Input-output impact analysis in current or constant prices: does it matter?
- Erik Dietzenbacher^{1}Email author and
- Umed Temurshoev^{1}
DOI: 10.1186/2193-2409-1-4
© Dietzenbacher and Temurshoev; licensee Springer. 2012
Received: 26 March 2012
Accepted: 27 April 2012
Published: 27 April 2012
Abstract
This paper addresses the question whether the results of input-output (IO) impact analyses differ (and to what extent) when a framework in current prices or in constant prices is used. We consider the effect of an exogenous stimulus of final demand in current prices on (a) gross output in constant prices, and (b) employment. In an empirical application to Denmark, we found that all predicted effects were very similar. This holds in particular for the results at the aggregate, economy-wide level and, to a lesser extent, at the sectoral level.
JEL Classification:C67, D57.
Keywords
input-output tables impact analysis current prices constant prices1 Introduction
Since the 1990s, physical input-output tables (PIOTs) that measure the deliveries of an industry in a single unit of mass have been compiled. In terms of appropriation of resources (e.g. water, energy, land) for final demand categories, the models based on PIOTs are an alternative to the models based on ordinary monetary input-output tables (MIOTs). Hubacek and Giljum ([2003]) were the first to compare the results for the two models. When calculating land appropriation for exports, they found substantial differences and claimed that the use of PIOTs was more appropriate. This triggered a lively discussion along two different lines. The first focused on the treatment of waste in the model based on PIOTs and was able to explain a part of the differences (see Giljum and Hubacek [2004]; Giljum et al. [2004]; Suh [2004]; Dietzenbacher [2005]; and Dietzenbacher et al. [2009]).
Still, the differences remained quite substantial. Using a highly aggregated 3-sector PIOT (in million tons) and MIOT (in billion DM) for Germany in 1990 (see Hubacek and Giljum [2003]), the land use (in 1,000 hectares) as embodied in exports was calculated. The percentage difference for the total land appropriation amounts to 6.4% (7,281.3 thousand hectares when the MIOT based model is used versus 6,845.8 when the PIOT based model is used). For the three underlying sectors, however, the results are quite dramatic. The percentage difference is 8.9% for the primary sector (MIOT: 6,339.3; PIOT: 5,822.4), 68.5% for the secondary sector (MIOT: 807.1; PIOT: 478.9) and −75.2% for the tertiary sector (MIOT: 134.9; PIOT: 544.5).
The second perspective was put forward in Weisz and Duchin ([2006]). They convincingly argue that the differences are caused by the fact that the two types of input-output (IO) tables cannot be ‘translated’ into each other by using a single price for all the deliveries of a given sector (or industry). Instead, deliveries from sector i to sector j have a different price than deliveries from sector i to sector k or to the final demand categories. They calculate that the implicit prices of commodity outputs (in DM per ton) range from 0.02 to 0.27 for the primary sector, from 0.67 to 3.80 for the secondary sector, and from 5.31 to 163.09 for the tertiary sector.
The same applies to IO tables in current and in constant prices. That is, sectors do not have a single price deflator that holds uniformly within a corresponding row of the IO table; rather, the intermediate deliveries require cell-specific deflators. This raises the question to what extent the results differ between using the model based on an IO table in current prices and the model based on an IO table in constant prices. The present paper addresses this question. In the next section, we will present the methods, one of which is novel. Section 3 discusses the results of an application using Denmark’s IO tables and Section 4 concludes.
2 Methods
The central question is whether the results of input-output (IO) impact analyses differ (and to what extent) when a framework in current prices or in constant prices is used. To deal with this issue, we consider the following two simple cases of calculating the effect of an exogenous stimulus of final demand in current prices (a) on gross output in constant prices, and (b) on employment. Because both current and constant prices are involved, we begin with a description of the two IO frameworks.
Input-output table in current prices.
Inputs | Final demand (incl gross exports) | Totals | |
---|---|---|---|
Domestic outputs | Z | f | x |
Imports | M | 0 | m |
Value added | ${\mathbf{v}}^{\prime}$ | 0 | v |
Totals | ${\mathbf{x}}^{\prime}$ | f |
The matrix $\mathbf{L}={(\mathbf{I}-\mathbf{A})}^{-1}$ is known as the Leontief inverse and its typical element ${l}_{ij}$ denotes the (additional) domestic production in dollars by sector i that is required to satisfy one (extra) dollar of final demand of product j.
The IO table in constant prices is exactly similar to Table 1, the only difference being that all flows are expressed in constant prices. To distinguish between the two types of money flows, we add a bar on the top of each matrix/vector to indicate that its elements give the constant price value. For example, the domestic intersectoral transaction matrix in constant prices is denoted by $\overline{\mathbf{Z}}$. Now assume that an analyst is interested in forecasting the values of gross outputs in constant prices and the corresponding levels of employment that are required for a new final demand ${\mathbf{f}}_{1}$ in current prices.
In an ideal IO world, we have that each sector i produces exactly one commodity that is sold at a single price. That is, the price of commodity i does not differ across buyers (i.e. any sector j or final demand categories such as consumers or the government). In that case we have a single vector p of deflators (which are the reciprocal of the price indexes) and $\overline{\mathbf{Z}}=\stackrel{\u02c6}{\mathbf{p}}\mathbf{Z}$, $\overline{\mathbf{x}}=\stackrel{\u02c6}{\mathbf{p}}\mathbf{x}$, and $\overline{\mathbf{f}}=\stackrel{\u02c6}{\mathbf{p}}\mathbf{f}$. For the matrix with input coefficients we have $\overline{\mathbf{A}}=\overline{\mathbf{Z}}{\stackrel{\u02c6}{\overline{\mathbf{x}}}}^{-1}=\stackrel{\u02c6}{\mathbf{p}}\mathbf{Z}{\stackrel{\u02c6}{\mathbf{x}}}^{-1}{\stackrel{\u02c6}{\mathbf{p}}}^{-1}=\stackrel{\u02c6}{\mathbf{p}}\mathbf{A}{\stackrel{\u02c6}{\mathbf{p}}}^{-1}$ and for the Leontief inverse $\overline{\mathbf{L}}={(\mathbf{I}-\overline{\mathbf{A}})}^{-1}={(\mathbf{I}-\stackrel{\u02c6}{\mathbf{p}}\mathbf{A}{\stackrel{\u02c6}{\mathbf{p}}}^{-1})}^{-1}=\stackrel{\u02c6}{\mathbf{p}}{(\mathbf{I}-\mathbf{A})}^{-1}{\stackrel{\u02c6}{\mathbf{p}}}^{-1}=\stackrel{\u02c6}{\mathbf{p}}\mathbf{L}{\stackrel{\u02c6}{\mathbf{p}}}^{-1}$. In solving the analyst’s problem from the previous paragraph, we may start from a new final demand vector ${\mathbf{f}}_{1}$ in current prices and first deflate it into $\stackrel{\u02c6}{\mathbf{p}}{\mathbf{f}}_{1}$, after which the constant price IO framework is applied so as to yield $\overline{\mathbf{L}}\stackrel{\u02c6}{\mathbf{p}}{\mathbf{f}}_{1}$. Alternatively, we may first calculate the current priced outputs required for ${\mathbf{f}}_{1}$ as $\mathbf{L}{\mathbf{f}}_{1}$, which are then deflated into $\stackrel{\u02c6}{\mathbf{p}}\mathbf{L}{\mathbf{f}}_{1}$. Because $\overline{\mathbf{L}}\stackrel{\u02c6}{\mathbf{p}}=(\stackrel{\u02c6}{\mathbf{p}}\mathbf{L}{\stackrel{\u02c6}{\mathbf{p}}}^{-1})\stackrel{\u02c6}{\mathbf{p}}=\stackrel{\u02c6}{\mathbf{p}}\mathbf{L}$, the two approaches always (i.e. for any vector ${\mathbf{f}}_{1}$) yield the same answer. This implies that in an ideal world it does not matter whether the final demand vector is deflated first and then the constant price IO model is used to calculate the outputs, or whether the current price model is used first to calculate the outputs which are then deflated.
