Finance and Economics Discussion Series: 2008-14 Screen Reader version ^{♣}

Keywords: Adjustment costs, learning, young firms

Abstract:

We propose an explanation for the rapid post-entry growth of surviving firms found in recent studies. At the core of our theory is the interaction between adjustment costs and learning by entering firms about their efficiency. We show that linear adjustment costs, i.e., proportional costs, create
incentives for firms to enter smaller and for successful firms to grow faster after entry. Initial uncertainty about profitability makes entering firms prudent since they want to avoid incurring superfluous costs on jobs that prove to be excessive ex post. Because higher
adjustment costs imply less pruning of inefficient firms and faster growth of surviving firms, the contribution of survivors to growth in a cohort's average size increases. For the cohort of 1988 entrants in the Portuguese economy, we conclude that survivors' growth is the main factor behind growth
in the cohort's average size. However, initial selection is higher and the survivors' contribution to growth is smaller in services than in manufacturing. An estimation of the model shows that the proportional adjustment cost is the key parameter to account for the high empirical survivors'
contribution. In addition, firms in manufacturing learn relatively less initially about their efficiency and are subject to larger adjustment costs than firms in services.

JEL Classification: E24, L11, L16

In recent years there has been renewed interest in explaining patterns of firm dynamics, with new longitudinal datasets confirming heterogeneities between firms of different size and age. In particular, small and young (surviving) firms tend to grow faster and have higher failure rates than
large and old firms, so that job destruction due to plant exit and job creation due to the scaling-up of firm size decrease with age.^{2} Moreover, entering
plants tend to be small, but survivors grow rapidly after entry and are the main factor behind the shift to the right of a cohort's size distribution.^{3} These
patterns differ significantly across countries and sectors, suggesting that technological differences are important, but that country specific factors also matter.^{4}

This paper proposes an explanation for the leading role of survivors' growth in post-entry firm dynamics based on the interaction between adjustment costs and a learning-about-efficiency mechanism. Following a literature that uses adjustment costs to account for some dynamic properties of firms' labor demand, such as Campbell and Fisher (2000), we show that adjustment costs can impact the lifetime dynamics of firms' labor demand in a way consistent with the data. To implement our theory, we use a standard model of firm dynamics with passive learning. In order to check the empirical fit of our model, we also assume that inefficient firms are pruned from the market, although the predictions of our theory hold even in the absence of a selection mechanism (e.g. when exit is not allowed).

Our contribution is twofold. First, we contribute to the empirical literature by introducing a decomposition of the change in a cohort's average size into a survivor component and a non-survivor component. Given the emphasis on survivors' growth, our measure allows a quick assessment of how well
a particular theory matches the data in that respect. We apply our decomposition to the 1988 cohort of entrants in the Portuguese economy, using the *Quadros de Pessoal* dataset. Similarly to Cabral and Mata (2003), we find that growth
of survivors is the main force behind the change in the cohort's average firm size. However, we also find that growth of survivors is especially intense in the initial years after entry and that there are significant cross-sector differences in terms of our decomposition. In particular, initial
exit rates are smaller and the survivors' contribution to changes in size is higher in manufacturing than in services.

Second, we contribute to the theoretical literature by introducing linear adjustment costs into a model of Bayesian learning about efficiency. Our assumption of linear or proportional costs is justified by the finding of high inaction rates in employment adjustment, in varying degrees across sectors. Our model builds on Jovanovic (1982) by adding proportional costs that apply not only to regular labor adjustment, but also to job creation at entry and job destruction at exit. We show that proportional adjustment costs create incentives for firms to start smaller and, if successful, grow faster after entry. We prove this analytically in a simplified model in which there is no exit of firms. This result shows that proportional costs can generate firm growth without selection. When firms are allowed to exit, selection intensifies the effects of adjustment costs on firm growth, while costs to adjustment reduce exit rates. Therefore, adjustment costs increase the contribution of surviving firms to growth in the cohort's average size.

All that is needed for firm growth under linear adjustment costs is the existence of a learning environment that generates a stochastic process for perceived efficiency with both persistence and decreasing uncertainty in age.^{5} The intuition for why firms grow faster and display smaller exit rates under proportional adjustment costs is that initial uncertainty about true profitability makes entering firms prudent; that is, they enter small and "wait
and see" since they want to avoid incurring superfluous entering/hiring costs and firing/shutdown costs on jobs that prove to be excessive ex post. This implies that surviving firms will grow faster, even though adjustment costs imply that there are fewer firms exiting the market and therefore
less pruning of inefficient firms.

The assumption that entering firms face a Bayesian learning problem concerning their efficiency is standard in selection theories and has been advanced as an explanation for the high rates of exit, job creation, and job destruction among young firms. The initial literature on adjustment costs
used a (strictly) convex specification in an attempt to explain the sluggishness in input responses to aggregate shocks. However, the assumption that costs of adjustment are linear is now standard in dynamic labor demand models, following a number of studies since the late 1980s that have
documented the importance of inaction in employment adjustment at the micro level.^{6} Since strictly convex costs imply smooth adjustments over time, whereas
linear costs imply immediate adjustment when it occurs, allowing for strictly convex costs, instead of linear costs, in the context where they also apply at entry and exit, would bias our analysis and eventually make our argument stronger. In the case of hiring/entering costs, entering firms would
prefer to start smaller and adjust gradually to their optimal size, even if their perceived productivity remained unchanged or learning was absent. For firing/exiting costs, firms experiencing large declines in perceived productivity would adjust downwards in several steps, a scenario that would
make firms start smaller to attenuate its effects. Therefore, by avoiding a bias towards firm growth, our decision to assume linear costs is conservative and permits a simplification of the methods employed to measure the effects of adjustment costs.^{7}

To assess our model quantitatively, we calibrate and estimate a version of the model with finite learning horizon and positive dispersion in entry size. We conclude that linear costs are the key element to account for the high empirical contribution of survivors to changes in a cohort's average size. A calibration/estimation for the manufacturing and services cohorts also suggests that firms in manufacturing learn relatively less initially about their efficiency and are subject to substantially larger adjustment costs than firms in services.

This paper is related to the literature on both adjustment costs and firm dynamics. Within the literature on adjustment costs, the paper is associated with theories that use linear adjustment costs to explain certain aspects of the dynamic behavior of labor demand and job flows. Well-known
examples are Bentolila and Bertola (1990), Hopenhayn and Rogerson (1993), and Campbell and Fisher (2000). Bentolila and Bertola
(1990) and Hopenhayn and Rogerson (1993) analyze the effects of proportional firing (and hiring) costs on the dynamics of hiring and firing decisions, and on average labor demand. Both papers conclude that high firing costs make hiring and firing
adjustments more sluggish, but they disagree on the implications of that for long-run employment. Campbell and Fisher (2000) use proportional costs of job creation and job destruction to explain the higher aggregate volatility of job destruction found in the
U.S. manufacturing sector. These costs imply that in reaction to aggregate wage shocks employment changes at contracting firms are larger than employment changes at expanding firms. What is new in our paper is the assumption that adjustment costs apply equally to the entry/exit decisions and the
hiring/firing decisions.^{8}

Within the literature on firm dynamics the paper is connected with theories that attempt to explain the stylized facts on the lifecycle dynamics outlined above. The two main explanations for these facts are theories based on selection of firms and theories based on financing constraints.^{9} Selection theories stress the tendency for firms that accumulate bad realizations of productivity to exit the market and for firms that accumulate good realizations
to survive and expand. This implies a composition bias towards larger and more efficient firms as smaller, inefficient, and slow-growing firms gradually exit the industry. Representative papers of selection theories are Jovanovic (1982), Hopenhayn (1992), Ericson and Pakes (1995), and Luttmer (2007). In all cases productivity realizations are exogenous, except in Ericson and Pakes (1995) where they are to
some extent endogenous.

