephone and Television Transmission | 0.19 | −0.01 | 0.20 | *** | −0.07 | 0.04 | −0.11 | *** |
| Business Equipment | 0.20 | −0.04 | 0.24 | *** | −0.10 | 0.04 | −0.14 | *** |
| Oil, Gas, and Coal Extraction and Products | 0.13 | −0.02 | 0.14 | *** | −0.12 | 0.06 | −0.18 | *** |
| Healthcare, Medical Equipment, and Drugs | 0.43 | −0.03 | 0.45 | *** | −0.20 | 0.07 | −0.28 | *** |
***represents significance level of 0.01. †Industry adjusted cost flexibility of the string firms is calculated as the difference between the average cost flexibility of the string firms in an industry and the average cost flexibility of all firms in the industry. A similar definition of industry adjusted cost flexibility applies for the non-string firms. In a similar manner, we calculate the industry adjusted demand uncertainty for the string firms and the non-string firms. Source of data: All financial statement data and number of employees are obtained from Compustat. Stock price data are obtained from CRSP.
| Variables | Big Firms (Firms with SIZE above sample medium) | Small Firms (Firms with SIZE below sample medium) | |||||||||
|---|---|---|---|---|---|---|---|---|---|---|---|
| String firms | Non-string firms | Difference in means | t-stat for Difference in means | String firms | Non-string firms | Difference in means | t-stat for Difference in means | ||||
| Cost Flexibility | 0.93 | 0.83 | 0.10 | 5.88 | *** | 0.84 | 0.56 | 0.28 | 8.03 | *** | |
| Demand Uncertainty | 0.14 | 0.24 | −0.10 | −73.93 | *** | 0.19 | 0.39 | −0.20 | −72.82 | *** | |
| N | 51,140 | 50,839 | 8417 | 46,929 | |||||||
| Number of Firms | 2175 | 5172 | 585 | 6762 | |||||||
SIZE is calculated as GDP-adjusted average sales for each firm, assuming 1973 as the base year for GDP adjustment. ***represents significance level of 0.01. Source of data: All financial statement data and number of employees are obtained from Compustat. Stock price data are obtained from CRSP.
group and the small firm group. Similarly, the demand uncertainty for string firms (non-string firms) in the big firm group is 0.14 (0.24), and the demand uncertainty for string firms (non-string firms) in the small firm group is 0.19 (0.39). The differences in demand uncertainty for string firms versus non-string firms are significant at the one percent level for both the big firm group and the small firm group. Thus, our results regarding cost flexibility and demand uncertainty persist after controlling for size.
Balakrishnan et al. (2014) argue that the logarithm specification introduces a bias towards sticky cost behavior. Accordingly, they suggest using a percentage change model to mitigate the bias30. Since we anticipate anti-sticky cost behavior for the string firm years, the bias towards sticky cost behavior introduced by the log-linear model lowers the sensitivity of our tests. That is, any anti-sticky cost behavior results found from using the log-linear model are, in fact, weakened by the log-linear model specification. Nonetheless, running the percentage change model provides an opportunity to examine our second and third hypotheses using an alternative model setting. Therefore, we test our hypotheses again using the percentage change models, formally stated as Model (3) and Model (4) below:
Δ O C i , t O C i , t − 1 = β 0 + β 1 Δ S a l e s i , t S a l e s i , t − 1 + ∑ s = 1 4 γ 1 , s × E c o n V a r s , i , t + ε i , t , (3)
and
Δ O C i , t O C i , t − 1 = β 0 + β 1 Δ S a l e s i , t S a l e s i , t − 1 + β 2 D e c i , t × Δ S a l e s i , t S a l e s i , t − 1 + β 3 D e c i , t × Δ S a l e s i , t S a l e s i , t − 1 × B r e a k i , t + β 4 Δ S a l e s i , t S a l e s i , t − 1 × B r e a k i , t + β 5 B r e a k i , t + β 6 D e c i , t + ∑ s = 1 4 γ 1 , s × E c o n V a r s , i , t + ∑ s = 1 4 γ 2 , s D e c i , t × Δ S a l e s i , t S a l e s i , t − 1 × E c o n V a r s , i , t + ε i , t , (4)
where ∆OCi is the difference between OCi,t and OCi,t−1; ∆Salesi,t is the difference between Salesi,t and Salesi,t−1; and all other variables are as previously defined. All prior predictions apply on the estimated coefficients from Model (3) and Model (4).
