Abstract
This paper develops limited and full information estimators for a simultaneous panel data model with spatial lags on the dependent variables and spatially autocorrelated error processes in the form of spatial autoregressive or spatial moving average processes. The spatial error components are estimated with various generalized moment procedures. Monte Carlo experiments show that the proposed estimators outperform traditional estimators and also provide results on the impact of misspecifying the error process. We illustrate the various estimators on an empirical example pertaining to competition in current and capital expenditure between French municipalities in the capital region of Ile-de-France.
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Data availability
Simulations and estimations are done by the authors with R program. Codes are available upon request. Data are also available upon request.
Notes
A list of frequently used notations is provided in Appendix A.1 for easy reference.
The weight \(\omega _{ij}\) represents the proximity between cross-sectional units i and j. The notion of proximity is not limited to the geographical sense. Indeed, it can be economic, technology, or social proximity, although endogeneity issues might arise when dealing with non-geographic weight matrices.
Note that since \({\textbf{A}}\) is assumed to be diagonal, the specification relates the disturbance vector in the l-th equation only to its own spatial lag. Allowing \({\textbf{A}}\) to be nondiagonal is beyond the scope of our paper.
Matrices \(Q_0\) and \(Q_1\) are standard transformation matrices used in the error component literature, with the appropriate adjustments implied by our adopted ordering of the data; compared to, e.g., Baltagi (2008). They are symmetric, idempotent and orthogonal to each other. Furthermore, \(Q_0+Q_1=I_{nT}\) and \(\text {tr}(Q_{nT,h})=n(T-1)^{1-h}\).
The limited GMM is obtained by considering each equation separately. This estimator is the same as the one proposed by Lee (2007b).
We follow Kelejian and Prucha (1998) and compute the adjusted \(\text {RMSE}^*({\hat{\lambda }}_k) =\left[ \text {bias}^2({\hat{\lambda }}_k) + \left( {\text {IQ}({\hat{\lambda }}_k)} /{1.35}\right) ^2\right] ^{1/2}\), where median is used instead of mean for bias. \(\text {IQ}\) is the inter-quartile range and \({\hat{\lambda }}_k\) is the estimator of kth parameter \(\lambda _k\).
Here, we used the comprehensive criteria proposed by Sasser (1969): \(\text {NOMAD}({\hat{\lambda }})=\frac{1}{RK}\sum _{k=1}^K\sum _{r=1}^R\left| \frac{{\hat{\lambda }}_{k,r}-\lambda _k}{\lambda _k}\right| \) where K is the number of parameters, R is the number of replications, \({\hat{\lambda }}_{k,r}\) is the estimator of kth parameter in rth replication.
The results obtained with the SMA specification are available upon request.
The départements are the middle-tier level of local governments in France.
Note that for \(m=0\), \([\text {E}(W_{nT}y_1),\ldots ,\text {E}(W_{nT}y_{m}),{\textbf{X}}]={\textbf{X}}\) by convention.
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A Appendix
A Appendix
1.1 A.1 Notations
The following list summarizes some frequently used notations in either the text or the Appendices:
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\(A^\top \) is the transpose operator for any \(m\times n\) matrix A.
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\(\text {E}(A)\) is the expected value of any input \(m\times n\) random matrix A.
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\(\text {tr}(A)=\sum _{i=1}^ma_{ii}\) is the sum of diagonal elements for any \(m\times m\) matrix A.
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For a \(n\times m\) matrix B the vectorization is denoted \(\text {vec}(B)=\big (b_{11},\ldots ,b_{n1},\ldots ,b_{1m},\ldots ,b_{nm}\big )\)
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If A, B and C are conformable matrices, then \(\text {vec}(ABC)= (C^\top \otimes A)\text {vec}(B)\).
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For any vector \(\textbf{a}\) of order n and \(\forall k\in {\mathbb {N}}\), let \(\overset{k}{\bar{\textbf{a}}}=M_n^k\textbf{a}\). This means that: a) for \(k=0\), \(\overset{0}{\bar{\textbf{a}}}={\textbf{a}}\); b) for \(k=1\), \(\overset{1}{\bar{\textbf{a}}}=\bar{\textbf{a}}\); and for \(k=2\), \(\overset{2}{\bar{{\textbf{a}}}}=M\bar{{\textbf{a}}}=\bar{\bar{{\textbf{a}}}}\).