However, real world cases are quite different. Neither do sectors produce a single commodity nor do all buyers of a particular commodity pay the same price. First, sectors are aggregates of establishments that produce different commodities, which implies that sectors sell baskets of commodities and the basket sold to sector j differs from the one sold to sector k. Due to the differences in the composition of the baskets, their prices will also be different. Second, the same commodity is often sold for prices that differ across buyers. As a consequence, deflators for the values in an IO table are typically cell-specific.
Next, we go back to the analyst’s problem of forecasting the gross output values in constant prices (and the corresponding employment levels) that are required for a new final demand ${\mathbf{f}}_{1}$ in current prices. The two approaches sketched above yield the following.
Option A (Deflation after gross output calculations in current prices)
Option B (Gross output calculations in constant prices after deflation of the final demands)
Now we have two estimates of gross outputs in constant prices, namely those given in Equations 4 and 7. However, as it is evident from the corresponding equations, these estimates are in general not equal to each other. They will be exactly equal for any final demand vector ${\mathbf{f}}_{1}$ if and only if ${\stackrel{\u02c6}{\mathbf{p}}}_{x}\mathbf{L}=\overline{\mathbf{L}}{\stackrel{\u02c6}{\mathbf{p}}}_{f}$ which does not hold in real world cases. Hence, the crucial issue to consider is the significance of differences between ${\overline{\mathbf{x}}}_{A}$ and ${\overline{\mathbf{x}}}_{B}$ both at the sectoral level and at the aggregate level (i.e. after summing over the sectors).
Using $\overline{\mathbf{x}}={\stackrel{\u02c6}{\mathbf{p}}}_{x}\mathbf{x}$ implies ${\overline{\mathit{\pi}}}^{\prime}={\mathbf{e}}^{\prime}{\stackrel{\u02c6}{\mathbf{x}}}^{-1}{\stackrel{\u02c6}{\mathbf{p}}}_{x}^{-1}={\mathit{\pi}}^{\prime}{\stackrel{\u02c6}{\mathbf{p}}}_{x}^{-1}$, so that Equation 8 can be rewritten as ${\mathbf{e}}_{B}=\stackrel{\u02c6}{\mathit{\pi}}{\stackrel{\u02c6}{\mathbf{p}}}_{x}^{-1}\overline{\mathbf{L}}{\stackrel{\u02c6}{\mathbf{p}}}_{f}{\mathbf{f}}_{1}$. Note that the estimates in Equations 2 and 8 are therefore exactly the same for any vector ${\mathbf{f}}_{1}$ if and only if $\mathbf{L}={\stackrel{\u02c6}{\mathbf{p}}}_{x}^{-1}\overline{\mathbf{L}}{\stackrel{\u02c6}{\mathbf{p}}}_{f}$. In other words, if and only if ${\stackrel{\u02c6}{\mathbf{p}}}_{x}\mathbf{L}=\overline{\mathbf{L}}{\stackrel{\u02c6}{\mathbf{p}}}_{f}$, which was also the necessary and sufficient condition for the equality of the gross outputs under the two options. Clearly, the two estimates in Equations 2 and 8 for employment will not match in general. Hence, it is of practical importance to find out what the size of the differences between ${\mathbf{e}}_{A}$ and ${\mathbf{e}}_{B}$ is.
Option C (Using cell-specific deflators)
We consider here another option that is feasible if IO data is available both in current and constant prices. The motivation for this method stems from the fact that deflators of observed IO tables are cell-specific. It has been well documented that a single deflator does not apply uniformly within a row of the IO table (see Statistics Canada [2001]). This is because a single commodity is sold for a different price to different buyers, and because sectors do not sell a single commodity but rather baskets of commodities and the composition of the baskets differs per buyer.
The proposed matching method consists of three steps. In the first step, the standard Leontief model in current prices (Equation 1) is used to derive the gross outputs vector ${\mathbf{x}}_{1}$ that is required for an exogenously specified final demand vector ${\mathbf{f}}_{1}$. In the second step, a new matrix of intermediate deliveries in current prices is calculated using the assumption that the domestic input matrix A is fixed. That is, ${\mathbf{Z}}_{1}={\mathbf{A}\stackrel{\u02c6}{\mathbf{x}}}_{1}$.
where ⊗ indicates the Hadamard product of element-wise multiplication.
To sum up, we have now three estimates for the gross outputs in constant prices and three employment forecasts. It should be noted that option A only requires an IO table in current prices and a vector of gross output deflators. Options B and C are more demanding in terms of data; they require the tables in current and constant prices to be available. Given the fact that in real world cases deflators do not apply uniformly within a row, option A seems to be the least preferred. Options B and C fully use the cell-specific deflators and are thus to be preferred if data is available.
The next section will empirically answer the question whether (and to what extent) the estimates differ from each other. We will consider the percentage differences of gross outputs and employment between the pair of methods, both at the sectoral and the total economy level. The following theorem shows that - at the sectoral level - the pairwise differences are exactly the same for gross outputs and employment (or any other factor of interest).
Theorem 1 Let${\mathrm{\Delta}}_{i}^{x}(j,k)=100\times ({\overline{x}}_{i}^{j}-{\overline{x}}_{i}^{k})/{\overline{x}}_{i}^{k}$and${\mathrm{\Delta}}_{i}^{e}(j,k)=100\times ({e}_{i}^{j}-{e}_{i}^{k})/{e}_{i}^{k}$be the percentage differences of, respectively, the gross output and employment estimates for sector i derived by methods j and k ($=A,B,C$). Then${\mathrm{\Delta}}_{i}^{x}(j,k)={\mathrm{\Delta}}_{i}^{e}(j,k)$holds for all i and all possible combinations of two different methods j and k.