Meanwhile, theories employing financing constraints argue that some imperfection in financial markets causes young firms to have limited access to credit, forcing them to enter at a suboptimally small scale. As firms get older and survive, they establish creditworthiness and build up internal resources that enable them to expand to their optimal size. Important contributions to this literature are those of Cooley and Quadrini (2001), Albuquerque and Hopenhayn (2004), and Clementi and Hopenhayn (2006). In Cooley and Quadrini (2001) a transaction cost on equity and a default cost on debt imply that equity and debt are not perfect substitutes, so that size depends positively on the amount of equity. In Albuquerque and Hopenhayn (2004) and Clementi and Hopenhayn (2006) lenders introduce credit constraints because of limited liability of borrowers and limited enforcement of debt contracts and because of asymmetric information on the use of funds or the return on investment, respectively.

Cabral and Mata (2003) analyze whether these two theories are consistent with the evolution of a cohort's size distribution in the Portuguese manufacturing sector. They find that, as the cohort ages, the firm size distribution shifts to the right largely due to growth of surviving firms rather than exit of small firms. In addition, they find that in the first year after entry younger business owners are associated with smaller firms but that is no longer the case once the cohort gets to age seven. Assuming that age is a proxy for the entrepreneur's initial wealth, the authors conclude that the age-size effect supports the idea of financially constrained firms starting at a suboptimal size and present a model with financing constraints capturing this effect.

More recently, Angelini and Generale (forthcoming) use survey and balance sheet information for Italian manufacturing firms to analyze the impact of financing constraints on the evolution of the firm size distribution. They find that financially
constrained firms tend to be small and young, although this does not have a significant effect on the overall firm size distribution. Moreover, they find that financing constraints decrease firm growth, with this effect being entirely due to small firms. In particular, being young and financially
constrained does not have any additional effect. Based on these results and the fact that young firms grow faster than old firms, the authors conclude that financing constraints are not the main factor behind the evolution of the firm size distribution. In line with their argument, this paper
interprets the facts presented in Cabral and Mata (2003) and other cross-sector evidence as the result of the interaction between adjustment costs and learning about efficiency.^{10}

To our knowledge, this work is the first to suggest adjustment costs as an explanation for differences in firm dynamics by age. The paper by Cabral (1995) is nearest to this paper. In his model, firms must pay a proportional sunk cost to increase their production capacity. He argues that, in a model with Bayesian learning, a proportional capacity cost would make small entering firms grow faster than large entering firms. The reason is that small entrants are those whose initial profitability signals were not good, so their exit probabilities are higher, and therefore they choose to invest more gradually. Unlike our model, Cabral's model depends on the existence of selection. Also, by analyzing a size-growth relationship, his model is not able to explain why some large entering firms also grow substantially.

The paper is organized as follows. In section 2, we present evidence of firm dynamics for a cohort of entering firms. In section 3, we build the general model, obtain optimality conditions, and provide heuristic arguments explaining the effects of adjustment costs. In section 4, using a simplified version of the model we analytically prove the effect of linear adjustment costs on survivors' growth. In section 5, we calibrate and estimate a finite learning horizon version of the model and quantify the contribution of adjustment costs to firm dynamics. Section 6 concludes. All proofs are left for an appendix.

2 Firm Dynamics in a Cohort of Entering Firms

There is a well established literature on the identification and explanation of differences in behavior between young and old firms. In this section, we analyze firm dynamics in a cohort of entering firms. We use *Quadros de Pessoal*, a database containing information
on all Portuguese firms with paid employees. This dataset originates from a mandatory annual survey run by the Ministry of Employment, which collects information about the firm, its establishments, and its workers. All economic sectors except public administration are included. The panel we have
access to covers the period 1985-2000. Information refers to March of each year from 1985 through 1993, and to October of each year since the reformulation of the survey in 1994. On average the dataset contains 250,000 firms, 300,000 establishments, and 2,500,000 workers in each year.

The literature on firm dynamics typically finds that young firms grow faster than old firms. Using kernel density estimates of the firm size distribution in a cohort of entrants, Cabral and Mata (2003) argue graphically that the cohort's evolution is mostly due to growth of survivors rather than exit of small firms. Their analysis points to the need for a measure of the contribution of survivors versus non-survivors to the growth in a given cohort's average size. To accomplish this, we propose a decomposition of the cohort's cumulative growth that will later allow an assessment of the empirical relevance of adjustment costs. We consider the following decomposition:

where is the firm's age, is log-employment at firm in period , is the set of age- surviving firms, is the set of age- non-surviving firms, so that is a partition of , and is the number of firms in set .

In general, the growth in a cohort's average size can originate from growth of survivors or from smaller initial size of non-survivors. Any theory of firm dynamics should consider both these sources of growth. Our measure allows a check on whether a particular theory can explain the key source of growth in a cohort's average size. The survivor component compares the current average size of period survivors with their initial average size, so that it measures how much survivors have grown. The non-survivor component compares the average initial size of period non-survivors with the average initial size of period survivors, so that it measures how relatively small non-survivors were initially.

We can obtain a similar decomposition for employment-weighted moments. The weighted decomposition contains information about the entire distribution of employment, not just its cross-sectional mean, and is affected both by within- and between-firm growth. Therefore, the weighted decomposition
would be more relevant for assessing a richer model that considers the reallocation of employment shares between firms within the cohort. In the results that follow we focus on the unweighted decomposition because it analyzes within-firm growth, which in our model is the most relevant statistic to
assess the effect of adjustment costs on the incentives for firms to grow.^{12}

We can also produce a decomposition based on the cohort's annual growth instead of the cohort's cumulative growth. However, the annual version of the above decomposition is more sensitive to two aspects that would complicate the analysis in the paper. First, the annual survivor component is
significantly affected by the business cycle, especially after the first few years of life. To control for this, we would need to somehow remove the cyclical part of the survivor component. Second, as the age of the cohort increases, the annual survivor component becomes increasingly sensitive to
downsizing and exit by some survivors that become technologically outdated and consequently relatively less efficient. To fully consider this aspect of the data would force us to introduce additional parameters into the model that we present in section 3. Therefore, we believe
that by employing a decomposition based on the cohort's cumulative growth we avoid having to adjust the analysis for these two aspects, and instead focus on how intense is survivor's growth while learning-about-efficiency effects are significant.