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Let \(\upsilon _l\) and \(\upsilon _q\) be \(n\times 1\) vectors of spatial processes; \(\forall a,b\in {\mathbb {N}}\), \(\gamma ^{lq,h}_{ab} = {\overset{a}{{\bar{\upsilon }}}^{\top }_lQ_{nT,h}\overset{b}{{\bar{\upsilon }}}_q}/{\text {tr}\left( Q_{nT,h}\right) }.\)
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For any spatial matrix \(M_n\) of order n and \(\forall a,b\in {\mathbb {N}}\), let \(\phi _{ab}=\phi _{ba}=\frac{1}{n}\text {tr}\left( M^{\top {a}}_{n}M^b_{n}\right) \). This means that \(\phi _{00}=1\) and \(\phi _{01}=\phi _{10}=0\).
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Let \(A=[a_{ij}]\) and \(B=[b_{ij}]\) be \(n\times n\) nonstochastic matrices with zero diagonals. Let \(\epsilon _1\), \(\epsilon _2\), \(\epsilon _3\) and \(\epsilon _4\) be \(n\times 1\) vectors of independent, centered random variables. Let \(\Sigma _{lq}=\text {E}(\epsilon _l\epsilon _q^\top )\) for \(l,q=1,2,3,4\). Then, \(\text {E}(\epsilon _1^\top A\epsilon _2\epsilon _3^\top B\epsilon _4)=\text {tr}(\Sigma _{13}A\Sigma _{24}B^\top ) + \text {tr}(\Sigma _{14}A\Sigma _{23}B)\). See Liu and Saraiva (2019)
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Let \(A=[a_{ij}]\) be a \(n\times n\) nonstochastic matrix with zero diagonals and \(\textbf{c}=[c_{1},\ldots ,c_L]\) be a \(n\times 1\) nonstochastic vector. Let \(\epsilon _1\), \(\epsilon _2\) and \(\epsilon _3\) be \(n\times 1\) vectors of independents, centered random variables. Then, \(\text {E}(\epsilon _1^\top A\epsilon _2\epsilon _3^\top \textbf{c}) = 0\)
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\(\text {diag}(A_n)=\text {diag}(a_{11},a_{22},\ldots ,a_{nn})\) is a diagonal \(n\times n\) matrix from a square matrix A of order n.
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\(\text {diag}_{h=1}^p(A_{n,h})\equiv \text {diag}_{h}(A_{n,h})= \text {diag}(A_{n,1},\ldots ,A_{n,p})\) is a block diagonal \(np\times np\) matrix.
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\(I_n\) is an identity matrix of order n.
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\(\iota _n\) is a \(n\times 1\) vector of ones with \(n\in \mathbb {N}^*\).
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\(\Lambda _\lambda =\text {diag}_l(\Lambda _{nT}(\lambda _l))\), where \(\Lambda _{nT}(\lambda _l)=I_{T}\otimes \Lambda _n(\lambda _l)\); with \(\Lambda _n(\lambda _l)=(I_{n}-\lambda _l W_{n})^{-1}\) for SAR case or \(\Lambda _n(\lambda _l)=(I_{n}+\lambda _l W_{n})\) for SMA case.
