Evaluation of Public R&D Policy: A Meta-Regression Analysis ()

Syoum Negassi^{}, Jean-François Sattin^{}

Université Paris 1 Panthéon-Sorbonne, PRISM Sorbonne, Paris, France.

**DOI: **10.4236/ti.2019.101001
PDF HTML XML
406
Downloads
764
Views
Citations

Université Paris 1 Panthéon-Sorbonne, PRISM Sorbonne, Paris, France.

Economic theory and empirical evidence indicate that technological innovation is an important determinant of long-term economic development. Various country policies have been launched in favour of private research and development (R&D) with economic development as the main objective. As often in economics, public intervention is grounded on the presumed existence of market failures. The purpose of this paper is two-fold. First, it provides an overview of the history of R&D-related tax policies in more than ten industrial countries. Second, after reviewing the existent empirical evidence on the effectiveness of R&D tax credits policies, it presents a meta-regression analysis based on an econometric model. Our results show that an R&D tax credit is strongly significant in the studies taken cumulatively.

Keywords

Share and Cite:

Negassi, S. and Sattin, J. (2019) Evaluation of Public R&D Policy: A Meta-Regression Analysis. *Technology and Investment*, **10**, 1-29. doi: 10.4236/ti.2019.101001.

1. Introduction

US, European and Asia policy makers have been concerned about the technological performance of their countries for large parts of the Twentieth Century. These concerns were sharpened by the post-war rise of the Japanese economy, which enjoyed very high growth rates until the 1990s based on a strong technological base and high commitment to R&D. The phenomenal growth of US, European and Asian economies (specially the Asian tiger economies) over the 1980s and mid-1990s has also been based on a high-tech strategy. These competitive threats have coincided with an intellectual movement in economic theory which emphasizes the conscious accumulation of R&D and human capital in explaining economic growth [1] .

Public support for innovation-related activities has been justified in several ways. First, governments are responsible for providing new or improved technology for public sector functions (security, health, and communications) and R&D for these tasks may be performed in public research laboratories or contracted out to private firms and funded by public revenues. The second justification for public subsidies is to correct for market failures. Market failures in real and financial markets offer scope and justification for public support, as the return may be not sufficient to justify private investment. The broad consensus on the use of public support is based on the inefficiencies of the market. The neoclassical theory based on a positive externality argument suggests that, because of the “public good” characteristics of R&D activities, the level of private R&D expenditure would be systematically lower than the socially optimal level. These create a gap between private and social return on R&D, and as a result less than optimal levels of research. Incomplete appropriability of research output and externalities deriving from the public good nature of R&D are at the base of this [2] [3] . The characteristics of imperfect appropriability and imperfect excludability lead to the under-provision of innovation outputs by private decision makers in a market environment. This occurs since the benefits associated with R&D activities are easily and freely available to firms that are not engaged in R&D efforts. Indeed, the lack of full appropriability of R&D outcomes reduces the incentive to do R&D on the part of private firms so that, as in a classical Pigouvian context, government intervention through subsidization can reduce the extent of this “market failure”.

This argument has been widely criticized by several scholars. From an evolutionary perspective, Cohen and Levinthal [4] argued that knowledge cannot be so easily absorbed unless imitative firms, in turn, invest in a certain level of R&D effort: imitation is not costless and needs some pre-existing “hard core” R&D activity. This standpoint could lead to a paradoxical consequence: in an environment characterized by significant spillover effects, firms could have greater incentives to perform R&D since, in doing so, they might expand their absorptive capacity, i.e. their ability to benefit from the R&D efforts of others. In this way, they could more easily imitate and exploit market surpluses. As a consequence, the level of R&D could be too high (rather than too low), since many firms could undertake more R&D effort than that required to reach the optimal social results (e.g. by an increase of duplications in R&D expenditure).

Some scholars have suggested that R&D should not be taken as a pure public good: a firm has a great number of tools to protect its inventive capacity, such as patents and secrecy [5] . Therefore, the extent of positive externalities in production can be very limited and ⁄or industry-specific, and the need for supporting R&D activities more controversial than it might appear at first glance.

Additionally, knowledge is not subject to exhaustion or congestion because knowledge is a non-rival and partially excludable good [6] . The use of knowledge for one purpose does not diminish its supply or availability for other purposes. This “public good” feature demonstrates the social desirability of technological knowledge, but also presents a major disincentive for private investment.

There is also asymmetric information about the expected outcome of R&D investments and sunk costs in R&D investment. Moreover, investment in R&D is riskier than investment in physical assets, and as a result there are likely to be more financial constrained [7] [8] . Public investment is designed to encourage firms to carry out R&D by lowering marginal costs and decreasing the uncertainties that are typically connected to this activity. In addition to these direct effects at the firm level, positive indirect impacts are also expected to spill over to other firms in the system.

Economic theory and empirical evidence indicate that technological innovation is an important determinant of long-term economic development. Various country policies have been launched in favour of private research and development (R&D) with economic development as the main objective. For example, some countries like the United States and France, pioneered in R&D tax credit programs at the beginning of the 1980s. The popularity of R&D tax credits continued into this millennium, when other countries established their R&D tax credit programs in the end of 1990 and beginning of 2000, respectively. The rationale backing such policies is that governments can pursue regional economic development by correcting market failure in innovation, thus enhancing private incentive to invest in research and development.

Given that the R&D tax credit has been in existence in many countries for a number of years, one legitimate question is whether this R&D-preferential policy has induced additional private R&D expenditure in these countries. There is no doubt that jobs and income are ultimate goals in countries’ innovation-based economic development. However, increasing private spending on R&D in the country is a necessary intermediate step toward these final goals. Therefore, evaluating the effects of tax credits on private R&D spending is an important first step toward a full evaluation of the economic effects of R&D tax incentives. Since the R&D tax credit co-exists with other countries R&D policy efforts, we can also include other relevant policy factors such as countries’ cooperative technology programs in Europe, and input and output of the higher education sector. Although R&D tax credit is just one of several policy instruments on R&D, it is a common strategy being employed by many countries for many years.