Year |
CEx |
AvEmp |
CGrEmp |
SComp |
---|---|---|---|---|

1988 | 1.11 | |||

1989 | 15.6 | 1.27 | 15.2 | 69.5 |

1990 | 24.4 | 1.36 | 24.8 | 70.4 |

1991 | 30.8 | 1.43 | 31.2 | 69.7 |

1992 | 35.4 | 1.46 | 34.2 | 69.3 |

1993 | 40.0 | 1.46 | 34.6 | 68.9 |

1994 | 43.4 | 1.47 | 35.3 | 69.1 |

1995 | 46.7 | 1.48 | 36.1 | 68.7 |

1996 | 49.9 | 1.49 | 37.4 | 67.2 |

1997 | 52.7 | 1.51 | 39.6 | 68.5 |

1998 | 55.5 | 1.52 | 40.7 | 68.3 |

1999 | 58.5 | 1.54 | 43.0 | 68.9 |

Notes:

In table 1, we present the evolution of exit rates and the share of firm growth due to the survivor component in the 1988 cohort of entering firms for the overall economy.^{13} In 1988 there were entering firms. The exit rate is very high initially but tends to decrease as firms get
older.^{14} However, ten years after entry only of the initial entrants remain active. There is significant growth in the cohort's average size, especially in the first few years, which is mostly due to the growth of survivors rather than to the exit of small inefficient firms: survivors' growth contributes around
to the growth in the cohort's average size.^{15}

Notes:

Table 2 presents similar evidence on cohort dynamics for the manufacturing and services sectors.^{16} We include the employment shares
of each sector in the 1988 cohort of entering firms, which are close to shares in the overall economy. Although manufacturing has a much higher employment share than services, the number of entering firms in services surpasses that of manufacturing ( 6074 and 4834, respectively). Both sectors display a cumulative exit rate around by 1999. However, initial differences in exit rates are more significant, with manufacturing displaying the smallest values, and services displaying the highest values. In terms of initial size, manufacturing has the largest
entrants, and services the smallest. Although manufacturing has the largest entrants, it exhibits more growth in average employment and a larger contribution of survivors to that growth than services**.**

We perform two robustness checks on the previous findings. First, we redo our calculations using establishments rather than firms as the unit of analysis. For the 1988 establishment cohort, we obtain similar results, although exit rates and the survivor component are higher than in the case of
firms. Second, we examine an alternative cohort to make sure our results are not driven by business cycle conditions. The Portuguese economy experienced an expansion between 1986 and 1991, a period of slow growth with a recession between 1992 and 1994, and another weaker expansion between 1995 and
2000. The growth rates of real GDP were in 1989, in 1992, and
in 1995, so that the 1991 cohort did not face as favorable a macroeconomic environment as the 1988 cohort. However, the results for the 1991 cohort are, in all dimensions, very similar
to those presented above. The results for the 1994 cohort are also very similar, but with slightly smaller values for the survivor component in the first few years after entry.^{17}

Notes:

In table 3, we provide evidence on characteristics of labor adjustment in the 1988 cohort of entering firms. We use the distribution of the adjusted growth rate conditional on survival. Following Davis and Haltiwanger (1992), the adjusted growth rate in period is defined as , where . The table shows that the incidence of inaction is very high, increases with age, and is higher in services than in manufacturing. This may reflect technology-induced differences in adjustment costs, or job indivisibilities affecting to a larger extent the services sector for having a higher share of small firms. The table also shows that the large majority of firms have adjustment rates within the interval. A high rate of inaction and small adjustment is usually considered consistent with the presence of linear or proportional adjustment costs. An additional fact is the left skewness of the 1989 distributions, showing that survivors tend to grow initially, especially in manufacturing. This skewness is less evident in 1993, suggesting that adjustment patterns are different in initial years. The evidence on inaction justifies our assumption of linear adjustment costs in the model that we present next.

In this section, we introduce linear adjustment costs into a model of Bayesian learning about efficiency. We derive conditions for optimal employment over time and present heuristic arguments about the effects of adjustment costs on the path of employment. Our model is based on Jovanovic (1982), adding adjustment costs and using a different specification for the idiosyncratic shock.

We assume an industry with competitive output and input markets. Current profits of a representative firm are defined by

,

where
is the production function; is the amount of labor input;
is a productivity shock; and is the wage rate. The output price is
normalized to unity, so that all monetary values are expressed in units of the output price. Given the competitive environment, the firm treats as a constant.
Concerning technology we make the following assumption.

Part **(a)** basically ensures a well defined interior optimum. In some of the analyses below, we will further specialize by assuming that is Cobb-Douglas.
Meanwhile, part **(b)** establishes that in each period productivity is stochastic with a constant mean over the firm's lifetime. The productivity component, , is
made of two parts: , which is observed before entry, and , which is
never directly observed by the firm. Intuitively, can be thought of as indexing *ex ante* efficiency, measuring initial technology choice, while indexes *ex post* productivity, measuring how well a firm performs within its technology choice.

The introduction of is essential to obtain a non-degenerate distribution of firms' entry size, allowing an analysis of the contribution of survivors to growth in the cohort's average size. In contrast, the absence of in Jovanovic's (1982) model generates a degenerate distribution of firms' entry size. Under this scenario, for any period after entry, survivors and non-survivors have the same average initial size implying a value of to our measure of the survivors' component. By assuming , we avoid this aspect of Jovanovic's model.

Before entry the firm knows the parameters governing the stochastic process of , i.e., ,
,
and
, and learns its *ex ante* productivity, , after paying a research cost, . After entry, the firm will learn about its specific *ex post* productivity, , over time as it observes the realizations of productivity, . In particular, the firm forecasts
period- productivity based on the *ex ante* efficiency parameter and on the past realizations of productivity,
. Similarly to Zellner (1971), a firm with age has the following Bayesian posterior distribution for at the beginning of period :

In the absence of adjustment costs, while deciding whether to stay one more period or to exit, the firm compares the expected profit in case it stays, , with the opportunity cost of doing so, , the value it would recover by selling the (exogenously determined) capital initially acquired, i.e.,

where represents expected profits conditional on staying in period .

At entry, we have
, and in equilibrium expected profits must compensate for the cost of acquiring capital, i.e.,
. Since markets are competitive and there is no friction in the entry and exit processes, in equilibrium the research cost equals expected gains at
the research phase, i.e.,
. If
more firms will initiate research and later enter the industry, causing a decrease in output price until equality is restored. A strictly positive fixed
research cost, , is essential to avoid the extreme situation where trial research is so high that only the highest productivity firms enter and survive. Because there is no reliable
capital stock variable in *Quadros de Pessoal*, we do not make the capital decision endogenous to the model. Instead, we assume that firms are homogeneous along the capital dimension and face the same opportunity cost of remaining in activity, .

Up to this point, the only differences between our model and Jovanovic (1982) are that in the latter model the efficiency parameter implicitly affects the cost function and the cohort's entry size distribution is degenerate. Therefore, without adjustment costs there would be no intertemporal linkages in our model aside from the exit decision. As in Jovanovic, because is strictly increasing in , the exit decision is characterized by an age-dependent exit threshold. For values of above or equal to that threshold, the firm would stay and choose employment to maximize current period profits. For values of below that threshold, the firm would leave the industry, since its expected profitability is below the opportunity cost. The increasing confidence the firm puts in as it grows older implies that the exit threshold is increasing with age. This is the driving force underlying Jovanovic's result that the size distribution and the survival probability increase with age.

We now introduce linear adjustment costs into the model. The adjustment cost for continuing firms, , is defined as

where is the cost per unit of adjustment. Since this is a model with endogenous entry and exit of firms, we consider that this cost also applies to the entry and exit decisions, so that the costs for entering and exiting firms, and respectively, are given by, .

With adjustment costs, the problem now becomes,

for all periods after entry () in which the firm remains in the industry, and

for the entry period, where , the value of exiting, is defined as

.

Note that contrary to the case without adjustment costs, the previous period employment is a state variable for the current period optimization problem. Also, in and in the costs of hiring at entry and firing at exit are taken into account.
In general, we could allow for asymmetry among the cost parameters in , , and . However, asymmetries between the cost of regular firing and the cost of firing at exit or between the cost of regular hiring and the cost of hiring at entry lead to biases in entry and exit decisions. For example, if the per unit regular hiring cost is higher than the per unit entry hiring cost, then firms will hire more workers at entry in order to save on expected future higher hiring costs. Similarly, if the per unit regular firing cost is smaller than the per unit exit firing cost, then firms facing the prospect of exit will fire workers before exiting the industry, saving on expected future higher exit firing costs. To avoid these biases, throughout the paper we assume symmetry between the parameters in , , and . A more interesting distinction is between firing and hiring costs. We will see below that the conclusion of the paper is immune to asymmetries between the costs of adding and subtracting workers.