The results based on Model (3) are summarized in Panel A of
The results based on Model (4) are reported in Panel B of
For the string years of the string firms that experience at least one sales decrease during the string periods, the coefficient of D e c i , t × Δ S a l e s i , t S a l e s i , t − 1 is significantly positive (0.240) at the one percent level. This result shows that costs of these firms during the string years are anti-sticky, which supports our hypothesis H3. The coefficient of D e c i , t × Δ S a l e s i , t S a l e s i , t − 1 × B r e a k i , t is significantly negative (−0.410)
| Panel A: Strings and Cost Flexibility | ||||||||
|---|---|---|---|---|---|---|---|---|
| Independent Variables | (1) | (2) | (3) | (4) | ||||
| String firms | Non-string firms | String years of string firms | Non-string years of string firms | |||||
| Coef. (t-value) | Coef. (t-value) | Coef. (t-value) | Coef. (t-value) | |||||
| Intercept | −0.012 | * | 0.078 | *** | −0.019 | *** | −0.012 | |
| (−1.87) | (7.50) | (−3.50) | (−1.24) | |||||
| ΔS | 0.937 | *** | 0.539 | *** | 1.036 | *** | 0.885 | *** |
| (56.91) | (43.02) | (128.39) | (34.82) | |||||
| Employee Intensity | 0.148 | * | 0.053 | 0.061 | 0.185 | |||
| (1.83) | (0.22) | (1.54) | (1.22) | |||||
| Asset Intensity | 0.020 | *** | 0.009 | *** | 0.009 | ** | 0.024 | *** |
| (5.41) | (8.46) | (2.42) | (5.09) | |||||
| Successive Decrease | −0.014 | *** | −0.078 | *** | 0.005 | −0.019 | *** | |
| (−5.05) | (−20.74) | (1.39) | (−6.04) | |||||
| Stock Performance | −0.031 | *** | −0.012 | *** | −0.023 | *** | −0.035 | *** |
| (−10.72) | (−4.70) | (−13.62) | (−8.24) | |||||
| Industry Fixed Effect Included | Yes | Yes | Yes | Yes | ||||
| Adj-R2 | 0.66 | 0.31 | 0.87 | 0.55 | ||||
| N | 59,557 | 97,768 | 22,189 | 37,368 | ||||
| Number of firms | 2760 | 11,934 | 2760 | 2760 | ||||
Tests for Difference in Coefficients between Groups
Regression model: Δ O C i , t O C i , t − 1 = β 0 + β 1 Δ S a l e s i , t S a l e s i , t − 1 + ∑ s = 1 4 γ 1 , s E c o n V a r s , i , t + ε i , t . Δ S = Δ S a l e s i , t S a l e s i , t − 1 . *, **, and *** represent significance levels of 0.10, 0.05, and 0.01, respectively. See Appendix B for other variable definition. Source of data: All financial statement data and number of employees are obtained from Compustat. Stock price data are obtained from CRSP.
Regression model: Δ O C i , t O C i , t − 1 = β 0 + β 1 Δ S a l e s i , t S a l e s i , t − 1 + β 2 D e c i , t × Δ S a l e s i , t S a l e s i , t − 1 + β 3 D e c i , t × Δ S a l e s i , t S a l e s i , t − 1 × B r e a k i , t + β 4 Δ S a l e s i , t S a l e s i , t − 1 × B r e a k i , t + β 5 B r e a k i , t + β 6 D e c i , t + ∑ s = 1 4 γ 1 , s × E c o n V a r s , i , t + ∑ s = 1 4 γ 2 , s D e c i , t × Δ S a l e s i , t S a l e s i , t − 1 × E c o n V a r s , i , t + ε i , t . Δ S = Δ S a l e s i , t S a l e s i , t − 1 . *, **, and *** represent significance levels of 0.10, 0.05, and 0.01, respectively. See Appendix B for other variable definition. All financial statement data and number of employees are obtained from Compustat. Stock price data are obtained from CRSP.
at the one percent level, indicating that costs of these firms become sticky once the string ends. The above results are in line with those from Model (2). Hence, our findings from the percentage change model are supportive of the third hypothesis (H3).