Proof The possible pairs of methods are A and B, A and C, and B and C. Let us start with the last combination, i.e. $j=B$ and $k=C$. First, note that comparing ${\mathrm{\Delta}}_{i}^{x}(j,k)$ and ${\mathrm{\Delta}}_{i}^{e}(j,k)$ is equivalent to comparing the ratios of corresponding sectoral gross outputs and sectoral employment. Let // denote Hadamard element-wise division. Then using Equations 8 and 10 we easily obtain ${\mathbf{e}}_{B}//{\mathbf{e}}_{C}=\stackrel{\u02c6}{\overline{\mathit{\pi}}}{\overline{\mathbf{x}}}_{B}//\stackrel{\u02c6}{\overline{\mathit{\pi}}}{\overline{\mathbf{x}}}_{C}={\overline{\mathbf{x}}}_{B}//{\overline{\mathbf{x}}}_{C}$, which proves equivalence when methods B and C are compared.
Using Equations 1, 2, 4, 5 and 11, we derive that ${\mathbf{e}}_{B}//{\mathbf{e}}_{A}=\stackrel{\u02c6}{\overline{\mathit{\pi}}}{\overline{\mathbf{x}}}_{B}//\stackrel{\u02c6}{\mathit{\pi}}{\mathbf{x}}_{1}=\stackrel{\u02c6}{\overline{\mathit{\pi}}}{\overline{\mathbf{x}}}_{B}//\stackrel{\u02c6}{\overline{\mathit{\pi}}}{\stackrel{\u02c6}{\mathbf{p}}}_{x}{\mathbf{x}}_{1}=\stackrel{\u02c6}{\overline{\mathit{\pi}}}{\overline{\mathbf{x}}}_{B}//\stackrel{\u02c6}{\overline{\mathit{\pi}}}{\overline{\mathbf{x}}}_{A}={\overline{\mathbf{x}}}_{B}//{\overline{\mathbf{x}}}_{A}$. Going through similar steps proves that ${\mathbf{e}}_{C}//{\mathbf{e}}_{A}={\overline{\mathbf{x}}}_{C}//{\overline{\mathbf{x}}}_{A}$. □
The result above shows that the differences between the gross outputs of any two methods provide a complete picture at the sectoral level, because the differences between the employment forecasts (or any other factor) are the same. It should be noted that by working with percentage differences, we have implicitly assumed that the employment in each sector is positive. In case the employment in sector i is zero, we have that all forecasts for this sector are also zero (i.e. element i of the vectors ${\mathbf{e}}_{A}$, ${\mathbf{e}}_{B}$, and ${\mathbf{e}}_{C}$), which is an obvious result. Finally, it should be stressed that at the economy-wide level the percentage difference in overall gross outputs will - in general - not be equal to that in total employment estimates. For example, comparing methods B and C, we have for the ratio in total employment ${\mathbf{s}}^{\prime}{\mathbf{e}}_{B}/{\mathbf{s}}^{\prime}{\mathbf{e}}_{C}={\overline{\mathit{\pi}}}^{\prime}{\overline{\mathbf{x}}}_{B}/{\overline{\mathit{\pi}}}^{\prime}{\mathbf{x}}_{C}$, which generally differs from ${\mathbf{s}}^{\prime}{\mathbf{x}}_{B}/{\mathbf{s}}^{\prime}{\mathbf{x}}_{C}$, the ratio in overall gross outputs.
3 Empirical results
We use Danish input-output (IO) tables for the period of 2000-2007 that are available from Statistics Denmark at a 130-sector classification.^{4} These datasets distinguish between domestic and imported deliveries and their structure is given in Table 1. The unit of transactions is millions of Danish krones (DKK). We use the IO tables in current prices and in constant prices with the base year 2000. Further, the IO datasets are supplemented with tables showing employment figures (namely, the number of self-employed and employees, including people on a temporary leave of absence) for the 130 sectors.
Results of methods A, B and C for economy-wide gross output.
2001 | 2002 | 2003 | 2004 | 2005 | 2006 | 2007 | Mean | |
---|---|---|---|---|---|---|---|---|
Economy-wide gross output, n = 130 | ||||||||
(B − A)/A% | 0.011 | −0.033 | −0.007 | 0.012 | 0.002 | 0.006 | −0.009 | −0.002 |
(C − A)/A% | 0.008 | −0.022 | −0.002 | 0.012 | 0.001 | 0.001 | −0.010 | −0.002 |
(B − C)/C% | 0.003 | −0.011 | −0.005 | 0.000 | 0.001 | 0.005 | 0.002 | −0.001 |
Economy-wide gross output, n = 56 | ||||||||
(B − A)/A% | 0.028 | 0.026 | 0.042 | 0.033 | 0.001 | −0.009 | −0.005 | 0.017 |
(C − A)/A% | 0.022 | 0.023 | 0.038 | 0.028 | 0.000 | −0.008 | −0.010 | 0.013 |
(B − C)/C% | 0.006 | 0.004 | 0.004 | 0.006 | 0.001 | −0.001 | 0.006 | 0.003 |
Aggregation difference: ${|\mathrm{\Delta}\%|}_{n=56}-{|\mathrm{\Delta}\%|}_{n=130}$ | ||||||||
(B − A)/A% | 0.017 | −0.006 | 0.035 | 0.021 | −0.002 | 0.004 | −0.004 | 0.009 |
(C − A)/A% | 0.014 | 0.001 | 0.036 | 0.015 | −0.001 | 0.007 | 0.000 | 0.010 |
(B − C)/C% | 0.004 | −0.007 | −0.001 | 0.006 | −0.001 | −0.004 | 0.004 | 0.000 |
Table 2 clearly demonstrates that methods A, B and C provide essentially the same predictions of the economy-wide gross outputs. The reported percentage differences between the three methods are practically negligible. That is, on average, the values of overall outputs in constant prices differ from each other only by 0.001-0.002% when the number of sectors is 130. Intuitively speaking, one might expect that the further one is in time from the base year 2000, the larger the differences are. However, this is not the case, the differences vary over time without a clear pattern.
because $C/A$ is approximately 1 as follows from Table 2. If then $(B-C)/C$ is extremely close to 0, we have that $(B-A)/A$ approximately equals $(C-A)/A$. Second, recall that methods B and C both use the full matrix with cell-specific deflators, whereas option A only uses deflators for gross outputs and final demands.
Note that for the base year 2000, all three methods provide exactly the same outcomes since the current and constant priced IO data is exactly the same. Hence, the vectors of gross output deflators in Equation 3 and final demand deflators in Equation 6, and the matrix of intersectoral deflators P will consist only of ones. This implies that the vectors of predicted gross outputs in constant prices in Equations 4, 7 and 9, and employment vectors in Equations 2, 8 and 10 for methods A, B and C, respectively, exactly coincide.