In solving the firm's problem, we consider a two-step optimization procedure where the firm first chooses optimal employment in each of three possible scenarios, and then selects the scenario with the highest pay-off. More precisely,

,

where and are obtained by maximizing the objective function in
(4) over
and
, respectively, and is obtained by choosing
in (4). Although the adjustment cost function introduces a non-differentiability of the objective function at the frontiers between adjustment and
non-adjustment, the usual properties of the value function and its associated optimal exit policy function hold
In contrast, the non-differentiability of the objective function generates an inaction region in the employment policy, within which optimal employment does not vary with changes in productivity.

Equations (6), (7) and (8) are marginal conditions, similar to the smooth pasting conditions in the (*S*, *s*) model literature, and they state that if the firm adjusts then the marginal
adjustment cost must equal the expected present discounted value of the marginal revenue product for all future periods in which the firm is still in the industry, minus the increase in the exit cost when the firm decides to exit. This is the discrete-time analog of the continuous-time result
present in Nickell (1986) and Bentolila and Bertola (1990), adjusted for the fact that now we also have an exit decision. Because the firm will not change employment if the marginal cost of adjustment exceeds its marginal benefit
for the first unit of adjustment, proportional costs imply inaction in the employment decision of the firm.

Although the results in proposition 6 do not allow a formal proof of the effects on firm growth of adjustment costs in this general model, the following corollary of proposition 6 enables us to make qualitative heuristic statements about those effects.

Corollary #.:

As we have seen above, in the absence of adjustment costs, optimal employment is determined solely to maximize current period profits, so that
. Therefore, firms' growth is essentially a by-product of a selection mechanism: those firms that are inefficient, and therefore small, exit,
while those firms that are efficient survive and grow. There is an additional source of positive growth when the frictionless employment decision rule,
, is convex in
. Because of Jensen's inequality and because
is a Martingale, surviving firms will grow over time:
.
However, will not be convex in
for general
.^{20}

In arguing heuristically about the impact of the proportional cost on firm growth we use the property that is weakly increasing in
, and that
is locally weakly increasing in
. Because it is not immediately obvious why firing and hiring costs should give similar incentives for firm growth, we analyze separately these two costs.^{21} We present in figure 1 the case where there is a hiring cost, , and no firing cost, . This figure assumes a given
. For that specific value of ,
and
are the frontiers between non-adjustment and upward and downward adjustment, respectively. Therefore, if
there will be no adjustment and the marginal benefit of an additional unit of labor (represented by the dashed line) is
contained in the interval
. To simplify the argument, we consider a firm whose sequence of productivity draws is such that in every period it has a perceived productivity equal to the
unconditional mean of
, even though the firm's uncertainty over next period
decreases with age.

*Case 1: Hiring Cost:* *,*

Because the firm starts at the hiring margin, we must have at entry, and , for all subsequent periods, , with the two extremes of the interval representing firing and hiring of workers, respectively. Consider first a situation where exit is not allowed. Under this assumption, (9) would become

For the entry period, we have , which implies that the firm will start smaller when than when .The Bayesian learning mechanism implies both persistence and a reduction in variance with age in the Markov process associated with . The effect of persistence, that is, the fact that , was analyzed in the previous paragraph. The reduced uncertainty in the posterior estimate of productivity will be reflected in a smaller inaction region as firms accumulate information on realized productivity; that is, decreases with . This causes an increase in for those firms already at the hiring margin, which must be balanced by an increase in for the right hand side of (9) to remain equal to . As firms become more certain about their true productivity they are more willing to adjust to their long run optimal size. Because most firms are at the hiring margin, this will cause a further increase in average size.

Consider now the possibility of exit. In this case, the uncertainty reduction as the firm ages implies a decrease in the exit probability, and a further increase in the future-periods component of in (9). Consequently,
needs to increase further in order to offset that.^{23} On the other hand, the smaller exit probability implies less pruning of inefficient slow-growing firms as a cohort ages, which tends to make growth in average firm size smaller. Therefore, we will have less cohort growth due to non-survivors and more cohort growth due
to survivors, so that survivors' contribution to average firm growth in the cohort should increase when exit is allowed.

*Case 2: Firing Cost:* ,

In this case we have , , . Assume first that exit is not allowed. The intuition is the same as in case 1. In comparison with , when firms start smaller and subsequently hire more frequently than they fire. As firms age, the reduction in variance of causes an increase in , which must be compensated by an increase in for firms at the hiring margin. When exit is possible, those effects become more intense, since the exit probability will decrease as firms age.

From the heuristic intuition we have just given it becomes clear that proportional hiring and proportional firing costs reinforce each other in creating incentives for firms to grow. In the end, our assessment of the relevance of linear adjustment costs for firm growth will depend on how well a pure selection model can fit the empirical evidence, and on how much adjustment costs improve the fit. Before we move into a quantitative assessment, we present analytical results for a simple version of the general model.

4 Model with One Period Learning Horizon and No Exit

In this section, we analyze a model where firms' efficiency is revealed after the first period of life and where firms' lifetime horizon is know with certainty at entry. We assume that firms live for periods, , and that no exit is allowed prior to age . These two simplifications allow us to determine the effect of linear adjustment costs on firm growth.

The introduction of adjustment costs implies an additional expected operating cost for entering firms. Therefore, the equilibrium price must increase to generate higher expected future profits that compensate for the costs incurred while adjusting to optimal size. As a consequence, pre-entry pruning of inefficient firms should increase while post-entry pruning should decrease. This is optimal from a social point of view, since with higher adjustment costs there should be less experimentation in order to save in unrecoverable costs. Therefore, the assumption that exit is exogenous is not critical for the results in this section. Since adjustment costs attenuate post-entry pruning, even if exit was endogenous to the model, the relative contribution of survivors to growth in the cohort's average size would increase through this channel. By eliminating any exit prior to we focus only on the incentives for survivors to grow.

To formulate the problem, we use the fact that once the firm learns its true efficiency in period 2, it will adjust once and for all to its long run employment level, and it will not adjust in any of the following periods.^{24} Therefore, assuming that upon exit at age the firm recovers its initial investment net of exit costs, the
optimization problem in period 2 is

where , and and are defined as above. In period 1, we then have Finally, the equilibrium price is determined by the condition that potential entrants break even, i.e., .

We examine the impact of adjustment costs on the log growth rate of employment, rather than the standard growth rate, in order to attenuate the effect of Jensen's inequality on firm growth.^{25} In this simple model, the inaction region of optimal employment can be expressed as an interval:
. Therefore, the average log growth rate between period 1 and period 2, conditional on
, is defined as

where is the support of the distribution of , and and are the frontiers between non-adjustment and downward and upward adjustment, respectively. Depending on the specific value of and the magnitude of the adjustment cost parameters, we might have and/or . However, in the results that follow, we assume that and the adjustment cost parameters are such that both downward adjustment and upward adjustment occur with positive probability, i.e., and . Since we assume exogenous exit, we ignore the indirect effect of adjustment costs that works through changes in the equilibrium price, and implicitly assume that the research cost, , adjusts to maintain an equilibrium. This indirect price effects influence average firm size in both periods, but are of second order importance for the average log-growth rate.