There have been many policy analyses of R&D tax credit, which confirm the effectiveness of R&D tax incentives on private spending in R&D. Studies of tax incentives aim mainly at measuring the additional private R&D spending and the cost-effectiveness of the incentives. Econometric estimation using two types of parametric methods developed first: impact models [9] in which a binary variable shows the impact of the tax incentive, and demand models [10] that directly obtain the price-elasticity of R&D investment. More recently, parametric approaches have been combined with non-parametric ones in the evaluation of public policies. The second set of approaches has been widely used to determine whether R&D direct subsidies complement or crowd out private spending on R&D. In these studies, the recent concern about endogeneity and selection problems has led researchers to identify patterns in the distribution of public support and to estimate counterfactual status [11] .

As more and more emphasis is being given to the role of government supporting innovation-related activity, a clearer understanding of the historical intent of R&D related tax policies and of the effectiveness of these policies appears to be necessary.

The purpose of this paper is two-fold. First, it provides an overview of the history of R&D-related tax policies in more than ten industrial countries. Second, after reviewing the existent empirical evidence on the effectiveness of R&D tax credits policies, it presents a meta-regression analysis based on an econometric model.

Section 2 presents the aspects of the public scheme to be evaluated. Section 3 is devoted to the R&D tax incentives schemes and theoretical framework of the effectiveness of public policies with a brief introduction to models that are widely used in the evaluations of R&D public policies. Section 4 outlines the empirical methodologies and section 5 presents results and discussion.

2. R&D Tax Incentives Schemes and Theoretical Framework of Government Policies for Private R&D

2.1. Public Policy Scheme

R&D tax incentives also often seek to understand the channels underlying a possible increase in the amount of R&D caused by the policy. For example, many questions can be raised: by how much do R&D tax incentives increase investment for firms that already investing in R&D; how many firms that were not yet investing in R&D are induced to invest in R&D to the tax incentives; and how does the presence of R&D tax incentives across countries affect the decision of firms to locate their R&D investment in different tax jurisdictions.

The effectiveness of R&D tax incentives on increasing R&D investment can be evaluated by estimating the private “R&D price elasticity”, which measures the percentage change in R&D investment resulting from tax relief for every percentage change in its after-tax price (also called the user cost of R&D), or by the “incrementality ratio,” which measures the change in R&D investment per dollar of forgone tax revenue that is spent on R&D fiscal incentives.

The incremental credit is meant to target tax relief to R&D expenditure that would not have occurred in absence of the credit. On the other hand, volume credits do not provide additional incentives to increase R&D investment from previous years since conditional on current level of R&D, firms will receive a tax credit regardless of their past investment.

An incremental scheme supports more firms with high R&D growth relative to a volume-based scheme which supports equally all R&D performing firms. A combination of volume and incremental tax incentives (hybrid schemes) maintains the level R&D investment and simultaneously rewards high growth in R&D investment [12] .

R&D tax incentives may also affect the overall level of R&D investment in a country by encouraging R&D by firms that have not previously invested in R&D. R&D tax incentives schemes can provide special provisions for new claimants (e.g. France) or starts-up (e.g. France, Netherland and Korea). At the same time, fiscal incentives might not be sufficient to spur a firm’s decision to invest in R&D; there is scarce empirical evidence on this issue, (see our results).

R&D tax incentives are now used in 26 out of 34 OECD member countries. Among non-OECD member countries, Brazil, China, India, Russia, Singapore and South Africa provide tax incentives for R&D.

The existing R&D tax incentives schemes differ significantly across countries in terms of their generosity, their design, and how they explicitly target different firms or specific areas. Tax incentives for R&D include expenditure-based tax incentives, tax credits, R&D tax allowance, payroll withholding tax credit for R&D wages, and taxing royalty income and other income from knowledge capital at a preferential rate. Tax incentives differences are illustrated in Table 1. Most OECD countries and emerging countries provide fiscal incentives through tax credits or enhanced allowances. Tax credits allow a direct deduction from the tax payable while enhanced allowances provide an additional tax deduction (above a normal deduction rate of 100% for wages, and depreciation for capital cost) from corporate taxable income. The main difference between the two mechanisms is that the former directly reduces the tax liability while the latter approach the reduction in tax liability depends on corporate income tax rate.

Table 1. R&D tax incentives schemes in selected developed and emerging countries, 2013.

This table shows in: (a) the three kind of tax incentives for R&D in the world; (b) countries which use payroll withholding as tax credit for R&D wages; (c) taxing royalty income and other income from knowledge capital at a preferential rate; (d) countries with ceilings on amounts given to the enterprises; (e) countries with Income based R&D tax incentives; (f) countries without tax incentives.

R&D tax incentives may apply to all qualified R&D expenditures (volume-based credits like in Canada) or only to the additional amount of R&D expenditure above a certain base amount (incremental credits like in USA).

Support for business R&D through the tax system is typically part of a broader set of policies to support investment in R&D, which also includes direct support, such as grants, loans or procurements contracts.

The overall costs associated with the R&D tax incentives schemes depend both on the uptake of the scheme by firms and the design of tax incentives in a country. Significant differences exist in the generosity of R&D tax incentives across countries and within countries between small and large firms.

2.2. Theoretical Background

The majority of research on the effects of public policies on firm R&D expenditure have chosen to measure the presence/absence of “additionality” of public incentives by skipping, at least implicitly, the essential step of providing an explicit theoretical framework to explain this causal relation (and also without entering too much into the analysis of other types of additionality, such as that based on output variables: productivity, profitability, innovation performance, etc.). David et al. [13] and David and Hall [14] provide more sound theoretical bases for the understanding of the effect of public policies on private R&D investment. Their structural model identifies the optimal level of R&D investment as the point at which marginal rate of returns (MRR) and marginal capital costs (MCC) associated with R&D investments are equal. This is the classic profit maximization strategy of firms. The MRR curve derives from sorting R&D projects according to their internal rate of return, as in a usual investment plan. This curve is a decreasing function of R&D expenditure, since firms will first implement projects with higher internal rates of return and then those presenting lower rates. The MCC curve, instead, reflects opportunity costs of investment funds, at any level of R&D. This curve has an upward slope due to the assumption that, as soon as the number of projects to implement increases, firms have to shift from financing them through retained earnings to equity and/or debt funding (i.e. from internal to external and more costly sources).