Macro-economic factors such as GDP growth may also contribute to the occurrence of strings of increasing earnings. Thus, to understand the extent to which macro-economic factors affect the occurrence of the strings in our study, we plot the number of ongoing strings and US GDP growth over our entire sample period (see
We further examine if GDP growth contributes to the ending of strings, by plotting the number of strings ended and GDP growth from 1978 to 201831. The results of regressing number of strings ended on GDP growth are also reported in
the one level. Our result indicates that GDP growth is negatively associated with the ending of strings of increasing earnings. Thus, it appears, as one would expect, that it is more difficult for firms to show increases in earnings when the economy is declining33. Overall, our tests suggest that GDP growth does not seem to contribute to the occurrence of strings.
Firms that maintain a string of consecutive increasing earnings over five years or more tend to have significantly higher P/E ratios and higher abnormal stock market returns compared to firms not generating such strings. Consequently, firms have a strong incentive to achieve a string of consecutive increasing earnings over five years or more.
Although consecutive revenue growth plays an important role in generating consecutive increasing earnings, the current study shows that cost management can play a proactive role in a firm’s ability to sustain a consecutive string of increasing earnings. In fact, the current study finds that over 27% of the increasing earnings strings include at least one period where sales were decreasing. These findings are consistent with other studies that have looked at this issue (e.g. Ghosh et al., 2005).
The above noted findings raise the following question: Are there specific factors associated with firms that successfully use cost management techniques to sustain a string of consecutive increasing earnings? As shown in the current study, one key factor facilitating such cost management is the degree to which a firm has cost flexibility, where cost flexibility refers to the ratio of a firm’s discretionary costs relative to its non-discretionary costs. More to the point, when compared to firms that were not able to maintain a string of increasing earnings over periods of five years or longer, firms with strings have a lower level of non-discretionary costs relative to discretionary costs. In addition, for strings that included at least one sales decrease, the string firms were able to aggressively practice what has become known in the literature as anti-sticky costing. These findings suggest that the conventional wisdom espoused in most textbooks concerning a firm’s desirability of taking on more fixed costs relative to variable costs during periods of high product demand needs to be modified to consider a firm’s motivation to sustain a string of consecutive increasing earnings over a period of five years or more. In other words, the additional fixed costs may increase profits in the short run but lower a firm’s ability to maintain a consecutive string of increasing earnings over a period of five years or longer due to the reduction in cost flexibility.
The current study also found that lower demand uncertainty facilitates the ability of a firm to sustain strings of increasing earnings. That is, lower demand uncertainty places a firm in a better position to plan for, and strategically manage, future costs. Indeed, part of the cost management process could include the hoarding of resources for a “rainy day” (i.e. firms with more certainty of demand for their products can essentially plan for, and manage, anticipated downturns in revenues). In other words, cost management and revenue management are related activities that do not have to be thought of as pejorative activities34. In fact, we agree with Ittner & Aguilar (2019), when he noted that “It’s about managing cost structures in conjunction with revenue growth and in conjunction with changing the product and service offerings”35. Thus, managers in firms motivated to achieve strings of increasing earnings over periods of five years or longer may wish to focus on products with highly predictable sales or on diversifying their product lines as a means of reducing overall sales fluctuations.
The findings from the current study also have capital market implications. The identification of firms with high-cost flexibility and low demand uncertainty could assist investors and analysts in predicting which firms are likely to maintain strings of consecutive increasing earnings in the future. Indeed, investors and analysts could develop and test models for predicting firms that are likely to have strings of increasing earnings based not only on revenue growth, but on the cost flexibility and demand uncertainty of firms. Given the vast amount of publicly available data on costs and product demand for firms, developing predictive models for identifying firms that are likely to have increasing earnings strings would be an excellent candidate for machine learning techniques.