1.2 A.2 Simultaneous moment functions
1.2.1 A.2.1 Proof of Equation (14)
Such that \(\overset{a}{{\bar{\epsilon }}} = \underset{a\text { times}}{\underbrace{M_{nT}\dots M_{nT}}}\epsilon =M_{nT}^a\epsilon \), \(M_{nT} Q_{nT,h}=(I_T\otimes M_n)(Q_{T,h}\otimes I_n)=Q_{nT,h} M_{nT}\) and \(Q_{nT,h}\Sigma _{lq}=\sigma _{h_{lq}}Q_{nT,h}\) for \(h=0,1\), one can write
1.2.2 A.2.2 Proof of Equation (15)
Since, \(\overset{a}{{\overline{\epsilon }}}_l=\overset{a}{{\overline{\upsilon }}_l}-\lambda _l\overset{a+1}{\overline{\upsilon }_l}\),
Such that \(\overset{a}{{\overline{\upsilon }}}^{\top }_l Q_{nT,h} \overset{b}{{\overline{\upsilon }}}_q=\text {tr}(Q_{nT,h})\gamma ^{lq,h}_{ab}\) we finally get,
1.2.3 A.2.3 Proof of Equation (20)
Since, for all \(a\in \mathbb {N}\), \(\overset{a}{{\overline{\upsilon }}}_l=\overset{a}{{\overline{\epsilon }}_l}+\lambda _l\overset{a+1}{\overline{\epsilon }_l}\)
Using (14), the expectation gives,
1.3 A.3 Derivation of \(\Omega _{\textbf{g}}\) in (52)
Since \(\Omega _{\textbf{g},11}=\text {E}\left( \textbf{g}_{1}\textbf{g}^\top _{1}\right) \) has a typical element \(\begin{bmatrix}\text {E}\left( \textbf{g}_{1,l}\textbf{g}^\top _{1,q}\right) \end{bmatrix}\) and such that
, then,
\(\Omega _{\textbf{g},22}=\text {E}\left( \textbf{g}_{2}\textbf{g}^\top _{2}\right) \) has a typical element \(\begin{bmatrix}\text {E}\left( \textbf{g}_{2,lq}\textbf{g}^\top _{2,kt}\right) \end{bmatrix}\) for \(l,q,k,t=1,\ldots ,L\); since
and such that, \(Q_{nT,h}=Q_{T,h}\otimes I_n\) for \(h=0,1\) with \(Q_{T,h}Q_{T,h'}=0\) if \(h\ne h'\) and \(\Xi _{nT,r}=I_T\otimes \Xi _{n,r}\) for \(r,s=1,\ldots ,p\), we have,
where,
are \(p\times p\) matrix of constants. Hence,
where, with the following matrix construction plan: \(\Psi _{row}({t,q})=[\circ \overset{t}{\rightarrow }\circ \; \circ \overset{t,q}{\rightarrow \rightarrow }\ ]\) and \(\Psi _{column}({l,k})=[\circ \overset{k}{\rightarrow }\circ \; \circ \overset{l,k}{\rightarrow \rightarrow }]\), the matrices \(\Psi _{1,h}\) \(\Psi _{2,h}\) have the following forms:
and
1.4 A.4 Identification
The identification of the spatial panel simultaneous equations model (1) relies on the two-step strategy initially adopted in Yang and Lee (2017), and Liu and Saraiva (2019). The first-step consists in the identification of the “pseudo” reduced form parameters and the second-step recovers the structural parameters from the pseudo” reduced form parameters.
1.4.1 A.4.1 Identification of the pseudo reduced form parameters
Let \(\Theta _0\), \(\Delta _0\), \({\textbf{B}}_0\) and \({\textbf{A}}_0\) be the matrices of the true parameters in the DGP. When \(\Theta _0\) is non singular, the pseudo reduced form of model (62) is
where \(\Phi _0=\Delta _0(I_{L}-\Theta _0)^{-1}\), \(\Pi _0={\textbf{B}}_0(I_{L}-\Theta _0)^{-1}\) and \(\textbf{V}=\textbf{U}(I_{L}-\Theta _0)^{-1}\). With \(\Phi _0=[\varphi _{lq,0}]\) and \(\Pi _0=[\pi _{1,0},...,\pi _{L,0}]\), under the GMM framework, the q-th equation in model (62) is given by
where