Both curves depend on a number of variables (other than R&D expenditure) that can move them either downward or upward. MRR depends of technological opportunities; state of demand; appropriability conditions and MCC of technological policy tools; macroeconomic conditions; external costs of funds; and venture capital availability. The equilibrium condition, MRR = MCC, provides the optimal level of firm R&D investment. According to this framework, we might wonder what kind of effect a subsidy would have on the equilibrium level of the R&D expenditure: additionality; crowding-out, etc.

The difficulties that private parties are confronted with in reaping the benefits from their R&D investments and the intrinsic risks associated with innovations leave significant room for government intervention. According to microeconomic theory, governments can stimulate private R&D investment and spur economic development by reducing the marginal cost of capital (MCC) and/or raising the marginal rate of return (MRR) on private R&D investment. Government policies that directly target R&D include intellectual property rights, R&D tax credits, direct funding to industries and government R&D labs, and investing in public services (higher education in science and engineering disciplines, programs for technology development and application, and so on).

The offer of R&D tax incentives offsets the inappropriability inherent in innovation by reducing the cost of private R&D activities. The tax incentives have involved allowing R&D expenditures to be expensed rather than capitalized, offering depreciation allowance and tax credits for eligible R&D expenditures, and other tax benefits such as exemption of sales and use taxes for R&D properties.

Direct subsidies (either R&D contracts or R&D grants) are another major way governments intervene in private R&D activities. While tax incentives reduce the cost of private R&D, direct public subsidies induce additional private R&D investment by raising the private MRR on R&D investment. Direct subsidies also relieve the firms of some joint costs of research and development activities. On the other hand, public R&D subsidies may simply substitute for some of the investment that the performing firms otherwise would have prepared to undertake. Moreover, public R&D subsidies may negatively affect private investment in R&D by introducing the upward pressure on the prices of R&D inputs, such as wages of scientists and engineers.

In the public finance literature, the quality of public services is generally regarded as an important factor in the decisions of business location and/or expansion. Public services provide direct benefits to businesses and help to reduce business cost. For R&D investment, two types of services are important: higher education (which is a major source of R&D human resources and knowledge spillovers to business R&D) and cooperative technology programs (which assist technology development and application to benefit companies and industries in the states).

In the past two decades, many governments in Europe have been very active in stimulating R&D investment within their borders by offering various incentives and services to industries. If properly designed and implemented, the additional private R&D spending induced by the tax incentives can bring about some desirable economic benefits to the county. These benefits may include more highly paid jobs, higher per capita income, and an appropriate share of other benefits from the R&D conducted in their territory.

A number of studies have been done to evaluate the effectiveness of tax incentives in making firms spend more on R&D. The usual evaluation consists in checking whether there is R&D additionality, in the sense that private firms increase their R&D expenditures by more than it costs the government to support the tax incentives program. If per dollar of government support less than one dollar of additional private R&D gets spent by business, then public support partially crowds out private funding for R&D. The evaluation of the so-called ‘‘bang for the buck’’ is a rough cost-benefit analysis that generally does not take into account factors like spillovers, indirect tax returns, administration costs and the opportunity cost of spending taxable income on R&D support.

Different models may be used in analyzing a wide range of issues relevant to an evaluation of tax incentives, but their highest relevance and most widespread use are in the analysis of input additionality and result additionality. The discussion is concentrated around these issues.

Hall and van Reenen [15] focus their discussion on estimating the input additionality effect, through econometric estimation of demand equations for R&D.

There are basically two approaches [15] :

1) R&D demand equation with shift parameter for existence of a tax credit scheme. The first approach is used in a large number of studies. In this approach, the demand equation includes a variable that indicates whether the firm had access to the tax incentive, in addition to other variables that affect R&D investments:

$\mathrm{ln}{\left(\text{R\&D}\right)}_{it}=\alpha +\beta {C}_{it}+\gamma {X}_{it}+{\epsilon}_{it}$ . (1)

where R&D i is the R&D expenditures of firm i, C_{i} is a variable measuring the taxcred it received by the firm i, and X_{i} is a vector of firm-specific characteristics affecting its R&D strategies (e.g. past R&D, cash flow and financial conditions, size, technological capabilities). In this specification, the parameter β (expected positive) measures the additionality ratio, which indicates the average increase that a tax credit induces in firms’ R&D investments.

This equation expresses the logarithm of the R&D investments of firm i in year t as a function of the presence of a tax incentive, C_{it}, that is equal to one if firm i had access to the scheme in year t and zero otherwise, and other variables, which are contained in the vector X_{it}. Such variables may be previous R&D investments, previous output and sales, expected future output, cash flow, product prices, etc. Whether the firms have been granted R&D subsidies through other channels will also be an important factor.

The β-parameter measures the expected growth of R&D investment following a firm getting access to the scheme. The basic framework assumes that this effect is identical across firms. This assumption is hardly innocuous, but it is not discussed by Hall and van Reenen [15] . Such models should be estimated on microdata to utilize cross-section variation in access to the scheme across firms. Using macro-data only, it is impossible to distinguish the effects of the scheme from unobserved macroeconomic shocks.

2) Demand equation with user cost of R&D. The second “demand equation” approach has very much in common with the one described above. The major difference is that instead of just including a variable indicating existence of or access to a tax incentive for R&D, one calculates the so-called “user cost” of R&D investments, i.e. a variable that reflects the price of R&D investments for the firm, on the margin, taking into account R&D tax incentives, other tax rules, interest rates and depreciation. The introduction of, for example, a tax deduction scheme for R&D will reduce the user cost of R&D.

For R&D tax incentives, the “user cost of R&D” model is employed in most of the empirical studies at levels ranging from individual firms to the whole economy. In a recent review, Hall and Van Reenen [15] conclude that a dollar in tax credit for R&D stimulates a dollar of additional private R&D investment. They argue that the estimation based on the “user cost of R&D” model is preferable because it is grounded in economic theory, and the price response of R&D investment can be estimated directly. However, some weaknesses still exist in the model. One important methodological issue is the simultaneity between the R&D investment level of a firm and the tax price it faces. Additionally, since the user cost of R&D is a composite measure of depreciation allowance, tax credit, corporate income tax rate, and personal income tax rate, the visibility of policy effects is low.