Optimal employment in period 2 is determined by

where the frontiers of adjustment are defined asWe then have the following result concerning the effects of changes in and on the cohort's average log growth rate of employment.

Consider first the hiring cost. In the proof, we show that an increase in decreases both
and
. The impact of on the growth rate depends on two opposing
effects. First, while in the case of
the cost of hiring can be equally spread out over
periods with certainty, in the case of
it will be spread out over either periods or one period,
depending on whether the firm learns in period 2 that it has overhired. Therefore, *ex ante* a proportionately greater part of is attached to period 1 in the case of
than in the case of
, affecting more
than
. This explains the positive effect on growth of for
. Second, the hiring cost on
can possibly be spread out over periods, while the hiring
cost on
can only be spread out over periods. This affects more
than
, and explains why the effect of on growth is not necessarily
positive for finite . However, as increases the first effect
dominates so that decreases
more than
and growth increases.^{28}

With respect to there is always a positive effect on growth, independently of the lifetime horizon. This occurs because an increase in decreases and increases . This positive effect always dominates the uncertain effect due to the fact that also decreases with .

When there are both hiring and firing costs and these costs are identical (
), then an increase in has a positive effect on
, for sufficiently high , where the
required is lower than in item **(a)** of proposition 8.

5 Calibration/Estimation Under Finite Learning Horizon

In the previous two sections, we developed heuristic and some formal arguments about the effect of adjustment costs on the incentives for firms to start smaller and grow faster after entry. In this section, we assess the contribution of adjustment costs to explain some of the basic facts on firm dynamics found in section 2, both for the overall economy and for the manufacturing and services sectors. To accomplish this, we perform a calibration/estimation of the model using computational methods.

To simulate the infinite learning horizon model we follow the suggestion of Ljungqvist and Sargent (2004) and consider an approximation where firms live forever, but learn their *ex post* true productivity component,
, with certainty at some age .^{29}

We assume that is Cobb-Douglas, i.e., , . Under this assumption, when adjustment is costless, optimal employment is given by

where is the productivity exit threshold. Therefore, with , optimal employment conditional on survival is a convex function of , so that Jensen's inequality implies growth of employment even if there is no selection. As in the previous section, in order to avoid any growth due to Jensen's inequality, we take logs of all variables and analyze the effects of adjustment costs on the log-growth rate.

Concerning the productivity distribution, we assume that
is lognormally distributed, i.e.,
.^{30} This assumption is made for computational simplicity, and it seems reasonable on empirical grounds (see Aw *et. al.*, 2004). In addition, this assumption is not critical as the results in section 4 suggest that the distribution of productivity mostly affects the intensity of the effect of adjustment costs on firm growth, but not the sign. In fact, proposition 8 is derived independently of the particular distribution of
. With the log-normal distribution assumption, the transition law for the
s is as follows.

,

.

Since we assume that the firm enters the industry already knowing its *ex ante* productivity component (see assumption 1), we will
get a non-degenerate distribution of initial size. This occurs because
, and
has positive variance in the cohort's initial distribution. The next proposition analyzes the properties of the optimization problem after is revealed to the firm in period .

, | (10) |

, , . |

This result enables us to simplify the computational algorithm significantly, since it implies a finite horizon dynamic programming problem. In appendix B, we present some details concerning the computational algorithm used to simulate the model. In the next subsection, we partially calibrate and estimate the learning model with costly adjustment, and in the following subsection we do a sensitivity analysis.

We calibrate and estimate our model to match statistics from the 1988 cohort of entering firms, both for the overall economy and the manufacturing and service sectors. We first calibrate parameters related to inputs directly from the data. We then use a form of the method of moments to estimate
the parameters associated with the learning process and the adjustment cost. These estimates are obtained so that the model generated moments match the evolution of firm size, of exit rates, and of the survivor component observed in the data. As discussed in appendix B, we find
the set of parameter values that minimize the method of moments objective function by using a simulated annealing method. This optimization method is robust to local minima, to discontinuities, and to the discretization implemented in order to simulate the model.^{31} A central element to our estimation strategy is a decomposition of the change in the cohort's average size into a survivor component and a non-survivor component. This decomposition
forces the model to match not only the growth in the cohort's average size but also the contribution of surviving and non-surviving firms to that growth. Similarly to section 2, with
, our decomposition is defined as

(11) |

Prior to estimation, we calibrate some parameters. The parameters and
are calibrated with data from INE (1997) containing the *Inquérito Annual às Empresas* from 1990 to 1995. These data are considered reliable and cover all firms in the Portuguese economy, with sampling among firms with less than 20
workers. We measure as the 1990-1995 average of the cost share of labor in value added, and as the 1990-1995 average cost per worker. We can also obtain these values at the one-digit sectoral level. We deflate all nominal variables using the GDP sectoral price indices available in the updated version of Séries Longas para a Economia
Portuguesa in Banco de Portugal (1997). The real interest rate is calibrated as the 1990-1995 average of the implicit real interest rate on public debt transactions on the secondary market of the Lisbon Stock Exchange. The data was also taken from
Banco de Portugal (1997). We deflate the nominal interest rates using the December-to-December consumer price index from INE (1990-5). The discount rate is then obtained as
, where is the average real interest rate.

The remaining parameters, ,
,
, , , and are estimated using a method of moments estimator, which attempts to make the model match closely the evidence on cohort
dynamics presented in section 2. In particular, the estimates are selected to minimize a weighted sum of the distance between the following moments in the model and the data: (a) the time-series of the cross-sectional mean of log-employment conditional on survival,
; (b) the time-series of annual changes in the cross-sectional standard deviation of log-employment conditional on survival,
; (c) the time-series of the cumulative exit rate,
; (d) and the time-series of the survivor component, as defined in (). In estimating the above parameters, the output price is normalized to 1, and the initial research cost, , is obtained by the equilibrium condition
.^{32}

The decision to estimate , instead of calibrating it, deserves some discussion. First, the main purpose of this parameter is to induce endogenous exit as it represents the firm's
opportunity cost of remaining in activity. In Hopenhayn (1992), the same result is accomplished using a fixed per period operating cost. Since the per period operating cost can be seen as the periodic payment in an annuity with a present discounted value of
, the two mechanisms are equivalent. Second, because *Quadros de Pessoal* misses any reliable capital stock variable, we consider the capital decision to be
exogenous. A rough estimate of the magnitude of is the present discounted value of an annuity with annual payments equal to the 1990-1995 average of value added minus labor costs, using the
same deflators as for .^{33} Because the sample
is biased towards surviving firms, this measure overestimates the value of , and we cannot use it as a reference to calibrate . Consequently, we estimate jointly with the remaining parameters in the model.

Parameter |
||||||
---|---|---|---|---|---|---|

0.56 | 0.56 | 0.57 | 0.57 | 0.73 | 0.73 | |

0.956 | 0.956 | 0.956 | 0.956 | 0.956 | 0.956 | |

11.8 | 11.8 | 13.1 | 13.1 | 7.5 | 7.5 | |

3.227 | 3.180 | 3.435 | 3.607 | 2.408 | 2.455 | |

0.218 | 0.205 | 0.257 | 0.188 | 0.143 | 0.122 | |

0.259 | 0.255 | 0.261 | 0.253 | 0.153 | 0.137 | |

0.571 | 0.656 | 0.558 | 0.526 | 0.359 | 0.314 | |

668.4 | 775.3 | 1136.4 | 1291.1 | 179.8 | 189.0 | |

0 | 0.70 | 0 | 1.13 | 0 | 0.11 | |

122.5 | 76.5 | 180.7 | 224.1 | 22.2 | 18.6 | |

0.0861 | 0.0629 | 0.1727 | 0.1236 | 0.0480 | 0.0439 |

Notes:

We present in table 4 the calibrated and estimated parameters for the three cohorts and the model with (*AC*) and without (*NAC*) adjustment costs, and in figure 2 we plot the overall economy data
moments and the equivalent moments in the *AC* and *NAC* models. From table 4, we verify that more information is revealed ex post
, and that there is significant noise in the learning process (
,
). For the overall economy cohort, the *AC* model implies an estimate for the proportional cost of about of the annual wage. As can be seen in figure 2, this proportional cost improves noticeably the fit of the survivor component.