The findings from the current study also show that firms with strings that experience at least one sales decrease during the string periods are associated with anti-sticky cost behavior during the string period, and sticky cost behavior once the string ends. These findings make it clear that managers adjust costs differently when trying to maintain a string of increasing earnings than during non-string periods. Although anti-sticky cost behavior has been identified in a variety of settings (e.g. see Banker & Byzalov, 2014), our findings provide empirical evidence of such behavior in a setting not previously examined. Investors should, however, be cautious when investing in a firm with consecutive increasing earnings in which reductions in costs appear to be a dominant factor driving the increasing earnings (i.e. a cost-cutting strategy that will ultimately become unsustainable for a firm).
Prior studies found that firms maintaining strings of increasing earnings, compared to firms without such strings, are associated with higher price-earnings (P/E) ratios and receive abnormal stock market returns during the string periods. Thus, firms have an incentive to maintain strings of increasing earnings. Investors also have an incentive to better understand the way firms can achieve strings of increasing earnings.
Strings of increasing earnings result from consecutive revenue growth and/or cost management. Although revenue growth is an important driver of strings, we observe that having a pattern of consecutive revenue growth is neither necessary nor sufficient to maintain a string of increasing earnings. Indeed, cost management can play a proactive role in maintaining strings. This fact notwithstanding, little is known about the way firms manage costs to facilitate strings. To fill this void, the primary objective of the current study is to improve our understanding of how firms successfully manage their costs to facilitate maintaining a consecutive string of increasing earnings, especially during periods that include decreasing revenues (i.e. periods when consecutive revenue growth is clearly not the driver of a string of increasing earnings).
The findings from our study show that firms with strings of increasing earnings have higher cost flexibility compared to firms without such strings. Furthermore, our results show that the string firms experiencing at least one sales decrease during the string periods exhibit anti-sticky cost behavior during the string periods. Once the string ends, however, the costs of firms with strings over a period of declining sales become sticky. Taken together, the findings from the current study show that firms with strings, in contrast to firms without such strings, tend to commit to less non-discretionary costs and use management discretion in cost adjustment decisions to sustain strings of increasing earnings. In addition, we find that string firms are associated with lower demand uncertainty relative to firms without a string. This latter finding indicates that lower demand uncertainty facilitates a firm’s ability to sustain a string of increasing earnings through improved cost planning.
As with all empirical studies, the one discussed in this paper has its limitations. One limitation is the lack of a stable measure of cost flexibility over multiple time periods. Another limitation is that our results are based on cross-sectional regressions that do not easily map to the cost management of individual firms. These limitations notwithstanding, we believe the findings from the current study further our understanding of the factors that contribute to the ability of firms to maintain a string.
We thank Shijun Cheng, Yi Cao, Juan Castillo, Jin Kyung Choi, Sebahattin Demirkan, Augustine Duru, Ruyun Feng, Charles Ham, Cody Hyman, Congcong Li, Laurel Mazur, Linda Myers, Ariel Rava, Noami Soderstrom, Tashfeen Sohail, Gerald Ward, and Lu Yan for their valuable comments on this paper. All remaining errors are our own.
Data are available from the public sources cited in the text.
The authors declare no conflicts of interest regarding the publication of this paper.