$\mathrm{ln}{\left(\text{R\&D}\right)}_{it}=\alpha +\beta {\rho}_{it}+\gamma {X}_{it}+{\epsilon}_{it}$ . (2)

in which ${\rho}_{i}$ is a variable measuring the user cost of R&D (i.e. its marginal costs), and the parameter β (expected negative) is the elasticity of R&D with respect to its price, measuring by how much R&D will increase when its marginal costs decrease.

In which ${\rho}_{it}$ is a variable measuring the user cost of R&D (i.e. its marginal costs), and the parameter β (expected negative) is the elasticity of R&D with respect to its price, measuring by how much R&D will increase when its marginal costs decrease.

The key advantage of the user cost approach compared to the shift parameter approach is that one may utilize variations in the generosity of the scheme across firms, and also changes over time. Such variation may be very useful in identifying the effect of the scheme. In addition, variations in other components of the user cost (tax rules, interest rates, depreciation rates) may in theory help in identifying the effects of the fiscal measure. Within this framework, one may calculate the price elasticity of R&D, that is, how large the percentage change of R&D investments that follows from a one percentage change in the user cost.

The user cost is calculated by calculating what it costs for a profit-maximizing firm to invest “an additional dollar” in R&D at time t, and then “sell” this project in the next period. The tax system affects this cost in two respects. First, the return to the investment is taxed at a rate τ_{i}. Second, the investment cost is reduced by the tax subsidy and the allowed tax depreciation.

3. Econometric Analysis

Our meta-regression analysis builds upon a new database containing information on a large number of recent firm, country and state level studies on the effects of R&D tax credits. We then investigate the factors that may explain differences in the estimated effects that are reported in the literature. In addition to several other control factors, the key explanatory variable that we focus on refers precisely to the specific characteristics. Our meta-regressions investigate whether those studies have controlled for these specific characteristics.

A clearer understanding of the historical intent of R&D-related tax policies and of the effectiveness of these policies appears to be necessary. Analysis of the effects of public financing on private investment in R&D has been the objective of numerous applied studies without it having been possible to arrive at a definite conclusion. After the creation of a data-base including all relevant studies and their results and characteristics, a meta-analysis was carried out to examine whether the characteristic of the applied studies influence the results and explain the differences in the empirical literature on this subject.

This is an interesting pattern that calls for further research (i.e. constructed a model which takes into account some of the most important characteristics that explain variation in the estimated effects of R&D tax credits among different micro-econometric studies available in the literature). If corroborated by future investigations, this finding would cast some important doubts on the effectiveness of R&D tax incentives. This would in fact imply that fiscal resources intended to stimulate R&D and economic competitiveness have a relatively stronger effect on those specific characteristics that are characterized by low technological opportunities, sluggish demand conditions and weak spillover effects to the rest of the economy. If so, R&D tax incentives mechanisms should be redesigned in order to take into account the specific conditions that shape innovation propensity and dynamics in different industries of the economy, and in particular allocate a greater amount of fiscal incentives to R&D to high-opportunity and technologically dynamic sectors.

The specific novelty of our survey paper and its intended contribution to the literature are twofold. First, we carry out a meta-analysis is to create a database that includes the relevant studies on the effectiveness of R&D tax credit policies and on the relation between public funding of R&D and private R&D expenditure. In the end, more than 60 empirical studies were used in our meta-analysis (see Table 2). As is usual, most of them present more than one result (more than 700 estimation points in our econometric analysis, 341 for additivity ratio and 284 for user cost). The adoption of the meta-regression database and methodology opens up for future updates and extensions of this type of analysis of the effects of R&D policy. Second, in explicitly investigating the role of the specific characteristics, we create a bridge between the R&D policy literature, on the one hand, and the important strand of research on firms’ industrial patterns of innovation, on the other.

To compare the results of the existing studies it is necessary to have a summary statistic of the main variable which is the dependent variable in the meta-regression. The empirical studies used in the meta-analysis sometimes estimate elasticity and other marginal effects. The objective of a meta-analysis is to examine whether the characteristics of studies influence the results. These characteristics are the independent variables (also frequently called moderator variable) in the meta-regression. The variables are presented in the next section.

Table 2. List of papers working on the effect of tax credit on private R&D.

3.1. Data and Indicators

Following the standard meta-regression analysis methodology [16] , the search process for relevant papers to include in the meta-analysis database included many reviews. Only papers that presented an econometric analysis of the effects of R&D tax creditson firm-level innovation and that provided enough information regarding the effect estimates (their standard errors or t-statistics) were further considered. Our literature search focused more carefully on those more old and recent micro-econometric studies produced from 1983 onwards. Earlier studies had been identified and surveyed in previous overview papers, which made some of our data collection tasks easier [13] [17] [18] [19] [20] .

Typically, meta-analysis is a quantitative technique to summarize and evaluate the available empirical parameters (estimates) on a particular issue. That is, meta-analysis establishes guidelines to review, integrate, and synthesis studies examining similar research questions.

Then, it can detect whether consensus conclusions are emerging in the studies and whether differences in the results across literatures. Therefore, the goal of meta-analysis is to detect the existence of an association among the variable of interest, the estimation of magnitude and the statistical significance of such association. By making the process of research explicit and systematic, meta-analysis clearly compares the different studies in a systematic way.

Meta-analysis is more objective than the traditional literature review. Meta-analysis can include non-sampling characteristics as a moderator variable in a meta-regression model. Typically, each study on the effects of R&D fiscal incentives presents estimation results for several regressions. But, there is no clear benchmark or rule in the meta-regression literature for deciding how many and which of these reported regressions should be included in a meta-regression analysis dataset. Another problem is concerned with the conclusions by comparing and aggregating studies which are using different measuring techniques, definitions of variables, and subjects among the studies. The heterogeneity exists among studies because results from poorly-designed studies are included with results from good studies.

In order to have as many observations as possible and thus increase the variability of our sample, the selection criterion we used was somewhat broad. We included all different regressions produced by the same micro-econometric study as different observations in our dataset, as long as these regressions differed between them in some substantial way, e.g. in terms of their subsample, time period, model specification, tax-credit measure or dependent variable. This procedure is in line with other recent meta-analysis exercises in other fields of economic research [21] [22] .

