Abstract
In this work, we test the employment impact of distinct types of innovative investments using a representative sample of Spanish manufacturing firms over the period 2002–2013. Our GMM-SYS estimates generate various results, which are partially in contrast with the extant literature. Indeed, estimations carried out on the entire sample do not provide statistically significant evidence of the expected labor-friendly nature of innovation. More in detail, neither R&D nor investment in innovative machineries and equipment (the so-called embodied technological change, ETC) turn out to have any significant employment effect. However, the job-creation impact of R&D expenditures becomes highly significant when the focus is limited to the high-tech firms. On the other hand - and interestingly - ETC exhibits its labor-saving nature when SMEs are singled out.
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Notes
See The Guardian, January 5th, 2017.
A different perspective is opened by Aldieri and Vinci (2018), providing empirical evidence that financial shocks and economic crises may actually amplify the possible labor-saving impact of innovation.
However, this result can be due to the discrete nature of the adopted measure of process and product innovation (dummy variables). Interestingly enough, once the authors restrict their attention to (important) product innovation which went along with patent applications, they found out a highly positive and significant employment effect.
While Section 2.1 has focused on studies based on firm-level data (as the one used in this paper), analyses conducted at the sectoral level provide consistent results, with the labor-friendly impact of innovation - in most cases proxied by R&D expenditures - limited to the high-tech sectors (see Bogliacino and Pianta 2010; Bogliacino and Vivarelli 2012; Piva and Vivarelli 2018).
The only notable exception is the already mentioned recent article by Barbieri et al. (2019), where the Authors use four Italian CIS innovation surveys to assess the impact of R&D expenditures and ETC (defined as the innovative expenditures devoted to the acquisition of machinery, equipment and software, excluding expenditures on equipment for R&D) on employment. Differently from this study, data limitations (both in terms of lack of a proper longitudinal dimension and of paucity of observations, namely 892) have prevented the Authors to perform a proper panel estimation of a dynamic and augmented demand for labor as the one proposed in eq.(2) in the present paper.
Averaging the Community Innovation Surveys (CIS) all across European countries and sectors, the mean outcome is that about 50% of innovation inputs can be accounted for R&D while the rest for ETC; obviously enough, these proportions change across countries and sectors.
ETC is generally very difficult to measure because of the complexity in singling out the two different components of capital formation (that one characterized by standard technologies and that one characterized by ETC incorporating new technologies). In this context, disentangling ETC is one of the novel contributions of this study (see Section 3.2).
This broader perspective is also endorsed in methodological advice as to the collection of data regarding innovation; in particular, this is well represented by the shift from the R&D-focused Frascati Manual (“Guidelines for the collection of R&D data”, first published in 2015) to the Oslo Manual in the 1990s (OECD, 1st edn. 2018).
Obviously enough, the distinction between product and process innovation is often ambiguous from an empirical point of view (see, for instance, the diffusion of computers and telecommunication devices) and in many cases the two forms of innovation are strictly interrelated. However, from a theoretical point of view, we can conclude that two are the innovative inputs and two are the innovative outputs, with R&D mainly (but not only) related to product innovation and ETC mainly (but not only) related to process innovation.
GMM-SYS requires that T is, at least, equals to 3.
NACE is the usual industrial classification of economic activities within the European Union while CLIO is the nomenclature used by the Spanish input–output tables. The Spanish Accounting Economic System (Spanish National Statistics Institute: http://www.ine.es/) officially recognizes both classifications.
As a consequence, our final sample does include zero values both with regard R&D and ETC; this means that discontinuous and occasional innovators are considered in our analysis and participate to generate the obtained results.
Specifically, information provided in current prices in the ESEE database were converted into constant prices by using sectoral GDP deflators (source: INE-Spanish National Statistics Institute) centered on the year 2010.
The average R&D intensities (computed as R&D/VA ratios) are respectively 5.68% for the high-tech, 2.00% for the low-tech, 3.26% for the large and 1.42% for the small firms. The average ETC intensities (computed as ETC/VA ratios) are respectively 0.6% for the high-tech, 1.97% for the low-tech, 1.6% for the large and 0.93% for the small firms.
Notice that in the following tables the GMM-SYS estimated coefficients for the lagged dependent variable always turn out within the upper bound given by the corresponding POLS estimated coefficients and the lower bound given by the FE estimated coefficients; these outcomes strongly support the chosen methodology (see Bond 2002).
Moreover, a battery of differenced Hansen tests has been run to test the alternative ways to instrument the various variables (available upon request). In the preferred specification, the lagged dependent variable and the investment variable have been considered endogenous. In addition, in the Appendix, a summary table (Table 8) with a lower number of instruments to test for robustness for severely reducing the instrument count (instruments including lags from two to four when AR(2) is not rejected and from three to four when AR(2) is rejected) is reported, as suggested by Roodman (2009). As can be seen, results from Tables 5, 6, and 7 are confirmed.
For sake of space, single results for the time dummies are not reported in the Tables, but are available upon request.
The correlation coefficient between Value added and Investment in physical capital turned out to be as high as 0.78. To mitigate possible multicollinearity issues, we decided to lag the Investment variable, as well (the correlation coefficient dropping to 0.35).
As a robustness check, we tested specification (2) using stocks (instead of flows) for the investment, ETC and R&D variables. Stocks were computed through the perpetual inventory method, assuming an obsolescence rate of 6% for investment and ETC and 15% for R&D, as common in the literature. Results are consistent with those reported in Table 5 and are available upon request.
Control variables have the expected signs both in high-tech and low-tech firms. No relevant differences emerge in the magnitude of coefficients, with the exception of the cost of labor which affects employment more in high-tech companies than in low-tech ones (−0.284 vs. -0.236). This may suggest that more qualified and expensive workers are employed in the high-tech sectors.
The chosen size threshold is 200 employees, very close to the size median of our sample (199) and allowing a good balance between the two estimates (1,233 observations vs 1,171).
As in the previous estimates, control variables have the expected signs both in large and small firms. However, employment in small firms reveals to be positively and significantly affected by capital formation and more sensitive to the cost of labor.
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Pellegrino, G., Piva, M. & Vivarelli, M. Beyond R&D: the role of embodied technological change in affecting employment. J Evol Econ 29, 1151–1171 (2019). https://doi.org/10.1007/s00191-019-00635-w
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DOI: https://doi.org/10.1007/s00191-019-00635-w