Block-Wise Weighted Least Square

Fundamentals
Title	Block-Wise Weighted Least Square
Author(s)	J. Sanz Subirana, JM. Juan Zornoza and M. Hernandez-Pajares, University of Catalunia, Spain.
Level	Medium
Year of Publication	2011

Let's consider two linear [math]\displaystyle{ [m_1\times n], [m_2\times n] }[/math] equations systems, sharing the same unknown parameters vector [math]\displaystyle{ {\mathbf X} }[/math]:

[math]\displaystyle{ \begin{array}{l} {\mathbf Y_1}={\mathbf G_1}\,{\mathbf X};{\mathbf R_1}\\[0.3cm] {\mathbf Y_2}={\mathbf G_2}\,{\mathbf X};{\mathbf R_2}\\ \end{array} \qquad \mbox{(1)} }[/math]

where [math]\displaystyle{ {\mathbf R_1} }[/math] and [math]\displaystyle{ {\mathbf R_2} }[/math] are the covariance matrices of measurement vectors [math]\displaystyle{ {\mathbf Y_1} }[/math], [math]\displaystyle{ {\mathbf Y_2} }[/math].

Thence the two systems can be combined into a common [math]\displaystyle{ [(m_1+m_2)\times n] }[/math] system as:

[math]\displaystyle{ \left[ \begin{array}{c} {\mathbf Y_1} \\ {\mathbf Y_2} \end{array} \right] = \left[ \begin{array}{c} {\mathbf G_1}\\[0.2cm] {\mathbf G_2} \end{array} \right] {\mathbf X} ;\qquad {\mathbf R}=\left[ \begin{array}{cc} {\mathbf R_1} & {\mathbf 0} \\[0.2cm] {\mathbf 0} & {\mathbf R_2} \end{array} \right] \qquad \mbox{(2)} }[/math]

where no correlation between the two measurement vectors [math]\displaystyle{ {\mathbf Y_1} }[/math] and [math]\displaystyle{ {\mathbf Y_2} }[/math] is assumed in matrix [math]\displaystyle{ {\mathbf R} }[/math].

From (3) and (4) (see Best Linear Unbiased Minimum-Variance Estimator (BLUE))

[math]\displaystyle{ \hat{\mathbf X}=({\mathbf G}^T\,{\mathbf R}^{-1}\,{\mathbf G})^{-1}{\mathbf G}^T\,{\mathbf R^{-1}}\,{\mathbf Y} \qquad \mbox{(3)} }[/math]

[math]\displaystyle{ {\mathbf P}=({\mathbf G}^T\,{\mathbf R}^{-1}\,{\mathbf G})^{-1} \qquad \mbox{(4)} }[/math]

it is easy to show that taking the corresponding augmented matrices [math]\displaystyle{ {\mathbf Y} }[/math] and [math]\displaystyle{ {\mathbf G} }[/math], the WLS solution of previous system (\ref{eq:bbwlms}) yields:

[math]\displaystyle{ \hat{\mathbf X}=\left [{\mathbf G_1}^T\,{\mathbf R_1}^{-1}\,{\mathbf G_1} + {\mathbf G_2}^T\,{\mathbf R_2}^{-1}\,{\mathbf G_2} \right ]^{-1} \left [{\mathbf G_1}^T\,{\mathbf R_1^{-1}}\,{\mathbf Y_1} + {\mathbf G_2}^T\,{\mathbf R_2^{-1}}\,{\mathbf Y_2} \right ] \qquad \mbox{(5)} }[/math]

[math]\displaystyle{ {\mathbf P}=\left [{\mathbf G_1}^T\,{\mathbf R_1}^{-1}\,{\mathbf G_1} + {\mathbf G_2}^T\,{\mathbf R_2}^{-1}\,{\mathbf G_2} \right ]^{-1} \qquad \mbox{(6)} }[/math]

Comments:

• Recursive computation: From previous approach, the following recursive computation of estimate [math]\displaystyle{ {\mathbf X} }[/math] can be written:

[math]\displaystyle{ \begin{array}{rl} {\mathbf P_1}=&\left [ {\mathbf G_1}^T\,{\mathbf R_1}^{-1}\,{\mathbf G_1} \right ]^{-1}\\[0.2cm] \hat{\mathbf X}_{(1)}=&{\mathbf P_1} \cdot \left [{\mathbf G_1}^T\,{\mathbf R_1^{-1}}\,{\mathbf Y_1} \right ]\\[0.4cm] {\mathbf P_2}=&\left [{\mathbf P_1}^{-1}+ {\mathbf G_2}^T\,{\mathbf R_2}^{-1}\,{\mathbf G_2} \right ]^{-1}\\[0.2cm] \hat{\mathbf X}_{(2)}=& {\mathbf P_2} \cdot \left [{\mathbf P_1^{-1}}\,{\mathbf X_{(1)}} + {\mathbf G_2}^T\,{\mathbf R_2^{-1}}\,{\mathbf Y_2} \right ]\\ \end{array} \qquad \mbox{(7)} }[/math]

Note: If only the final estimate is desired, it is best not to process data sequentially using (7), but instead to apply (see Best Linear Unbiased Minimum-Variance Estimator (BLUE))

[math]\displaystyle{ \hat{\mathbf X}=({\mathbf G}^T\,{\mathbf R}^{-1}\,{\mathbf G})^{-1}{\mathbf G}^T\,{\mathbf R^{-1}}\,{\mathbf Y} \qquad \mbox{(8)} }[/math]

and (6), that accumulates the equations without solving until the end Bierman, 1976] . This could be especially useful in case of numerical instabilities, avoiding the propagation of the numerical inaccuracies along the recursive steps.

• Constrains: A priory information can be added to the linear system (1) as constrain equations [math]\displaystyle{ {\mathbf \Lambda}={\mathbf A} {\mathbf X} }[/math] with a given weight [math]\displaystyle{ {\mathbf W}={\mathbf R_\Lambda}^{-1} }[/math]. Indeed:

[math]\displaystyle{ \begin{array}{l} {\mathbf Y}={\mathbf G}\,\,{\mathbf X};{\mathbf R}\\[0.1cm] {\mathbf \Lambda}={\mathbf A}\,\,{\mathbf X};{\mathbf R_\Lambda} \end{array} \qquad \mbox{(9)} }[/math]