3.2. Econometric Methods

The empirical studies estimate the Equations (1) and (2) presented in Section 2 of this study. According to those empirical studies, the main coefficient of interest is an estimate of the impact of tax credits R&D investment (β). Different researchers might present specific estimates of the effect of tax credit on R&D expenditure with and without a particular control variable.

Because the empirical studies mostly use different data sets, sample sizes and independent variables, variances of these estimated coefficients may not be equal and meta-regression errors are likely to be heteroscedastic. In order to compare with the research results from the empirical literature, it is necessary to transform the summary statistics to a common and comparable metric which is based on the concept of standardization [23] .

Glass [24] [25] introduced the concept of effect size to integrate the findings of an experimental literature, so that effect size allows diverse studies to be compared directly.

In addition, Meta-analysis has been suggested by Stanley and Jarrell [26] as a means of summarising more accurately regression results across studies, such as those investigating the relationship between R&D tax credit and R&D activity, and making generalisations from available empirical evidence. Stanley and Jarrell [26] pay attention to the reported t-statistic, which provide the critical tests in the empirical studies.

Several variables have been applied in the literature to test the relation between tax credit and R&D investment; our study follows Stanley and Jarrell [26] using t-values to compare a number of studies. In our work, the t-statistic which will be considered as the dependent variable had to be an estimate of the impact of some measures of tax credit. Most of the studies in our data sets provided more than one set of results for the estimation of initial regression. Following Stanley and Jarrell [26] , multiple estimates from the same study were used as separate observations if they referred to different years. Estimates from dissimilar models using data from the same year were also included as separate observations. On the other hand, an alternative modelling approach is to include only one estimate from each study and that is the best estimate by the authors. Nonetheless, the best estimate is not obvious in some cases, while the variation in the results is a key focus of most papers. Our study applies the first approach to aggregate different multiple estimates.

An advantage of the t-statistic is this standardized variable is a unitless measure, allowing easy comparability across studies. It is why, in our work, we can ignore issues regarding the measurement scales of the R&D investment and tax credit variables. For this reason, we will include in our models a range of measures of public policies (tax credits, etc.) and measures of R&D investment. Our paper will try to explain differences in the size of the estimated tax credit effects in the literature. Indeed, most econometric studies focus greater attention on significance than size because t-statistics are function of size. In our case, observation is the sample size for each study estimate; see the variable of number of observations in our data sets, which gives sample size for each study.

To explain variation in the empirical results in the literature, we quantify the impact of data and specification differences on the reported effect of tax credit on R&D activities. Our dependent variable, which is the parameter of interest, contains a vector of estimates of the effect being measured (the effect of tax credit on R&D investment). The t-statistics (dependent variable in this study) are explained by the many economic variables (dummy or continuous) and the usual error term. These moderator variables will be discussed below.

3.2.1. Publication Selection Bias

“The simplest and most commonly used method to detect publication selection is an informal examination of a funnel plot” [27] . A funnel graph of our dataset is a scatter diagram of estimated effect (user-cost elasticity and additionality ratio in our case). The expected shape is an inverted funnel (this means an absence of publication selection).

Graphs are very often vulnerable to subjective interpretation and it is better to model publication selection which involves a meta-regression analysis between user-cost elasticity and its standard error [28] [29] [30] [31] :

${a}_{si}={\beta}_{1}+{\beta}_{0}S{e}_{si}+{\epsilon}_{si}.$ (3)

where
$s=1,\cdots ,n$ (n studies),
$i=1,\cdots ,k$ (k regression estimates),
${a}_{si}$ is the user-cost elasticity or the additivity elasticity for study s and regression estimate i,
$S{e}_{si}$ is its standard error and
${\epsilon}_{si}$ is the error term. Equation (3) is the explicit representation of meta-regression analysis model for publication selection. In the absence of publication selection, observed effects should vary randomly around the true value, β_{1}, independently of standard error. When all studies are selected for statistical significance, publication selection bias will be proportional to the standard error
$S{e}_{si}$ .

Studies using larger samples can be expected to report smaller publication bias. In most econometric models, ${\epsilon}_{si}$ is considerate to be heteroscedastic and to avoid it the classical practice is to weight Equation (1) by $S{e}_{si}$ . Dividing Equation (3) by this term gives:

$\frac{{a}_{si}}{S{e}_{si}}=\frac{{\beta}_{1}}{S{e}_{si}}{\beta}_{1}+{\beta}_{0}+\frac{{\epsilon}_{si}}{S{e}_{si}}.$ (4)

$\frac{{a}_{si}}{S{e}_{si}}$ is the t-value (t of Student) for the estimated user-cost elasticity.

${t}_{si}=\frac{{\beta}_{1}}{S{e}_{si}}{\beta}_{1}+{\beta}_{0}+\frac{{\epsilon}_{si}}{S{e}_{si}}.$ (5)

Equation (3) is the Weight Least Squares (WLS) of Equation (1). Egger et al. [32] point out that the t-test of the intercept in Equation (3) is a test for publication bias, which indicates whether some omitted variables in Equation (3) (characteristics of the studies … etc.) may lead to systemic selection effect and hence a bias in the estimated effect. Stanley [16] , argues that the meta-regression model can be used to test not only for publication selection, but also for the true empirical effect after having controlled for publication bias. The first test is referred to the funnel asymmetry test (FAT) and the latter as the precise-effect test (PET).

FAT tests the hypothesis:

$\{\begin{array}{l}{H}_{0}:{\beta}_{0}=0\iff \text{implies lack of publication selection}\\ \text{Again}\\ {H}_{1}:{\beta}_{0}\ne 0\iff \text{implies either upward}\left(\text{positive sign}\right)\text{\hspace{0.17em}}\text{or}\\ \text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\text{\hspace{0.05em}}\text{\hspace{0.05em}}\text{downward publication}\left(\text{negative sign}\right)\end{array}$

PET tests the hypothesis:

$\{\begin{array}{l}{H}_{1}:{\beta}_{1}=0\iff \text{implies no authentic empirical effect},\text{this means also}\\ \text{no true effect corrected for any publication bias}\\ \text{Again}\\ {H}_{1}:{\beta}_{1}\ne 0\iff \text{implies the existence of authentic empirical effect}\\ \text{and could be interpreted as the true effect corrected}\\ \text{for any publication bias}\end{array}$

3.2.2. Meta-Regression Analysis

In our study, in addition to these two tests, we will investigate the effectiveness of R&D tax credits policies reported in the literature. We therefore extend the basic model in Equation (5) to include a set of additional explanatory variables (X_{s}_{,i}). In the econometric specification, those explanatory variables correspond to individual study characteristics that may have a substantial impact on the results of studies examining the relationship between tax credits and R&D activities. Table 3 outlines a list of moderator variables. Those moderator variables can be continuous or binary variables. The binary variables used in this study reflect the presence or absence of variables and generally take the form of dummy variables.