Another observation is that the aggregation from 130 to 56 sectors tends to increase the percentage differences between the methods. Still, the largest difference between gross output projections is minimal (0.042%). So, from a practical view, aggregation from 130 to 56 sectors does not really change our conclusion. The average percentage differences ranged from 0.003 to 0.017% when 56 sectors were considered. Note that aggregation seems to affect the comparisons B-A and C-A, but not B-C. This is shown by the bottom part of Table 2 with changes (going from 130 to 56 sectors) in percentage differences. Larger changes are found for the comparisons B-A and C-A.
Results of methods A, B and C for economy-wide employment.
2001 | 2002 | 2003 | 2004 | 2005 | 2006 | 2007 | Mean | |
---|---|---|---|---|---|---|---|---|
Economy-wide employment, n = 130 | ||||||||
(B − A)/A% | 0.010 | −0.010 | 0.005 | 0.011 | −0.004 | −0.015 | −0.027 | −0.004 |
(C − A)/A% | 0.007 | −0.005 | 0.005 | 0.006 | −0.004 | −0.012 | −0.019 | −0.003 |
(B − C)/C% | 0.003 | −0.005 | 0.000 | 0.005 | 0.000 | −0.003 | −0.008 | −0.001 |
Economy-wide employment, n = 56 | ||||||||
(B − A)/A% | 0.005 | 0.000 | 0.007 | 0.022 | −0.005 | −0.012 | −0.007 | 0.001 |
(C − A)/A% | 0.002 | −0.001 | 0.004 | 0.013 | −0.004 | −0.008 | −0.005 | 0.000 |
(B − C)/C% | 0.003 | 0.002 | 0.003 | 0.009 | −0.001 | −0.005 | −0.002 | 0.001 |
Aggregation difference: ${|\mathrm{\Delta}\%|}_{n=56}-{|\mathrm{\Delta}\%|}_{n=130}$ | ||||||||
(B − A)/A% | −0.005 | −0.010 | 0.003 | 0.011 | 0.000 | −0.003 | −0.020 | −0.003 |
(C − A)/A% | −0.005 | −0.003 | −0.001 | 0.007 | 0.000 | −0.005 | −0.014 | −0.003 |
(B − C)/C% | 0.000 | −0.003 | 0.003 | 0.004 | 0.000 | 0.002 | −0.006 | 0.000 |
Results of methods A, B and C for sectoral gross outputs and sectoral employment.
2001 | 2002 | 2003 | 2004 | 2005 | 2006 | 2007 | Mean | |
---|---|---|---|---|---|---|---|---|
(B − A)/A%, n = 130 | ||||||||
Min | −1.278 | −2.562 | −1.586 | −0.862 | −0.588 | −1.215 | −1.708 | −1.400 |
Q1 | −0.006 | −0.031 | −0.013 | −0.005 | −0.010 | −0.018 | −0.038 | −0.017 |
Median | 0.002 | −0.006 | 0.000 | 0.003 | 0.001 | 0.000 | −0.001 | 0.000 |
Q3 | 0.011 | 0.006 | 0.013 | 0.024 | 0.022 | 0.030 | 0.035 | 0.020 |
Max | 0.472 | 0.307 | 0.348 | 0.635 | 0.520 | 1.747 | 3.297 | 1.046 |
(B − A)/A%, n = 56 | ||||||||
Min | −0.492 | −1.423 | −1.555 | −0.844 | −0.192 | −0.655 | −1.403 | −0.938 |
Q1 | −0.010 | −0.013 | −0.009 | 0.001 | −0.004 | −0.025 | −0.006 | −0.009 |
Median | 0.001 | −0.001 | 0.001 | 0.013 | 0.002 | −0.001 | 0.006 | 0.003 |
Q3 | 0.012 | 0.024 | 0.019 | 0.053 | 0.013 | 0.028 | 0.052 | 0.029 |
Max | 0.857 | 1.106 | 1.692 | 0.725 | 0.521 | 0.981 | 3.459 | 1.334 |
(C − A)/A%, n = 130 | ||||||||
Min | −1.321 | −2.542 | −1.565 | −0.850 | −0.584 | −1.090 | −1.395 | −1.335 |
Q1 | −0.010 | −0.021 | −0.011 | −0.008 | −0.005 | −0.014 | −0.020 | −0.013 |
Median | 0.000 | 0.000 | 0.000 | 0.000 | 0.001 | 0.000 | 0.000 | 0.000 |
Q3 | 0.007 | 0.011 | 0.014 | 0.017 | 0.020 | 0.022 | 0.028 | 0.017 |
Max | 0.463 | 0.303 | 0.346 | 0.632 | 0.490 | 1.679 | 3.280 | 1.028 |
(C − A)/A%, n = 56 | ||||||||
Min | −0.458 | −1.334 | −1.565 | −0.839 | −0.192 | −0.547 | −1.147 | −0.869 |
Q1 | −0.013 | −0.008 | −0.010 | −0.003 | −0.006 | −0.028 | −0.007 | −0.011 |
Median | 0.000 | 0.000 | −0.001 | 0.003 | 0.002 | 0.000 | 0.003 | 0.001 |
Q3 | 0.008 | 0.013 | 0.015 | 0.035 | 0.011 | 0.031 | 0.040 | 0.022 |
Max | 0.724 | 0.992 | 1.680 | 0.940 | 0.492 | 0.954 | 3.447 | 1.318 |
(B − C)/C%, n = 130 | ||||||||
Min | −0.055 | −0.255 | −0.214 | −0.279 | −0.071 | −0.270 | −0.409 | −0.222 |
Q1 | 0.000 | −0.010 | −0.002 | 0.000 | −0.002 | −0.005 | −0.007 | −0.004 |
Median | 0.002 | −0.003 | 0.000 | 0.003 | 0.000 | 0.000 | 0.000 | 0.000 |
Q3 | 0.006 | −0.001 | 0.001 | 0.009 | 0.002 | 0.006 | 0.005 | 0.004 |
Max | 0.070 | 0.063 | 0.069 | 0.110 | 0.123 | 0.575 | 0.868 | 0.268 |
(B − C)/C%, n = 56 | ||||||||
Min | −0.034 | −0.091 | −0.057 | −0.213 | −0.022 | −0.109 | −0.259 | −0.112 |
Q1 | 0.000 | −0.002 | 0.000 | 0.002 | −0.004 | −0.005 | −0.002 | −0.002 |
Median | 0.003 | 0.001 | 0.003 | 0.007 | −0.001 | −0.001 | 0.000 | 0.002 |
Q3 | 0.006 | 0.004 | 0.008 | 0.016 | 0.002 | 0.001 | 0.011 | 0.007 |
Max | 0.132 | 0.113 | 0.056 | 0.098 | 0.089 | 0.314 | 0.629 | 0.204 |
The results at the sectoral level show that the differences for certain sectors can be much larger indeed than those at the economy-wide level. The largest percentage differences are observed in all six panels of Table 4 (or boxplots of Figure 1) for 2007. For the original data ($n=130$), the largest difference between the results of methods A and B is 3.297%, while it is 3.280% for A-C and 0.868% for B-C. Similar findings hold for the aggregated data ($n=56$). All these major differences concern the estimates of the same sector, namely, Manufacture of office machinery and computers (code 300000). This sector produced 1,885 mln DKK in 2007, which equals only 0.0617% of the Danish economy-wide gross output in current prices for that year. The corresponding percentage for gross output in constant prices is 0.0941%. So, the largest differences at the sectoral level were found for a sector that was very small in terms of output.