with \({\textbf{R}}_l=(i_{L,l}^\top \otimes W_{nT})(I_{nTL}-\Phi _0^\top \otimes W_{nT})^{-1}\), \({\textbf{x}}=\text {vec}({\textbf{X}})\), \({\textbf{v}}=\text {vec}({\textbf{V}})\) and \(i_{L,l}\) be the l-th vector of an identity matrix \(I_L\). We note that \(\text {E}(W_{nT}y_l)={\textbf{R}}_l(\Pi _0^\top \otimes I_{nT}){\textbf{x}}\) since \(\text {E}({\textbf{R}}_l{\textbf{v}})=0\). Now, the residual function
for the q-th equation can be rewritten as
where \(\rho _{q}=(\varphi _{1q},\ldots ,\varphi _{Lq},\pi _{q}^\top )^\top \) and \(d_q(\rho _q)=[\text {E}(W_{nT}y_1),\ldots ,\text {E}(W_{nT}y_L),{\textbf{X}}](\rho _{q,0}-\rho _{q})\). The pseudo reduced form parameters in model (62) can be identified by the moment conditions proposed in the Sect. (4.3.1) on the main text. Then, the linear and quadratic moment functions can be written as
Let \(\textbf{f}({\rho })=\begin{bmatrix}\textbf{f}^\top _{1}({\rho })&\textbf{f}^\top _{2}({\rho })\end{bmatrix}^\top \) where \(\rho =(\rho _1,\ldots ,\rho _L)\), \(\textbf{f}_{1}({\rho })=\begin{bmatrix}\textbf{f}_{1,1}^\top&\quad \cdots&\quad \textbf{f}_{1,L}^\top \end{bmatrix}^\top \) and \(\textbf{f}_{2}({\rho })=\begin{bmatrix}\textbf{f}_{2,11}^\top&\quad \cdots&\quad \textbf{f}_{2,1L}^\top&\quad \textbf{f}_{2,21}^\top&\quad \cdots&\quad \cdots&\quad \textbf{f}_{2,LL}^\top \end{bmatrix}^\top \). The identification of \(\rho _0\) by means of the moment conditions \(\text {E}[{\textbf{f}}(\rho _0)] =0\), requires that the moment equations \(\lim _{n\rightarrow \infty }(nT)^{-1}\text {E}[{\textbf{f}}(\rho _0)] =0\) have a unique solution at \(\rho =\rho _0\) (see Hansen 1982). From (66), it follows that
for \(l=1,\ldots ,L\). The linear moment equations, \(\lim _{n\rightarrow \infty }\frac{1}{nT}\text{ E }[{\textbf{f}}_{1,l}(\rho _l)]=0\), have a unique solution at \(\rho _l=\rho _{l,0}\) if \(\textbf{H}^\top [\text {E}(W_{nT}y_1),\ldots ,\text {E}(W_{nT}y_L),{\textbf{X}}]\) has full column rank for n sufficiently large. A necessary condition for this rank condition is that \(\text {rank}[\text {E}(W_{nT}y_1),\ldots ,\text {E}(W_{nT}y_L),{\textbf{X}}]=k+L\) and \(\text {rank}(\textbf{H})\ge k+L\) for n sufficiently large.
However, if the rank condition fails (i.e., \([\text {E}(W_{nT}y_1),\ldots ,\text {E}(W_{nT}y_L),{\textbf{X}}]\) does not have full column rank), identification of the model may still be feasible through the quadratic moment conditions. Suppose for some \(m=\{0,1,\ldots ,L-1\}\), \(\text {E}(W_{nT}y_l)\) and \([\text {E}(W_{nT}y_1),\ldots ,\text {E}(W_{nT}y_{m}),{\textbf{X}}]\) are linearly dependentFootnote 12 such that \(\text {E}(W_{nT}y_l)=\sum _{q=1}^{m}c_{1,ql}\text {E}(W_{nT}y_q)+{\textbf{X}} c_{2,l}\) for \(l=m+1,\ldots ,L\), where \((c_{1,1l},\ldots ,c_{1,m l},c_{2,l}^\top )\in {\mathbb {R}}^{k+m}\) is a vector of constants. This allows to write
and thus, \(\lim _{n\rightarrow \infty }\frac{1}{nT}\text{ E }[{\textbf{f}}_{1,l}(\rho _l)]=0\) entails that:
for \(j=1,\ldots ,m\) and \(q=1,\ldots ,L\), provided that \(\textbf{H}^\top [\text {E}(W_{nT}y_1),\ldots ,\text {E}(W_{nT}y_m),{\textbf{X}}]\) has full column rank for large enough n. Therefore, \((\varphi _{1q,0},\ldots ,\varphi _{mq,0},\pi _{q,0}^\top )\) can be identified if \(\varphi _{lq,0}\) (for \(l=m+1,\ldots ,L\)) can be identified from the quadratic moment conditions. With \(\rho _q\) given by (67), we have
where \(\text{ E }({\textbf{v}}{\textbf{v}}^\top )=\sum _{h=0}^1(I_L-\Theta _0)^{-1}({\hat{\Lambda }}_{\lambda }^{-1})^{\top }(\Sigma _h\otimes Q_{nT,h}){\hat{\Lambda }}^{-1}_{\lambda }(I_L-\Theta _0^\top )^{-1}\) and \(\text {E}({\textbf{v}}{\textbf{v}}_q^\top )= \text{ E }({\textbf{v}}{\textbf{v}}^\top )(i_{L,q}\otimes I_{nT})\). Thus, at \(\Phi _0\), the quadratic moment equations, \(\lim _{n\rightarrow \infty }\frac{1}{nT}\text{ E }[{\textbf{f}}_{2,lq}(\rho _l,\rho _q)]=0\) for \(l,q=1,\ldots ,L\), have a unique solution, if the equations
for \(r=1,\ldots ,p\) and \(l,q=1,\ldots ,L\). The following assumption provides sufficient conditions for the identification of the pseudo reduced form parameters.
Assumption 9
At least one of the following conditions holds:
(a) \(\lim _{n\rightarrow \infty }\frac{1}{nT}\textbf{H}^\top [\text {E}(W_{nT}y_1),\ldots ,\text {E}(W_{nT}y_L),{\textbf{X}}]\) exists and has full column rank.
(b) \(\lim _{n\rightarrow \infty }\frac{1}{nT}\textbf{H}^\top [\text {E}(W_{nT}y_1),\ldots ,\text {E}(W_{nT}y_m),{\textbf{X}}]\) exists and has full column rank for some \(0 \le m \le L-1\). Equation (67) for \(r=1,\ldots ,p\) and \(l,q=1,\ldots ,L\), have a unique solution at \(\Phi _0\).
1.4.2 A.4.2 Identification of the structural parameters
Having identified the “pseudo” reduced form parameters \(\Phi _0\) and \(\Pi _0\) from the linear and quadratic moment conditions, we can proceed on the identification of the structural parameters \({\textbf{C}}_0=[(I_L-\Theta _0)^\top ,-\Delta _0^\top ,-{\textbf{B}}_0^\top ]^\top \) through the linear restrictions \(\Phi _0=\Delta _0(I_{L}-\Theta _0)^{-1}\) and \(\Pi _0={\textbf{B}}_0(I_{L}-\Theta _0)^{-1}\) in a similar way to the classical linear simultaneous equations model. Given \(D_l\) restrictions on \({\textbf{c}}_{l,0}\) such that \({\textbf{D}}_l{\textbf{c}}_{l,0}\)=0, where \({\textbf{D}}_l\) and \({\textbf{c}}_{l,0}\) are, respectively, \(D_l\times (k+2L)\) matrix of known constants and the l-th column of \({\textbf{C}}_0\), the rank and order conditions for \({\textbf{c}}_{l,0}\) to be identified are as follow: (i) - the sufficient and necessary rank condition is \(rank({\textbf{D}}_l{\textbf{C}}) = L-1\); (ii) - the necessary order condition is \(D_l\ge L-1\), for \(l=1,\ldots ,L\).
Assumption 10
The following conditions holds for \(l=1,\ldots ,L\), \({\textbf{D}}_l{\textbf{c}}_{l,0}=0\) for some \(D_l\times (k+2L)\) constant matrix \(D_l\) with \(rank({\textbf{D}}_l{\textbf{C}}) = L-1\).
1.5 A.5 Tables
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Amba, M.C.O., Mbratana, T. & Le Gallo, J. Spatial panel simultaneous equations models with error components. Empir Econ 65, 1149–1196 (2023). https://doi.org/10.1007/s00181-023-02368-z
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DOI: https://doi.org/10.1007/s00181-023-02368-z