Table 3. Variables in our models, Independent Variables: Tstudent = t-statistic.

NB: Some variables come from Russell Thomson who has given us his dataset constructed by him.

${t}_{s,i}=\left(\frac{{\beta}_{1}}{S{e}_{s,i}}\right)+{\beta}_{0}+{\displaystyle {\sum}_{j=1}^{k}{\alpha}_{j}}\left(\frac{1}{S{e}_{s,i}}\right){X}_{j,s,i}+{\gamma}_{s,i}\left(\frac{1}{S{e}_{s,i}}\right)$ . (6)

${t}_{s,i}$ is the effect of tax credit on R&D investment.

By using Equation (6), we will test the following two hypotheses:

Hypothesis 1: Tax credit reduces the cost of R&D activity.

Hypothesis 2: Tax credit induces higher levels of R&D activity.

A comparison of empirical studies is difficult due to the heterogeneity of empirical models used. In our case, we split our data set in two due to the existence of two approaches in the evaluation of tax incentives (see Section 3 of this study). The sample across different literature suggests a number of explanatory variables, so we outline a list of moderator variables (see Table 3). We introduce four type of moderator variables:

· variables which represent the R&D investment measure: R&D expenditures by the private enterprises, Direct Government support on R&D, High Edu, Funds from abroad foreign enterprises;

· variables which represent R&D tax incentives: tax credit, labour tax, corporate tax, machinery tax, building tax;

· variables which represent data characteristics and methodology;

· variables which represent the various explanatory variables reported in the original studies.

4. Results and Discussion

4.1. Funnel

Figure 1 and Figure 2 plot the estimated user-cost elasticity and estimated additionality ratio with their inverse of standard error (weight). These graphs are referred to as funnel graphs because in the absence of publication selection it should look like an inverted funnel [28] . The symmetric shape is a necessary condition to exclude publication bias. These two figures have a funnel form and seem symmetric. We know that the visual interpretation of the funnel graph may be ambiguous, for this reason the FAT is generally associated with the Meta-regression analysis of Equation (3).

Table 4 displays results of Equation (1). This equation is a specification which only includes the constant ${\beta}_{0}$ (the publication bias effect) and $\frac{1}{Se}$ (measure of the true empirical effect of R&D tax incentives).

4.2. Meta-Analysis

Many specifications designed to inform what study attributes affect the significance, the sign, and the magnitude of the estimated R&D tax credit effects are estimated. The R&D tax credit effects variable (represented by t-statistics) is then regressed on several study characteristics that are presumed to influence the study outcome.

Table 5 and Table 6 present the results of meta-regression analysis. It reports the results of the estimation of Equation (3) and Equation (4), referring to the empirical approach in which the dependent variable used in previous studies is additionality ratio (Equation (1)) and referring to the second model specification that is typically adopted in the literature, which has as dependent variable the user-cost elasticity (Equation (2).

Figure 1. Funnel_Additivity, 341 observations (regression results).

Figure 2. Funnel_UserCost, 284 observations (regression results).

Table 4. Regression results of Equation (3) for both cases (Additionality ratio and user-cost elasticity).

***Significant at 1%.

Table 5. Meta-Analysis of Additivity ratio of R&D tax credit effects.

*Significant at 10%, **Significant at 5%, ***Significant at 1%.

Table 6. Meta-Analysis of User Costelasticity of R&D tax credit effects.

*Significant at 10%, **Significant at 5%, ***Significant at 1%.

A comparison of our results showed noticeable difference from other meta-analyse studies because we disaggregate the beta index on 3 components (respectively wages, mechanicals and building sub-indexes) that assess the R&D tax advantages allowed to firms depending on the nature of their spending. The effect of tax credit is mainly rooted in the fiscal advantages displayed toward wage, mechanicals and buildings appear to have a significant impact on the mean effect size of tax credit.

Our focus now shifts to different types of fiscal incentives. Fiscal incentives for R&D can take various forms (see Table 1). There are many reasons for the government to use these policy instruments: changes in tax structure often affect agents’ behavior. For example an increase in corporate tax rates distort the relative value of resources and lower the net rate of return to private R&D investment. Then, R&D activities are less attractive and the rate of growth declines. Therefore, taxes on investment and income have a detrimental impact on investment activities and economic growth in an economy. On the other hand, R&D tax credit can support firms to increase financial resources which are committed to technological innovation. That is tax credit deducted from the corporate income tax, so an increase in R&D tax credit lowers the user cost of capital and R&D investment becomes more competitive. Then, tax credit will stimulate further research on R&D and contribute to economic growth and social welfare.

Five specifications designed to inform what study attributes affect the significance, sign, and magnitude of estimated R&D tax credit effects are estimated and the results are reported below in Table 5 and Table 6. Positive coefficients of the moderator variables indicate that the characteristic of the study tends to provide a significant relationship between R&D tax credits and R&D expenditures. A negative sign implies that the associated characteristic of the study tends to return a non-significant relationship between the two variables. A non-significant coefficient implies that the characteristic of the study does not influence the relationship.

In Table 4, the estimated parameter for the constant is significant for both specification (User-cost or Additionality), providing evidence of publication (selection) bias effect. The parameter is positive in the case of Additionality specification and negative in the User-cost specification, indicating that previous studies overestimated the effect of R&D tax credits on firm’s innovation activities (in additionality) and they failed to control for a set of factors that may affect this relationship (in User-cost). In addition to the publication bias, note that the estimated coefficient on the inverse of the standard error is negative and is not significant in both specifications. This implies no authentic empirical effect (measured by the coefficient of the inverse of the standard error), this means also no true effect corrected for any publication bias. The slope of PET in these specifications serves as a test for empirical effect corrected of publication bias. Our estimations of Equation (6) will try to correct this publication bias. The PET does not find a significant evidence of positive of R&D tax credit effects for both sample of our analysis.