A similar finding holds for some of the other years. Again, considering the original data ($n=130$), it turns out that Manufacture and distribution of gas (code 402000) is responsible for the largest deviation of the outcomes when comparing methods A-B and A-C for 2001, 2002, 2003 and 2006 (with the largest difference of −2.562% in 2002). The shares of this sector’s outputs in the overall gross outputs in current prices for these years are, respectively, 0.478, 0.388, 0.411 and 0.682%. The corresponding shares representing the constant price data are 0.484, 0.465, 0.4654 and 0.480%.
When taking the sectoral level into account, most differences between the methods are well below 1%. Methods B and C provide estimates of both gross output in constant prices and employment that are very close to each other again. The percentage differences range from −0.409 to 0.868%. For all the comparisons, we find that the outcomes when using aggregated data are very similar to those for the full 130-sector data. Summarizing, there are only few sectors for which the outcomes of the different methods show a difference in the range of 1.0-3.5% (these sectors are clear outliers in the boxplots of Figure 1). Moreover, these sectors contribute very little to the overall gross output. In all cases, their shares in gross output (both in current and constant prices) are well below 1%. This explains why, for the economy-wide level figures given in Tables 2 and 3, we found such very small differences between the predictions of the three methods.
Suppose now that one is concerned about the precision of sectoral predictions. That is, suppose a 2-3% difference is an issue even for sectors with a small contribution to the economy total output (or total employment). In that case, one might prefer methods B and C to method A. This is because the forecasts for B use a domestic input matrix that is already expressed in constant prices, while C uses cell-specific deflators to obtain an input matrix in constant prices. Apparently, from these two approaches, option B is slightly simpler to implement. Hence, in case IO data in constant prices is available, we recommend (on the base of our findings) to use option B. That is, first deflate the exogenously given final demand with the final demand deflators and use the IO data in constant prices to predict gross output and/or any other factor of interest through Equations 7 and 8.
On the basis of these sectoral results and the economy-wide differences provided in Tables 2 and 3, we may conclude that, on average, the three methods considered in this paper perform very, very similarly for most practical purposes. The simplest of the three options is method A, for which one does not need to have IO data in constant prices (including separate deflators for final demands). That is, one can simply use the standard Leontief model in current prices to predict the sectoral gross outputs (and/or any other factor of interest) as required for an exogenously specified final demand in current prices. The obtained gross outputs then need to be deflated with the widely available gross output deflators to find the gross output estimates in constant prices.
When analyzing the differences in results obtained when using a model based on a monetary IO table with a model based on a physical IO table, Weisz and Duchin ([2006]) called attention to the role of prices. They argue that the common assumption is that each sector applies a single price for all of its sales. If this assumption is approximately met, the results obtained from the two models may be expected to be similar. The same also applies for the models based on IO tables in current prices and in constant prices. That is, the finding that the three methods produce outcomes that are very close to each other may to a large extent be caused by the fact that the cell-specific deflators are very much the same within each sector. If that is the case, the columns of the matrix P and the vectors ${\mathbf{p}}_{x}$ and ${\mathbf{p}}_{f}$ are very similar.
Table 5 in the Appendix reports the descriptive statistics of deflators of intermediate inputs and final demand for each of 130 supplying sectors for Denmark. The year 2007 was chosen for this purpose as it is the furthest from the base year 2000. We find that for 97 sectors, the coefficient of variation (i.e. the ratio of the standard deviation and the mean) is less than 10%. For the interquartile range ($\mathrm{IQR}=\mathrm{Q}\mathrm{3}-\mathrm{Q}\mathrm{1}$), we find that 110 sectors have $\mathrm{IQR}<0.100$. This indicates that in 110 sectors, 50% of the sector’s prices fall in a range of 0.100 (which is a small range when compared to an overall average price around one). Only 5 sectors showed an interquartile range larger than 0.200. All in all, it seems to be the case that the cell-specific deflators are fairly similar within each sector.
At the same time, it should be emphasized that the prices show quite a number of outliers. For example, the prices range from 0.105 to 8.670 in sector 4 and from 0.388 to 31.009 in sector 27. Taking the ratio between the largest and the smallest observation for each sector, i.e. $\mathrm{Max}/\mathrm{Min}$, we find the following. For 37 sectors $\mathrm{Max}/\mathrm{Min}\ge 2.000$, in 10 of these sectors $\mathrm{Max}/\mathrm{Min}\ge 4.000$, and in 4 of these sectors we even find $\mathrm{Max}/\mathrm{Min}\ge 25.000$. In the present case, the outliers only play a marginal role because they typically are for deliveries with a small value and their effect is, thus, very small. This need not always be the case, however.
When the cell-specific deflators have a limited variability, the situation is close to the situation with a single vector p of deflators. As we have seen, in such a situation there simply is no difference between applying methods A and B (and C). This finding is consistent with the practice of constructing tables in constant prices by applying (an adapted form of) the double deflation method (see Dietzenbacher and Hoen [1998, 1999]).
4 Concluding remarks
In this paper we have investigated whether it matters for input-output (IO) impact analysis that the IO data is expressed in current or in constant prices. In particular, we calculated the amount of gross outputs in constant prices and employment as required for an exogenously specified vector of final demands in current prices. For this purpose we have compared three methods, all of which make use of the Leontief IO framework. These methods differed from each other in using IO data expressed: only in current prices, plus gross output deflators (A); in constant prices, plus final demand deflators (B); and in both current and constant prices to derive cell-specific price indices (C).
We found that all three methods essentially provide very similar predictions, for the economy-wide gross output and employment in particular. For such purposes, we recommend using the simplest method (A) which does not require the availability of IO data in constant prices. That is, use the standard Leontief method (based only on the IO data in current prices) to derive the estimates of gross outputs in current prices and other factors of interest (such as employment). The obtained gross outputs then need to be deflated by the widely available gross output deflators to find the corresponding outputs in constant prices.
Whenever IO data in constant prices is available, we recommend using approach B. That is, the vector of exogenously specified final demands in current prices first needs to be deflated by the corresponding final demand deflators (also available from various statistical dataset). Then the derived final demand stimulus vector in constant prices is used to predict the gross outputs in constant prices and any other factor using the IO framework in constant prices.
The methods A and B provided very similar results at the aggregate level, that is, in terms of total gross output or total employment. However, at the sectoral level the differences were somewhat larger (up to 3.5%) for sectors with a small contribution to the total gross output. Hence, if one is worried about such deviations, then option B is preferred, because the value of the intermediate deliveries between the sectors is already expressed in constant prices. Note that the aggregation of sectors (from 130 to 56) did not affect our findings.