Tseng, C.-Y., Zhou, L., Gordon, L. A., & Loeb, M. P. (2022). Cost Management and Strings of Increasing Earnings. Open Journal of Accounting, 11, 243-282. https://doi.org/10.4236/ojacct.2022.114013
Using our sample consisting of firm years from 1973 to 2018, we examine the market performance of firms experiencing strings of increasing earnings.36 Following Barth et al. (1999): we estimate Models (A1) and (A2) below:
P r i c e i t = a 0 + ∑ y r = 1974 2018 a 0 , y r D y r , i t + a 1 N I i t + ∑ y r = 1974 2018 a 1 , y r ( D y r , i t × N I i t ) + a 1 , u p D u p , i t × N I i t + a 2 G r o w t h i t × N I i t + a 3 E V A R i t × N I i t + a 4 D E i t × N I i t + a 5 B V E i t + ε i t , (A1)
P r i c e i t = a 0 + ∑ y r = 1974 2018 a 0 , y r D y r , i t + a 1 N I i t + ∑ y r = 1974 2018 a 1 , y r ( D y r , i t × N I i t ) + ∑ N = 1 9 a 1 , u p , N ( D u p , N , i t × N I i t ) + a 2 G r o w t h i t × N I i t + a 3 E V A R i t × N I i t + a 4 D E i t × N I i t + a 5 B V E i t + ε i t , (A2)
where
Price = fiscal year-end share price;
NI =net income per share before extraordinary items and discontinued operations;
D = indicator dummy variables for years (Dyr): firm with at least five consecutive years of increasing earnings including yeart (Dup): or firm with N consecutive years of increasing earnings (Dup,N);
Growth = five-year compound annual growth rate of book value of equity, i.e. ( B V E t / B V E t − 6 ) 1 / 5 − 1 ;
EVAR = variance of past six years’ percentage change in earnings ( N I t − N I t − 1 ) / a b s / N I t − 1 / ;
BVE = book value of equity per share.
Model (A1) tests if firms with strings of increasing earnings outperform firms without such strings. The results are summarized in TableA1. Consistent with Barth et al. (1999): our coefficient on D y r , i t × N I i t is significantly positive (3.170), suggesting that the P/E ratios are higher for firms with strings than for firms without strings. Model (A2) examines whether the earnings multiples change with the length of the string. As shown in TableA1, the coefficients for D u p , N , i t represent the excess P/E ratios for firms in the Nth year of the string. All coefficients are statistically significant. The estimates are 1.067, 2.016, 2.049, 2.744 and 3.556 for N = 1 , 2 , 3 , 4 , 5 , respectively. The results show that the P/E ratios are monotonically increasing in the number of years a firm has been maintaining the strings, i.e. the longer the string, the higher the excess P/E ratio the stock market awards the firm.
In order to examine how the P/E ratio change when a string of increasing earnings ends, we modify Model (A2) by adding a dummy variable Break for the year the string of increasing earnings ends, formally stated as (A3) below:
| Independent Variables | Model (A1) | Model (A2) | Model (A3) | |||||||
|---|---|---|---|---|---|---|---|---|---|---|
| Coefficient | t-Stat | Coefficient | t-Stat | Coefficient | t-Stat | |||||
| Intercept | 10.089 | *** | 91.55 | 9.770 | *** | 89.32 | 9.459 | *** | 86.90 | |
| NI | 5.064 | *** | 101.59 | 4.219 | *** | 79.25 | 3.135 | *** | 53.93 | |
| Dup × NI | 3.170 | *** | 71.99 | |||||||
| Dup,1 × NI | 1.067 | *** | 16.04 | 2.423 | *** | 33.37 | ||||
| Dup,2 × NI | 2.016 | *** | 31.21 | 3.376 | *** | 47.57 | ||||
| Dup,3 × NI | 2.049 | *** | 30.63 | 3.422 | *** | 46.79 | ||||
| Dup,4 × NI | 2.744 | *** | 39.87 | 4.125 | *** | 55.03 | ||||
| Dup,5 × NI | 3.556 | *** | 43.32 | 4.941 | *** | 56.68 | ||||
| Dup,6 × NI | 3.901 | *** | 43.66 | 5.265 | *** | 56.14 | ||||
| Dup,7 × NI | 4.478 | *** | 38.75 | 5.834 | *** | 49.16 | ||||