It is reasonable to expect that if tax credit is significant across studies, estimation of Equation (6) will generate a positive and statistically significant coefficient for the main variable R&D tax credit (Tax in Table 5). In different models (Table 5), results show that R&D tax credit is strongly significant in the studies taken cumulatively. A number of them have been done to evaluate the effectiveness of tax incentives in making firms spend more on R&D. The usual evaluation consists in checking whether there is R&D additionality, in the sense that private firms increase their R&D expenditures by more than it costs the government to support the tax incentives program. The evaluation of the so-called ‘‘bang for the buck’’ is a rough cost-benefit analysis that generally does not take into account factors like spillovers, indirect tax returns, administration costs and the opportunity cost of spending taxable income on R&D support.

Different models may be used in analyzing a wide range of issues relevant to an evaluation of tax incentives, but their highest relevance and most widespread use are in the analysis of input additionality and result additionality. The discussion is concentrated around the input additionality effect, through econometric estimation of demand equations for R&D.

The second “demand equation” approach has very much in common with the one described above. The major difference is that instead of just including a variable indicating existence of access to a tax incentive for R&D, one calculates the so-called “user cost” of R&D investments, i.e. a variable that reflects the price of R&D investments for the firm, on the margin, taking into account R&D tax incentives, other tax rules, interest rates and depreciation. The introduction of say a tax deduction scheme for R&D will reduce the user cost of R&D.

For R&D tax incentives, the “user cost of R&D” model is employed in most of the empirical studies at levels ranging from individual firms to the whole economy. Since the economic theory indicates that user cost of capital is a contributor to R&D investment, the exclusion of variables which are related to the user cost in a study may affect the estimated tax credit effects leading to a mis-specified model. This is why we have included an indicator of size, human capital, subsidy, etc. All our models (in Table 5 and Table 6) present sensitivity results at three levels of significance (1%, 5% and 10%) for the estimated tax credit effects.

The intercept in most of our models (example model 1 and model 6) is significant in both specifications, implying that there is a statistically significant relationship between tax credit and R&D activity.

Some data characteristics do affect positively the empirical analysis of the influence of tax credit on R&D activities, such as number of observations, the number of years covered by the study, and industry, firm, state or country level data. In contrast, a negative coefficient implies that number of observations and average years tends to provide a non-significant relationship between tax credit and R&D. The variable of the number of years covered is significantly positive in all our models, implying that early studies seem to give higher support to the relationship between tax credit and R&D. For instance, the variable of time dummy is significantly negative in some of our models. This indicates that the inclusion of this variable weaken the relationship between tax credit and R&D. In addition, the number of observations is significantly positive in models 6 and 9, that is, larger number of observations increase the probability of positive effect of tax credit on R&D activities.

Results indicate the inclusion of high-technology industry (variable HTD) as a variable matter. Controlling for high-technology industry through a dummy variable contributes Controlling for high-technology industry through a dummy variable contributes to an important increase in the effect of R&D tax credit on R&D activities. These results suggest that there is a positive program effect on R&D spending for the high-technology industry in the different studies. In sum R&D tax credit have positive effects on growth of R&D spending for all industry and the high-technology industry. This tells us that the R&D tax credit has the effect of increasing R&D spending not only for the high-technology industry but also for the industry. This evidence supports the appropriateness of this public policy on the grounds that the primary purpose of this credit law has been fulfilled.

On the other hand, our results show that our expectation is not totally realized because in most models the tax credit is not strongly significant. Among the variable capturing data characteristic (variable TD), the coefficient of the observation (variables NB and PEP), the country of data (Variable USNOUS), and the panel data (variable Desta) are also significant.

From the results, Private R&D expenditures, Government expenditure in high education, do not significantly affect the tax credit significance (coefficients positive and no significant except in model 10 Table 6). At all observation levels, Knowledge stocks (Variable HE) reveal positive effect but this is not strongly supported (only model 10 shows highly positive result).

The relationship between public funding and private funding is unclear from insignificant estimates in all our models.

5. Conclusion

This study presents a quantitative review of the empirical literature on the R&D investment from R&D tax credit policy. This study applies meta-regression analysis a sample of 625 t-statistics (341 t-statistics for additivity ratio model and 284 t-statistics for the user cost model) assembled for more than 60 studies to investigate the overall impact of tax credit on firms’ R&D investment. The research has painted a broad picture of the sorts of applications, methods, and findings, in the published literature. Our results show tax credit, other tax policy, estimation methods, sectorial dummy and level of analysis increased the estimated effect of tax credit on R&D expenditure. Lagged R&D, the inclusion of time, industry dummy, level of education and corporate tax rate do not appear to impact the estimated effect of R&D spending.

Conflicts of Interest

The authors declare no conflicts of interest regarding the publication of this paper.

[1] | Aghion, P. and Howitt, P. (2005) Growth with Quality-Improving Innovations: An Integrated Framework. In: Aghion, P. and Durlauf, S., Eds., Handbook of Economic Growth, Elsevier, Amsterdam, Vol. 1A, 67-110. https://doi.org/10.1016/S1574-0684(05)01002-6 |

[2] | Mulkay, B. and Mairesse, J. (2003) The Effect of the R&D Tax Credit in France. LEREPS and UNU-MERIT, Preliminary Draft. |

[3] | Arrow, K.J. (1962) Economic Welfare and the Allocation of Resources for Invention. In: Nelson, R.R., Ed., The Rate and Direction of Inventive Activity: Economic and Social Factors, Princeton University Press, Princeton, 609-625. https://doi.org/10.1515/9781400879762-024 |

[4] | Cohen, W.M. and Daniel, A. Levinthal, D.A. (1990) Absorptive Capacity: A New Perspective on Learning and Innovation. Special Issue: Technology, Organizations, and Innovation, 35, 128-152. https://doi.org/10.2307/2393553 |

[5] | Nadiri, M.I. (1993) Innovations and Technological Spillovers. NBER Working Paper No. 4423. https://doi.org/10.3386/w4423 |

[6] | Romer, P. (1990) Endogeneous Technological Changes. Journal of Political Economy, 98, S71-S102. https://doi.org/10.1086/261725 |