Figure 2 shows that although the *NAC* model can generate moments on firm size and exit rates that are close to equivalent empirical moments, it cannot satisfactorily match the empirical survivors' contribution. That is, the NAC model cannot explain the main source of growth in the cohort's average size, since survivors contribute much more to growth in the data than in the *NAC* model. This shortcoming occurs especially in the initial years after entry as the path of the
survivor component is almost flat in the data, whereas it is increasing in the *NAC* model. The larger initial distance between the *NAC* model and the data in terms of the survivor component reflects the fact that, in the absence of adjustment
costs, learning has a larger initial impact on the exit of small inefficient firms than on growth of survivors.

In table 4, we also calibrate/estimate the *AC* and *NAC* models for the manufacturing and services sectors, and in figure 3 we present a summary of the implied moments. In discussing the results for
the two sectors we consider the estimates for the *AC* model. Firms in manufacturing initially learn relatively less about their efficiency than firms in services (
is smaller in manufacturing), and adjustment costs need to be relatively higher in manufacturing than in services to account for the much higher survivor
component in manufacturing (the proportional costs amount to and of
the annual wage, respectively). The higher adjustment costs and smaller knowledge about their efficiency at entry, implies higher incentives for manufacturing firms to start smaller and to gradually adjust to optimal size as they survive and their uncertainty is resolved. Firms in manufacturing
also pay a relatively higher initial research cost ( is higher). This, together with the smaller initial knowledge about their efficiency (
is smaller), implies that manufacturing firms are more likely to enter the industry at the research phase (
equals in manufacturing and in services).

While the introduction of adjustment costs clearly improves the fit of the survivor component in the model, we cannot claim that the proportional cost explains completely the path of the survivor component in the data. In fact, in all three cohorts the initial growth of survivors seems larger
than the *AC* model can explain. Additionally, in the manufacturing sector, although the *AC* model raises noticeably the contribution of survivors relative to the *NAC* model, the survivor component generated by the
*AC* model is still somewhat below the survivor component in the data. Several factors could be behind these results. First, the introduction of a fixed entry or fixed exit cost would improve the fit of the *AC* model. By introducing a wedge
between the "cost" of entry and the "benefit" of exit, these fixed costs would help to control both the fraction of firms that never enter the industry,
, and the amount of exit in the initial post-entry periods,
. As these fixed costs increase, the first fraction increases and the second probability decreases due to a larger initial selection. Therefore, these fixed
costs would allow more freedom in adjusting
to account for the long-run survivor component, without distorting much the initial exit rates. The proportional adjustment cost would also increase,
raising the long-run value of the survivor component and making its path flatter. Second, other theories that emphasize firm growth in the first years after entry, namely those based on financing constraints, can certainly also account for the high value of the survivor component, especially in the
manufacturing sector.

In this subsection we explain some aspects of the calibration/estimation exercise and provide a detailed sensitivity analysis to all parameters in the model. First, we do not attempt to match the level of the cross-sectional variance of log-employment, but only its change over time. This is because to fit the dispersion in employment, the model would require substantially larger values for both and . This would allow the model to match and , but would imply an excessive rate of growth in . However, this shortcoming is not a serious problem. It implies that only a fraction of the observed cohort's employment dispersion can be attributed to a Bayesian learning process about efficiency. The remaining part could be attributed to heterogeneity in the initial choice of technology.

For instance, consider a model where capital is endogenous and suppose that a firm chooses its initial stock of capital, , based on the realization of a random variable indexing
technology choice. Assume further that, after selecting , the firm keeps its capital stock unchanged for the remainder of its life. If the production function has constant returns to
scale, if the total opportunity cost is proportional to , i.e.,
, then we can easily prove that
, where is the value function conditional on the chosen . Therefore, in this alternative framework, dispersion in
would govern the initial dispersion in employment and only the subsequent evolution in employment dispersion would depend on the Bayesian learning process. This is the reason why we
attempt to match only the evolution of
, but not its level. In the estimated models presented in table 4 only little less than of the observed dispersion in the cohort's log-employment can be attributed to the learning process.^{34}

Second, the value of affects the long-run contribution of survivors, since a relatively smaller initial dispersion would make the average size of exiting firms closer to the average size of surviving firms in the entry period, and in this case most growth would be due to survivors. In the aforementioned extended model with an initial choice over , if we had we would have a non-degenerate initial distribution of size, entirely due to the heterogeneity in , but the survivors' component would be in each period. This would occur because the distribution of initial size among exiting firms would be equal to the distribution of initial size among surviving firms. This also explains why even with heterogeneity over , we would still need to assume in order to match the empirical facts on the importance of the survivor component.

While we could increase the long-run contribution of survivors by tinkering with the ratio
, without adjustment costs the model cannot match the observed flatness in the path of the survivor component. For any choice of
and
, it will always be the case that the survivor component will exhibit an increasing path in the absence of adjustment costs. Note also that the ratio
affects both the exit rate and the evolution of the cross-sectional firm size dispersion. If this ratio becomes too small, post-entry exit rates become
excessively high and the size dispersion increases too fast. This is the reason why in the *NAC* model we cannot find a value for this ratio that attains the long-run contribution of survivors found in the data, and simultaneously matches the behavior of the cumulative
exit rate and the evolution of the cross-sectional size dispersion. Therefore, the value we select for this ratio is disciplined by the exit rates and the evolution of firm size dispersion in the cohort.

Third, to show that proportional adjustment costs are crucial for our model to fit the evidence on the survivors' contribution to growth in the cohort's average size, in figure 4 we perform a sensitivity analysis with respect to each parameter in the model. We take as
benchmark the *NAC* model estimated for the overall economy cohort in which we do not attempt to match the evidence on the survivor component.^{35}

From figure 4, we see that the model with costless adjustment cannot match satisfactorily the contribution of survivors to growth, even if we allow parameters (except for the proportional cost) to vary one by one from their benchmark values. In fact, no other parameter
besides the proportional cost can shrink significantly the distance between the survivor component at different ages of the cohort without changing much the exit rates. The main effect of these costs is to put more emphasis on individual firm growth in the initial years of life, when exit of
inefficient firms is very intense.^{36}

To emphasize the role of the proportional adjustment cost in replicating the evidence on the contribution of survivors, in figure 5 we present the impact of changes in on the survivor component, using as a benchmark the estimates for the *AC* model for the overall economy cohort in table 4. We conclude that allowing for even a small value of has a substantial impact on the survivors' contribution, with a larger effect in the initial years of life.

6 Conclusion

In this paper, we show that a model with learning about efficiency and linear adjustment costs generates incentives for entering firms to be smaller and for successful firms to expand faster after entry. We present evidence on firm dynamics for a cohort of entrant firms in the Portuguese economy. The evidence shows that growth in the cohorts' average size is driven largely by growth of survivors rather than by pruning of small inefficient firms, with rapid growth of survivors in the initial years after entry and with significant differences between manufacturing and services in the contribution of survivors. A calibration and estimation of the model reveals that the proportional adjustment cost is the key parameter to explain the high contribution of survivors to growth in the cohorts' average size. In order to explain the higher contribution of survivors in manufacturing than in services, adjustment costs need to be higher in manufacturing, both in absolute terms and in relation to the wage.