Finally, we would like to raise three remarks, each indicating a potential direction for further research. First, all exercises in this paper used the average of the seven final demand vectors (i.e. averaged over 2001-2007) as the exogenously specified starting point. Of course, this implies that we have been working with a very specific final demand vector ${\mathbf{f}}_{1}$. Note that “size” does not matter for our exercise, in the sense that $k{\mathbf{f}}_{1}$ (for an arbitrary non-zero scalar k) would have resulted in exactly the same percentage differences between the methods. What does matter, however, and may influence the results is the sectoral mix of the final demands. A possibility for further investigation is not to rely on specific final demand vectors, but simply include any possibility. To this end, one should consider the full set of n ($=130,56$) unit vectors.^{5} This is because any vector can be written as a linear combination of the n unit vectors.
Second, Denmark was chosen because of data availability, but may of course be a very specific case. The results for other countries may be different. For example, for Denmark we found that there was only limited variability in the prices of each sector, which implies that methods A, B and C will generate similar results. At the same time, however, some clear outliers were observed. If these outliers occur for small deliveries, they will generate little effect. If such outliers had occurred for a few large deliveries, their influence might have been more pronounced. Clearly, this calls for an examination of a set of (preferably diverse) countries.
Third, in this paper we have restricted the aggregation to the case of $n=56$ sectors, obtained from the original 130 sectors. The reason is that further aggregation is not recommended from an economic viewpoint (although data availability often necessitates one to aggregate further). A much more detailed analysis of the effects of aggregation might be interesting though, because there are two opposing forces at work. On the one hand, suppose that there is a uniform price for each of the original sectors (but the uniform prices differ across the sectors). Aggregation implies that the deliveries of an aggregated sector are baskets of goods produced by the original sectors and that these baskets will have a different mix of goods for different buyers (see also de Mesnard and Dietzenbacher [1995]). Because the prices differ across the original sectors, the aggregated sectors are not likely to sell their products (i.e. baskets) at a uniform price. Aggregation may thus be expected to increase the discrepancies between the methods. On the other hand, if the prices of the original sectors exhibit outliers, aggregation may have a smoothening effect. In that case, the prices of some aggregated sectors may be more uniform than the original sectors and aggregation might reduce the discrepancies. An empirical analysis might provide an insight into the results of these two opposing forces at different levels of aggregation.
Appendix
Descriptive statistics of intermediate inputs and final demand deflators for each supplying sector (year 2007).
Sector | 1 | 2 | 3 | 4 | 5 | 6 | 7 | 8 | 9 | 10 | 11 | 12 | 13 |
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Min | 0.485 | 0.744 | 0.750 | 0.105 | 0.497 | 0.444 | 0.674 | 0.668 | 0.515 | 0.750 | 0.671 | 0.711 | 0.649 |
Q1 | 0.920 | 0.863 | 0.870 | 0.865 | 0.808 | 1.000 | 0.805 | 0.872 | 0.821 | 0.895 | 0.855 | 0.839 | 0.834 |
Median | 0.924 | 0.868 | 0.871 | 1.000 | 0.821 | 1.000 | 0.820 | 0.889 | 0.827 | 0.904 | 0.888 | 0.857 | 0.862 |
Q3 | 0.933 | 0.873 | 0.900 | 1.000 | 0.846 | 1.000 | 0.914 | 0.894 | 0.830 | 0.914 | 0.911 | 0.892 | 0.902 |
Max | 1.994 | 1.000 | 1.000 | 8.670 | 1.221 | 1.000 | 1.000 | 1.053 | 1.000 | 1.197 | 1.000 | 1.019 | 1.116 |
Mean | 0.974 | 0.869 | 0.895 | 1.002 | 0.841 | 0.988 | 0.846 | 0.879 | 0.820 | 0.914 | 0.875 | 0.866 | 0.876 |
Std | 0.204 | 0.024 | 0.059 | 0.791 | 0.097 | 0.073 | 0.059 | 0.051 | 0.051 | 0.065 | 0.056 | 0.048 | 0.067 |
CV | 0.209 | 0.028 | 0.066 | 0.790 | 0.116 | 0.074 | 0.069 | 0.058 | 0.062 | 0.071 | 0.063 | 0.055 | 0.077 |
Sector | 14 | 15 | 16 | 17 | 18 | 19 | 20 | 21 | 22 | 23 | 24 | 25 | 26 |
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Min | 0.228 | 0.500 | 0.805 | 0.564 | 0.747 | 0.796 | 0.854 | 0.875 | 0.678 | 0.849 | 0.734 | 0.706 | 0.793 |
Q1 | 0.870 | 0.809 | 1.226 | 0.879 | 0.753 | 0.866 | 0.923 | 0.927 | 0.748 | 0.942 | 0.927 | 1.098 | 1.038 |
Median | 0.875 | 0.809 | 1.239 | 0.881 | 0.753 | 0.903 | 0.926 | 0.927 | 0.836 | 0.952 | 0.984 | 1.134 | 1.103 |
Q3 | 0.879 | 0.811 | 1.245 | 0.884 | 0.753 | 0.922 | 0.929 | 0.927 | 0.885 | 0.968 | 1.084 | 1.146 | 1.147 |
Max | 1.000 | 1.000 | 1.996 | 1.000 | 1.000 | 1.095 | 1.079 | 1.242 | 5.593 | 1.046 | 1.312 | 1.402 | 1.281 |