| Dup,8 × NI | 3.623 | *** | 28.60 | 4.993 | *** | 38.57 | ||||
| Dup,9 × NI | 5.173 | *** | 72.32 | 6.548 | *** | 84.63 | ||||
| Break × NI | 2.760 | *** | 44.85 | |||||||
| GROWTH × NI | 0.346 | *** | 5.42 | −0.037 | −0.58 | −0.374 | *** | −5.84 | ||
| EVAR × NI | −0.001 | *** | −16.78 | −0.001 | *** | −14.68 | −0.001 | *** | −11.78 | |
| DE × NI | −0.072 | *** | −12 | −0.051 | *** | −8.48 | −0.032 | *** | −5.44 | |
| BVE | 0.813 | *** | 181.45 | 0.792 | *** | 177.05 | 0.760 | *** | 168.85 | |
| N | 143,249 | 143,249 | 143,249 | |||||||
| Adj. R2 | 0.55 | 0.55 | 0.56 | |||||||
| F-Statistic | 2100.75*** | 1980.95*** | 2008.79*** | |||||||
| p-value | (<0.0001) | (<0.0001) | (<0.0001) | |||||||
Regression model: Model (A1): P r i c e i t = a 0 + ∑ y r = 1974 2018 a 0 , y r D y r , i t + a 1 N I i t + ∑ y r = 1974 2018 a 1 , y r ( D y r , i t × N I i t ) + a 1 , u p D u p , i t × N I i t + a 2 G r o w t h i t × N I i t + a 3 E V A R i t × N I i t + a 4 D E i t × N I i t + a 5 B V E i t + ε i t ; Model (A2): P r i c e i t = a 0 + ∑ y r = 1974 2018 a 0 , y r D y r , i t + a 1 N I i t + ∑ y r = 1974 2018 a 1 , y r ( D y r , i t × N I i t ) + ∑ N = 1 9 a 1 , u p , N ( D u p , N , i t × N I i t ) + a 2 G r o w t h i t × N I i t + a 3 E V A R i t × N I i t + a 4 D E i t × N I i t + a 5 B V E i t + ε i t ; Model (A3): P r i c e i t = a 0 + ∑ y r = 1974 2018 a 0 , y r D y r , i t + a 1 N I i t + ∑ y r = 1974 2018 a 1 , y r ( D y r , i t × N I i t ) + ∑ N = 1 9 a 1 , u p , N ( D u p , N , i t × N I i t ) + a 2 B r e a k i t × N I i t + a 3 G r o w t h i t × N I i t + a 4 E V A R i t × N I i t + a 5 D E i t × N I i t + a 6 B V E i t + ε i t . Definition of variables: Price is the fiscal year-end share price; NI is net income per share before extraordinary items and discontinued operations; D represents indicator dummy variables for years (Dyr): firm with at least five consecutive years of increasing earnings including yeart (Dup): or firm with N consecutive years of increasing earnings (Dup,N); Growth is the five-year compound annual growth rate of book value of equity, i.e. ( B V E t / B V E t − 6 ) 1 / 5 − 1 ; EVAR is the variance of past six years’ percentage change in earnings, i.e. ( N I t − N I t − 1 ) / a b s ( N I t − 1 ) ; BVE is the book value of equity per share; and Break is a dummy variable that takes value of 1 for the year when earnings decrease, and 0 otherwise. ***represents significance level of 0.01. Source of data: All financial statement data are obtained from Compustat. Stock price data are obtained from CRSP.
P r i c e i t = a 0 + ∑ y r = 1974 2018 a 0 , y r D y r , i t + a 1 N I i t + ∑ y r = 1974 2018 a 1 , y r ( D y r , i t × N I i t ) + ∑ N = 1 9 a 1 , u p , N ( D u p , N , i t × N I i t ) + a 2 B r e a k i t × N I i t + a 3 G r o w t h i t × N I i t + a 4 E V A R i t × N I i t + a 5 D E i t × N I i t + a 6 B V E i t + ε i t , (A3)
where B r e a k i t is a dummy variable that takes value of 1 for the year when earnings decrease, and 0 otherwise.
The results based on Model (A3) are also shown in TableA1. The excess P/E ratios of the first five years of the string are 2.423, 3.376, 3.422, 4.125 and 4.941, all statistically significant. The P/E ratios are again monotonically increasing as the string gets longer. When the string ends, the excess P/E ratio declines to 2.760, suggesting the market reacts to the end of strings of increasing earnings by reducing the firm’s P/E ratio.
Source of data: All financial statement data and number of employees are obtained from Compustat. Stock price data are obtained from CRSP.