[7] |
Hyytinen, A. and Toivanen, O. (2005) Do Financial Constraints Hold Back Innovation and Growth? Evidence on the Role of Public Policy. Research Policy, 34, 1385-1403. https://doi.org/10.1016/j.respol.2005.06.004 |

[8] | Czarnitzki, D. (2005) Extent and Evolution of the Productivity Deficiency in Eastern Germany. Journal of Productivity Analysis, 24, 209-229. https://doi.org/10.1007/s11123-005-4706-0 |

[9] | Berger, P.G. (1993) Explicit and Implicit Tax Effects of the R&D Tax Credit. Journal of Accounting Research, 31, 131-171. https://doi.org/10.2307/2491268 |

[10] | Hall, B.H. (1993) Industrial Research During the 1980s: Did the Rate of Return Fall? Brookings Papers on Economic Activity, No. 2, 289-344. https://doi.org/10.2307/2534741 |

[11] | Herrera, L. and Heijs, J. (2007) Difusión y Adicionalidad de las AyudasPúblicas a la Innovación. Revista de Economía Aplicada, 15, 177-197. |

[12] | Criscuolo, C., Czarnitzki, D., Hambro, C. and Warda, J. (2009) Design and Evaluation of Tax Incentives for Business Research and Development: Good Practice and Future Development. Final Report Submitted by the Expert Group on Impacts of R&D Tax Incentives to the European Commission, Directorate General. |

[13] |
David, P.A., Hall, B.H. and Toole, A.A. (2000) Is Public R&D a Complement or Substitute for Private R&D? A Review of the Econometric Evidence. Research Policy, 29, 497-529. https://doi.org/10.1016/S0048-7333(99)00087-6 |

[14] |
David, P.A. and Hall, B.H. (2000) Heart of Darkness: Modelling Public-Private Interactions inside the R&D Black Box. Research Policy, 29, 1165-1183.
https://doi.org/10.1016/S0048-7333(00)00085-8 |

[15] | Hall, B.H. and van Reenen, J. (2000) How Effective Are Fiscal Incentives for R&D? A Review of the Evidence. Research Policy, 29, 449-469. https://doi.org/10.1016/S0048-7333(99)00085-2 |

[16] | Stanley, T. (2008) Meta-Regression Methods for Detecting and Estimating Empirical Effects in the Presence of Publication Selection. Oxford Bulletin of Economics and Statistic, 70, 103-127. |

[17] | Parsons, M. and Phillips, N. (2007) An Evaluation of the Federal Tax Credit for Scientific Research and Experimental Development. Department of Finance Working Paper 2007-08. |

[18] | Mohnen, P. and Lokshin, B. (2009) What Does It Take for an R&D Tax Incentive Policy to be Effective? CIRANO Scientific Series 2009s-11. https://doi.org/10.2139/ssrn.1499876 |

[19] | Hall, B.H., Jacques Mairesse, J. and Mohnen, P. (2009) Measuring the Returns to R&D. NBER Working Paper Series 15622. https://doi.org/10.3386/w15622 |

[20] | Yang, I.-H. (2011) The Effectiveness of Tax Credits as a Policy Tool to Promote R&D Activity: A Systematic Review and Meta-Regression Analysis. Dissertation, Auckland University of Technology, Auckland. |

[21] |
Doucouliagos, H. and Stanley, T.D. (2009) Publication Selection Bias in Minimum-Wage Research? A Meta-Regression Analysis. British Journal of Industrial Relations, 47, 406-428. https://doi.org/10.1111/j.1467-8543.2009.00723.x |

[22] | Efendic, A., Pugh, G. and Adnett, N. (2011) Confidence in Formal Institutions and Reliance on Informal Institutions in Bosnia and Herzegovina: An Empirical Investigation Using Survey Data. Economics of Transition, 19, 521-540. https://doi.org/10.1111/j.1468-0351.2010.00408.x |

[23] | Lipsey, M.W. and Wilson, D.B. (2001) Practical Meta-Analysis. SAGE, Thousand Oaks. |

[24] | Glass, G. (1976) Primary, Secondary, and Meta-Analysis of Research. Educational Researcher, 5, 3-8. https://doi.org/10.3102/0013189X005010003 |

[25] | Glass, G. (1977) Integrating Findings: The Meta-Analysis of Research. Review of Research in Education, 5, 351-379. https://doi.org/10.2307/1167179 |

[26] |
Stanley, T. and Jarell, S.B. (1989) Meta-Regression Analysis: A Quantitative Method of Literature Survey. Journal of Economic Surveys, 3, 161-170.
https://doi.org/10.1111/j.1467-6419.1989.tb00064.x |

[27] | Sutton, A.J., Duval, S.J., Tweedie, R.L., Abrams, K.R. and Jones, D.R. (2000) Empirical Assessment of Effect of Publication Bias on Meta-Analyses. British Medical Journal, 320, 1574-1577. https://doi.org/10.1136/bmj.320.7249.1574 |

[28] | Ashenfelter, O., Harmon, C. and Oosterbeek, H. (1999) A Review of Estimates of Schooling/Earnings Relationship, with Test for Publication Bias. Labour Economics, 6, 453-470. https://doi.org/10.1016/S0927-5371(99)00041-X |

[29] | Card, D. and Krueger, A.B. (1995) Time-Series Minimum-Wage Studies: A Meta-Analysis. American Economic Review, 85, 234-243. |

[30] |
Görg, H. and Strobl, E. (2001) Multinational Companies and Productivity Spillovers: A Meta-Analysis. Economic Journal, 111, F723-F740.
https://doi.org/10.1111/1468-0297.00669 |

[31] | Mookerjee, R. (1991) A Meta-Analysis of the Export Growth Hypothesis. Economics Letters, 91, 395-401. https://doi.org/10.1016/j.econlet.2005.12.020 |

[32] | Egger, M., Davey, S.G., Schneider, M. and Minder, C. (1997) Bias in Meta-Analysis Detected by a Simple Graphical Test. BMJ, 315, 629-634. https://doi.org/10.1136/bmj.315.7109.629 |

Journals Menu

Copyright © 2021 by authors and Scientific Research Publishing Inc.

This work and the related PDF file are licensed under a Creative Commons Attribution 4.0 International License.