Mean | 0.865 | 0.820 | 1.256 | 0.874 | 0.756 | 0.900 | 0.929 | 0.940 | 0.904 | 0.956 | 1.006 | 1.112 | 1.094 |
Std | 0.068 | 0.059 | 0.196 | 0.047 | 0.022 | 0.051 | 0.027 | 0.058 | 0.583 | 0.027 | 0.116 | 0.094 | 0.096 |
CV | 0.078 | 0.071 | 0.156 | 0.053 | 0.029 | 0.056 | 0.029 | 0.062 | 0.645 | 0.028 | 0.116 | 0.084 | 0.088 |
Sector | 27 | 28 | 29 | 30 | 31 | 32 | 33 | 34 | 35 | 36 | 37 | 38 | 39 |
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Min | 0.388 | 0.800 | 0.592 | 0.740 | 0.706 | 0.539 | 0.774 | 0.782 | 0.603 | 0.820 | 0.776 | 0.795 | 0.754 |
Q1 | 0.733 | 0.818 | 0.817 | 1.000 | 0.799 | 0.777 | 0.801 | 1.199 | 0.854 | 0.868 | 0.848 | 0.887 | 0.914 |
Median | 0.788 | 0.841 | 0.819 | 1.000 | 0.816 | 0.777 | 0.808 | 1.416 | 0.874 | 0.877 | 0.867 | 0.892 | 0.940 |
Q3 | 0.895 | 0.884 | 0.883 | 1.000 | 0.844 | 0.848 | 0.850 | 1.434 | 0.920 | 0.883 | 0.878 | 0.901 | 0.950 |
Max | 31.009 | 1.116 | 1.209 | 1.000 | 1.180 | 1.098 | 1.000 | 1.445 | 1.129 | 1.000 | 1.354 | 1.239 | 1.304 |
Mean | 1.298 | 0.860 | 0.864 | 0.961 | 0.824 | 0.814 | 0.830 | 1.296 | 0.890 | 0.880 | 0.872 | 0.898 | 0.930 |
Std | 3.098 | 0.057 | 0.088 | 0.093 | 0.069 | 0.094 | 0.046 | 0.192 | 0.068 | 0.024 | 0.060 | 0.045 | 0.074 |
CV | 2.387 | 0.067 | 0.102 | 0.097 | 0.083 | 0.115 | 0.055 | 0.148 | 0.076 | 0.027 | 0.069 | 0.050 | 0.079 |
Sector | 40 | 41 | 42 | 43 | 44 | 45 | 46 | 47 | 48 | 49 | 50 | 51 | 52 |
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Min | 0.674 | 0.744 | 0.381 | 0.423 | 0.631 | 0.700 | 0.463 | 0.518 | 0.418 | 0.676 | 0.774 | 0.728 | 0.422 |
Q1 | 0.806 | 0.866 | 0.798 | 0.752 | 0.793 | 0.801 | 0.806 | 0.820 | 0.804 | 0.909 | 0.935 | 0.886 | 0.882 |
Median | 0.806 | 0.901 | 0.881 | 0.804 | 0.863 | 0.915 | 0.851 | 0.869 | 0.806 | 0.927 | 0.938 | 0.924 | 0.940 |
Q3 | 0.806 | 0.924 | 0.896 | 0.840 | 0.873 | 0.927 | 0.854 | 0.892 | 0.827 | 0.932 | 0.939 | 0.934 | 0.943 |
Max | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.107 | 1.000 | 1.000 | 1.000 | 1.080 | 1.134 |
Mean | 0.809 | 0.892 | 0.817 | 0.792 | 0.832 | 0.872 | 0.831 | 0.861 | 0.816 | 0.913 | 0.930 | 0.909 | 0.906 |
Std | 0.058 | 0.041 | 0.132 | 0.070 | 0.078 | 0.070 | 0.052 | 0.060 | 0.063 | 0.039 | 0.025 | 0.059 | 0.088 |
CV | 0.072 | 0.046 | 0.161 | 0.088 | 0.093 | 0.080 | 0.063 | 0.070 | 0.077 | 0.043 | 0.027 | 0.064 | 0.097 |
Sector | 53 | 54 | 55 | 56 | 57 | 58 | 59 | 60 | 61 | 62 | 63 | 64 | 65 |
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Min | 0.840 | 0.735 | 0.754 | 0.711 | 0.406 | 0.670 | 0.792 | 0.704 | 0.755 | 0.847 | 0.464 | 0.317 | 0.067 |
Q1 | 0.851 | 0.912 | 0.952 | 0.881 | 0.914 | 0.918 | 0.927 | 0.848 | 0.890 | 0.848 | 0.519 | 0.635 | 0.894 |
Median | 0.852 | 0.931 | 0.953 | 0.916 | 0.931 | 0.920 | 0.937 | 0.915 | 0.928 | 0.848 | 0.559 | 1.000 | 0.894 |
Q3 | 0.885 | 0.935 | 0.971 | 0.938 | 0.937 | 0.920 | 0.939 | 0.927 | 0.932 | 0.848 | 0.820 | 1.114 | 1.000 |
Max | 1.529 | 1.063 | 1.745 | 1.354 | 1.000 | 1.000 | 1.402 | 4.959 | 1.000 | 1.000 | 1.578 | 1.663 | 4.810 |
Mean | 0.901 | 0.921 | 0.967 | 0.916 | 0.914 | 0.907 | 0.932 | 0.955 | 0.910 | 0.849 | 0.693 | 0.901 | 0.996 |
Std | 0.124 | 0.042 | 0.094 | 0.070 | 0.060 | 0.045 | 0.049 | 0.424 | 0.043 | 0.013 | 0.227 | 0.261 | 0.491 |
CV | 0.138 | 0.046 | 0.098 | 0.076 | 0.065 | 0.050 | 0.053 | 0.444 | 0.047 | 0.016 | 0.328 | 0.290 | 0.493 |
Sector | 66 | 67 | 68 | 69 | 70 | 71 | 72 | 73 | 74 | 75 | 76 | 77 | 78 |
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Min | 0.720 | 0.833 | 0.779 | 0.775 | 0.790 | 0.743 | 0.818 | 0.556 | 0.449 | 0.728 | 0.777 | 0.692 | 0.527 |
Q1 | 0.726 | 1.000 | 0.779 | 0.787 | 0.813 | 0.819 | 0.836 | 0.808 | 0.749 | 0.823 | 0.941 | 0.931 | 0.960 |
Median | 0.726 | 1.000 | 0.779 | 0.797 | 0.813 | 0.850 | 0.836 | 0.889 | 0.845 | 0.857 | 1.003 | 0.965 | 0.960 |
Q3 | 0.726 | 1.000 | 0.779 | 0.835 | 0.813 | 0.888 | 0.836 | 1.004 | 0.897 | 0.899 | 1.035 | 1.007 | 0.960 |
Max | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.902 | 1.000 | 2.611 | 1.085 | 1.818 | 2.266 | 17.723 | 1.787 |
Mean | 0.735 | 0.999 | 0.785 | 0.812 | 0.817 | 0.873 | 0.838 | 0.936 | 0.829 | 0.866 | 0.997 | 1.103 | 0.945 |
Std | 0.047 | 0.015 | 0.033 | 0.035 | 0.028 | 0.122 | 0.020 | 0.247 | 0.110 | 0.111 | 0.140 | 1.466 | 0.097 |
CV | 0.064 | 0.015 | 0.043 | 0.043 | 0.035 | 0.140 | 0.024 | 0.263 | 0.133 | 0.128 | 0.140 | 1.329 | 0.103 |
Sector | 79 | 80 | 81 | 82 | 83 | 84 | 85 | 86 | 87 | 88 | 89 | 90 | 91 |
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Min | 0.782 | 0.781 | 0.818 | 0.837 | 0.674 | 0.521 | 0.765 | 0.714 | 0.812 | 0.707 | 0.793 | 0.814 | 0.964 |
Q1 | 0.891 | 0.825 | 0.839 | 0.842 | 0.679 | 0.738 | 0.781 | 0.727 | 0.895 | 0.852 | 0.795 | 1.002 | 1.238 |