The paper proposes a channel through which linear adjustment costs to job creation and job destruction can affect firm size dynamics. Therefore, proportional costs not only make job creation and job destruction more sluggish, but also affect the lifetime dynamics of firm size. Although our theory does not provide a complete explanation for the evidence on the survivor component, the success of our model in better approximating the growth of survivors as the main source for growth suggests that adjustment costs do play a significant role in firm size adjustments after entry. From our results, we conclude that selection theories are more relevant to explain firm exit than to explain growth of survivors. Financing constraints theories should also play a role in explaining growth of survivors. Although there is not much evidence that financing constraints can explain cross-sector differences in growth of survivors, financing constraints should be especially relevant when technology requires a large startup cost, such as in manufacturing industries.

Angelini and Generale (forthcoming) argue that financing constraints are not the main determinant behind the evolution of the firm size distribution. Therefore, any government intervention to eliminate financing constraints might not change the lifetime dynamics of firm size we find in this paper. Furthermore, this paper suggests that, in sectors where adjustment costs are high and learning is important, government policies aimed at curbing financing constraints might not produce the intended results, as firms under those circumstances have incentives to start smaller and expand faster.

A. Appendix: Proofs

,

where
is the posterior distribution of
. Because
is continuous and strictly decreasing in , and
is strictly increasing in
, we conclude that
is continuous and strictly increasing in
(see theorem 3.4.1 in Swartz, 1994). Therefore, for the purpose of predicting
,
, since
, where
is the inverse function of with respect to . Using the recursion
the conditional distribution of
can be represented as

;

**(a.i)** *Existence and Uniqueness:* This follows from the Contraction Mapping Theorem and Blackwell's sufficient conditions (see theorems 3.2 and 3.3 in Stokey *et al.*, 1989).

**(a.ii)** *Continuity in*
: Let
be the space of bounded functions on which are continuous
in
. This is clearly a closed subset of
, the space of bounded functions
. Since
with the sup norm
is a Banach space, then
is also a Banach space. Now consider
. Because
is also continuous and
satisfies the Feller property (see lemma 2), then is continuous in
(see lemma 9.5 in Stokey *et al.*, 1989). Since
is continuous, then
is continuous in
. Therefore, applying the maximum theorem, we conclude that
is continuous in
. Note that the set of admissible values for employment can be made compact. First, only non-negative values are acceptable for employment.
Second, we can choose a value for high enough, say , such that
, for all
, so that all values of interest are considered. is
finite since
, and is bounded. Therefore, as defined by (4) is continuous in
.

**(a.iii)** *Strict Monotonicity in*
: From lemma 2 (the transition function associated with
is monotone) if
is weakly increasing in
, then
is also weakly increasing in
. Then, because
is strictly increasing in
(and the constraint set is not affected by
),
is strictly increasing in
(see theorem 9.11 in Stokey *et al.*, 1989).

**(b)** *Exit Policy*: The exit policy is determined by the condition

.

We conclude that
is continuously differentiable at
, with probability one (given
and for all
).
Now consider a generic period , and assume that is continuously differentiable at with probability one. Because is a unique continuous function of , we can apply the dominated convergence theorem to conclude that is continuously differentiable at , for all (see theorems 3.2.16 and 3.4.3 in Swartz, 1994). Consequently, the same argument used for period can be repeated here.

,

If it is optimal for the firm to adjust upwards, then we must solve

and if it is optimal for the firm to adjust downwards, we must solve Now, the derivative can be rewritten aswhere some of the regions might be empty, and in separating the integrals we have taken into account the continuity of the integrand in at the frontiers.

For each of the above derivatives we have

,

Using the law of iterated expectations, we can rewrite the above as

Taking into account that , , , and , then we get the stated result.

, | |

, | |

, . |

After some algebra we get

where stands for the elasticity of the marginal product of labor. If , we have , and the above expression simplifies to

where

Under the assumption that marginal productivity is always positive, we need or otherwise the firm would prefer to pay the worker his lifetime salary, instead of firing him. If , we have , and the above expression simplifies to

which is positive for all .

, | |

, | |

, , , , |

so that, in the end, we get

, | |

. |

From here the result follows by noting that .

For the unconditional distribution, just note that is a sum of normal random variables, and that

Consider a firm that is in the industry at time , . We now prove that this firm will not change its employment level in period . For this, we use the easily proven fact that it is less costly to adjust in one step than in two steps, i. e.,

,

where
. We then have
. |

Therefore, at time it is optimal to set .

We now prove that the firm does not exit at time after remaining in the industry at time , . Because the firm stays at time , then . Now assume that in period the firm exits, so that

This then implieswhich is a contradiction.

B. Appendix: Computational Algorithm and Estimation Method

We describe the algorithm we use to numerically simulate and estimate the finite learning horizon model in several steps.

**(i)**- Discretization and transition probability matrices associated with : We discretize based on a uniform discrete approximation to the (cross-section) distribution of , which is . We then employ the method of Tauchen (1986) in order to build the transition matrices associated with this discrete approximation. We use a grid with 25 points.
**(ii)**- Discretization of We have used the decision rules for problem (12) in case of hiring and in case of firing, from which we consider
, , .

For the mean of we assume that if a firm is at the upper end of the grid for , then it should optimally decrease employment even at , and that if a firm is at the lower end of the grid for , then it should optimally increase employment and exit next period, even at . We then find the upper and lower end of the grid for such that those decisions occur, and use the same procedure to discretize as the one used for , considering 800 gridpoints. **(iii)**- Choice for We choose , and display results until period .
**(iv)**- Model simulation For a given set of parameters we numerically compute the optimal entry, employment, and exit policy rules. In doing this, for each point in the grid for
we compute the optimal employment associated with

since these do not depend on . In doing this, we first find the optimizer on the grid for presented in**(ii)**. Then, we use this maximizer to implement a golden section method to find a more precise value for this maximizer.^{39}We then convert these value functions into and , determine the inaction regions, and compute . With the optimal policy functions in hand, we generate a random sample with lifetime histories of , and compute all endogenous decisions associated with each realization of a firm's lifetime history. We then use this information to compute by simulation the relevant moments in the model. **(v)**- Moments used in estimation We consider four sets of moments, computed among firms that actually enter the industry:
**(a)**Exit rate: For , we consider**(b)**Average current size conditional on survival: For , we consider**(c)**Relative change in variance of current size conditional on survival: For , we consider^{40}

**(d)**Average entry size conditional on survival: For , we consider^{41} **(vi)**- Weighting matrix The weighting matrix is obtained as the inverse of the sample variance-covariance matrix of the moments in
**(v)**,, **(vii)**- Estimation method We use a simulated annealing method to search for the set of parameter values
that minimizes the method of moments objective function,
^{42}

"Comparative Analysis of Firm Demographics and Survival: Evidence from Micro-Level Sources in OECD Countries," *Industrial and Corporate Change*, 14 (3), 365-91.