Median | 0.953 | 0.825 | 0.839 | 0.859 | 0.679 | 0.740 | 0.782 | 0.727 | 0.920 | 0.868 | 0.795 | 1.116 | 1.316 |
Q3 | 1.016 | 0.825 | 0.842 | 0.906 | 0.679 | 0.744 | 0.785 | 0.727 | 0.941 | 0.890 | 1.000 | 1.162 | 1.373 |
Max | 1.786 | 1.000 | 1.000 | 1.035 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.205 | 1.000 | 1.314 | 1.518 |
Mean | 0.957 | 0.826 | 0.844 | 0.884 | 0.682 | 0.741 | 0.788 | 0.748 | 0.917 | 0.879 | 0.862 | 1.087 | 1.289 |
Std | 0.109 | 0.020 | 0.021 | 0.055 | 0.028 | 0.036 | 0.027 | 0.072 | 0.035 | 0.053 | 0.097 | 0.109 | 0.127 |
CV | 0.114 | 0.024 | 0.025 | 0.062 | 0.041 | 0.048 | 0.035 | 0.096 | 0.038 | 0.060 | 0.112 | 0.100 | 0.098 |
Sector | 92 | 93 | 94 | 95 | 96 | 97 | 98 | 99 | 100 | 101 | 102 | 103 | 104 |
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Min | 0.913 | 1.000 | 1.000 | 0.911 | 0.381 | 0.815 | 0.862 | 0.874 | 0.821 | 0.994 | 0.796 | 0.800 | 0.821 |
Q1 | 1.126 | 1.000 | 1.074 | 0.914 | 0.382 | 1.000 | 0.863 | 0.962 | 0.948 | 0.999 | 0.798 | 0.856 | 0.830 |
Median | 1.259 | 1.000 | 1.076 | 0.915 | 0.382 | 1.000 | 0.863 | 1.037 | 0.985 | 1.000 | 1.000 | 0.857 | 0.830 |
Q3 | 1.330 | 1.000 | 1.078 | 0.918 | 0.382 | 1.000 | 0.863 | 1.101 | 0.999 | 1.001 | 1.000 | 0.859 | 0.830 |
Max | 1.506 | 1.073 | 1.085 | 1.000 | 1.000 | 1.000 | 1.000 | 1.739 | 1.011 | 1.005 | 2.303 | 1.000 | 1.989 |
Mean | 1.229 | 1.001 | 1.074 | 0.919 | 0.387 | 0.999 | 0.869 | 1.037 | 0.968 | 1.000 | 1.128 | 0.868 | 0.841 |
Std | 0.148 | 0.009 | 0.012 | 0.017 | 0.054 | 0.016 | 0.027 | 0.119 | 0.042 | 0.002 | 0.484 | 0.040 | 0.103 |
CV | 0.120 | 0.009 | 0.011 | 0.018 | 0.140 | 0.016 | 0.031 | 0.115 | 0.044 | 0.002 | 0.429 | 0.046 | 0.123 |
Sector | 105 | 106 | 107 | 108 | 109 | 110 | 111 | 112 | 113 | 114 | 115 | 116 | 117 |
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Min | 0.762 | 0.749 | 1.000 | 0.777 | 0.780 | 0.826 | 0.829 | 0.750 | 0.762 | 0.826 | 0.814 | 0.818 | 0.500 |
Q1 | 0.762 | 0.790 | 1.169 | 0.791 | 0.793 | 0.846 | 0.838 | 0.874 | 0.782 | 1.000 | 1.000 | 0.859 | 0.662 |
Median | 0.762 | 0.795 | 1.171 | 0.792 | 0.796 | 0.846 | 0.838 | 0.875 | 0.811 | 1.000 | 1.000 | 0.859 | 0.662 |
Q3 | 0.762 | 0.821 | 1.172 | 0.793 | 0.798 | 0.847 | 0.839 | 0.875 | 0.841 | 1.000 | 1.000 | 0.859 | 0.663 |
Max | 1.000 | 1.000 | 2.048 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.992 |
Mean | 0.766 | 0.810 | 1.172 | 0.796 | 0.799 | 0.853 | 0.855 | 0.877 | 0.815 | 0.971 | 0.969 | 0.870 | 0.772 |
Std | 0.029 | 0.034 | 0.083 | 0.023 | 0.025 | 0.030 | 0.040 | 0.025 | 0.041 | 0.064 | 0.068 | 0.040 | 0.327 |
CV | 0.038 | 0.041 | 0.070 | 0.029 | 0.031 | 0.035 | 0.047 | 0.028 | 0.050 | 0.065 | 0.071 | 0.046 | 0.423 |
Sector | 118 | 119 | 120 | 121 | 122 | 123 | 124 | 125 | 126 | 127 | 128 | 129 | 130 |
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Min | 0.839 | 0.823 | 0.726 | 0.818 | 0.826 | 0.685 | 0.781 | 0.778 | 0.821 | 0.654 | 0.844 | 0.769 | 0.775 |
Q1 | 0.854 | 1.000 | 0.903 | 1.000 | 1.000 | 0.693 | 0.782 | 0.782 | 0.823 | 0.787 | 1.000 | 0.878 | 1.000 |
Median | 0.854 | 1.000 | 0.905 | 1.000 | 1.000 | 0.698 | 0.782 | 0.782 | 0.823 | 0.787 | 1.000 | 0.882 | 1.000 |
Q3 | 0.855 | 1.000 | 0.905 | 1.000 | 1.000 | 0.707 | 0.782 | 0.782 | 0.823 | 0.976 | 1.000 | 0.883 | 1.000 |
Max | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.000 | 1.902 | 1.000 | 1.000 | 1.000 |
Mean | 0.859 | 0.974 | 0.888 | 0.969 | 0.971 | 0.705 | 0.797 | 0.802 | 0.826 | 0.939 | 0.981 | 0.876 | 0.998 |
Std | 0.028 | 0.056 | 0.037 | 0.067 | 0.062 | 0.038 | 0.055 | 0.063 | 0.022 | 0.284 | 0.041 | 0.024 | 0.020 |
CV | 0.033 | 0.058 | 0.042 | 0.069 | 0.064 | 0.054 | 0.070 | 0.079 | 0.027 | 0.303 | 0.041 | 0.028 | 0.020 |
Matrices are given in bold, capital letters; vectors in bold, lower case letters; and scalars in italicized, lower case letters. Vectors are columns by definition, row vectors are obtained by transposition, indicated by a prime. $\stackrel{\u02c6}{\mathbf{x}}$ is a diagonal matrix with the elements of vector x along its main diagonal and zeros elsewhere.
It should be stressed that it is not necessary for the full import matrix to be given. Some countries only publish the row vector that consists of the column sums of M. This does not affect our analysis.
For example, the EU KLEMS dataset (http://www.euklems.net) provides price indices of gross outputs and intermediate inputs at the industry level, from which the price indices of final demands can be easily computed.
Declarations
Acknowledgements
We gratefully acknowledge financial support provided by EU FP7 WIOD project. This project is funded by the European Commission, Research Directorate General as part of the 7th Framework Programme, Theme 8: Socio-Economic Sciences and Humanities. Grant Agreement no: 225 281, http://www.wiod.org.
Authors’ Affiliations
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