"Firing Costs and Labour Demand: How Bad is Eurosclerosis?,"
1. Board of Governors of the Federal Reserve System (e-mail: eugenio.p.pinto@frb.gov). The views expressed in this paper are those of the author and do not necessarily reflect the views of the Federal Reserve Board or its staff. I would like to thank valuable comments from John Shea, John
Haltiwanger, Michael Pries, Boraan Aruoba, and Rachel Kranton. All remaining errors are my own. I would also like to thank the Direcção-Geral de Estudos, Estatística e Planeamento -
Ministério da Segurança Social, da Família e da Criança, for kindly allowing me to access the Quadros de Pessoal database, the University of Minho for their hospitality, and João Cerejeira and Miguel Portela for their help in extracting results. Return to Text

5. For example, firm growth would occur in our model even if exit was random with a constant probability for all firms, whereas that would not be true in a pure selection model. Return to Text

7. Although we could have included fixed adjustment costs they seem more relevant in the case of capital. Return to Text

8. Hopenhayn and Rogerson (1993) did consider that the firing cost applied also at exit, but in their model there is no learning process and they did not analyze the effect of the firing cost on firm growth.
Return to Text

9. Rossi-Hansberg and Wright (2007) advance an alternative theory based on mean reversion in the accumulation of industry-specific human capital. However, their model only deals with size-dependence of firm
dynamics, and has nothing to say about age-dependence of firm dynamics, which is our main concern. Return to Text

10. Our interpretation of the age-size effect is close to the alternative explanation proposed by Cabral and Mata (2003, footnote 14), in the sense that young business owners would be subject to a more intense learning.
Return to Text

11. Throughout the paper we will assume that firms enter in some generic period 0. Therefore, will represent both the
firm's age and the period (after entry) we are analyzing. Return to Text

12. For the weighted decomposition, the cumulative change would be
, where
is the weight of firm in period in set , with
. The weighted survivor component can be further decomposed as
The first term is a within-firm component, measuring average growth weighted by initial size; the second term is a between-firm component, measuring the contribution of changes in employment shares; and the third is a cross component. For the unweighted decomposition, the last two terms are zero,
since in this case
. Return to Text

13. We identify entering firms in year as those firms that have not been in the database before . Given the high incidence of temporarily missing firms, we select the 1988 entering cohort, using 1985 and 1986 to detect false entries. Similarly, we identify exiting firms in the -th period (after entry in 1988) as those firms that are present in the database in period , but do not reappear in any of the following
periods. Therefore, we display results only up to 1999, using 2000 to detect false exits. This procedure eliminates most false entries and false exits. Return to Text

14. We adopt the following procedures concerning temporarily missing firms. In calculating the exit rate we do not exclude temporarily missing firms, considering them as survivors. In calculating the cohort's mean log-employment at period , we scale it with a factor that compares that mean in period 0 between all firms and those not temporarily missing in period . We also adjust the data in 1994, when the survey moved from March to October, to correct for a higher than normal exit rate and average growth in this year. Return to Text

15. When we use employment-weighted data, we find that larger firms have smaller exit rates and, as a consequence, average employment increases more intensely than in the unweighted data. This and the fact that high-growth firms increase their weight over
time, explains a larger survivor component in the employment-weighted decomposition. A similar exercise for labor productivity reveals that survivors account for about of the change in
the cohort's unweighted average productivity. Return to Text

16. In order to obtain equivalent one-digit SIC87 sectors, we use the following correspondence in terms of CAE Rev. 1 codes : manufacturing
and services
. Return to Text

17. Reflecting our previous argument about the greater cyclical sensitivity of the decomposition based on the cohort's annual growth rate, we observe a substantial reduction in the annual survivor component associated with the 1988 and 1991 cohorts during the
1992-1994 slow growth period. However, a similar pattern does not occur with the 1994 cohort. This is one of the reasons why we choose a decomposition based on cumulative growth rates. Note also that the annual non-survivor component is not as sensitive to the business cycle as the annual survivor
component. Return to Text

18. In this model we do not consider the possibility that as firms get older they might decay or become obsolete. This could be achieved by assuming exogenous probabilities for those two events. This could generate both a decrease in size of old firms (decay)
and the exit of old firms (decay and obsolescence). Return to Text

19. Because in general is not concave, we cannot prove the usual differentiability properties of the value function. Therefore, in what
follows, we implicitly assume that
is differentiable at with probability one, in terms of
for all
. By part **(b)** of proposition 4 and the dominated convergence theorem, this implies that the objective functions
associated with , and are continuously differentiable in , so that marginal conditions can be applied to find interior optima. This assumption
also implies that
is differentiable at
with probability one. In proposition 5 of appendix A, we prove that this property holds both in a model with a finite lifetime horizon and
in a model with infinite-lived firms that face a finite learning horizon (as in sections 4 and 5). Return to Text

20. In general, from the optimal employment condition,
, we have
whose sign depends on
. Therefore, if decreasing returns to labor do not decrease too fast, that is,
, then we will have
. When
, then
, and when
,
, then
. Return to Text

21. In the discussion that follows, the hiring cost applies both to regular hiring and to hiring at entry and the firing cost applies both to regular firing and to firing at exit. Return to Text

22. When exit is not allowed, we can prove that is concave (and continuously differentiable) in , so that must decrease for to increase. Return to Text

23. This effect is similar to that of Cabral (1995). Return to Text

24. This result is formalized in proposition 10 below. Return to Text

25. As we saw above, when optimal employment is a convex function of
, Jensen's inequality implies positive expected growth, even in the absence of adjustment costs. Because the log transformation is concave, it will offset the convexity of the
optimal employment function. For example, for a Cobb-Douglas specification of
, the log growth rate eliminates the effect of Jensen's inequality, since
becomes linear in
. Return to Text

26. In proposition 8 below, if the production function is Cobb-Douglas the indirect price effects cancel out. Return to Text

27. In the proof, we consider a general production function and then specialize to a Cobb-Douglas specification in order to obtain the sign of the effect. From that general setup, we can say that the form of the production function should not be determinant
for these results when the elasticity of the marginal product of labor does not change much with the amount of labor used. Return to Text

28. In our simulations, was enough to generate a positive effect on growth. Return to Text

29. Note that this differs from the lifetime horizon used in section 4, with
. In this section, we assume an infinite horizon, so that
. In our simulations below, we assume that (years), and
present results until year 10. Return to Text

30. Under log-normality, and
. Although this violates assumption 1, this is not a problem in this section, since we will be using a discrete approximation to the productivity
distribution. Return to Text

31. The objective function is defined as
, where
is a vector of differences between the sample and model generated moments, and is the estimated variance-covariance matrix of . Return to Text

32. To make the computation of equilibrium easier for a given set of parameters, instead of changing the output price we change the fixed research cost so that the condition
is satisfied. Return to Text

33. The estimates are 1373.8 for the overall economy cohort, 3317.1 for the manufacturing cohort, and 269.1 for the services cohort. Return to Text

34. In figure 2, we rescale the estimated initial values of
to the level found in the data. Return to Text

35. The sensitivity analysis with a benchmark based on the overall economy *NAC* model in table 4 would produce similar results. Return to Text

36. Note that we would not be able to identify the hiring/entry cost, , and the firing/exit cost, , separately, because and produce almost identical results. This should be expected as the incentives created by proportional hiring/entry and firing/exit costs differ only in the displacement of time by one period. Return to Text

37. A similar result would hold for the case of infinite-lived firms that face a finite learning horizon, as in sections 4 and 5. However, in this case we would need to use proposition 10
first. Return to Text

38. In
and
we need to use
and
because , in general, is not concave in . Return to Text

39. See Press *et al.* (2007). Return to Text

40. This moment condition can be expressed in terms of the ratio of the time- and time-0 variances. Return to Text

41. This moment condition together with condition **(b)** can be expressed in terms of the survivor component. Return to Text

42. See Goffe *et al.* (1994). Return to Text