## 1.

## Introduction

The Stokes vector that is limited to the three first components is commonly referred to as the linear Stokes vector^{1} and includes intensity and two linear Stokes parameters. From its measurement, two primary parameters of interest are calculated: the degree of linear polarization (DoLP) and the angle of linear polarization (AoLP). The AoLP and DoLP are nonlinear transforms of the two linear Stokes parameters from Cartesian to polar coordinates. The AoLP expresses the orientation of the linear polarization state. The DoLP expresses the magnitude of the linear polarization state. This work presents an exact analytic solution for the central moments of the AoLP when the linear Stokes parameters are drawn from uncorrelated Gaussian distributions of different means but equal variance. Fluctuations due to a change in the object’s polarization state during data acquisition (e.g., atmospheric turbulence) or fluctuations due to system artifacts (e.g., error from mechanical motion of optical components) could potentially introduce significant correlations. To test the validity of the uncorrelated assumption both the polarimetric instrumentation and the postprocessing calculations must be considered. If in postprocessing, different raw measurements are used to calculate each linear Stokes parameter then the measurement statistics will be uncorrelated owing to the independence of each measurement. Correlations would be introduced by reusing an individual measurement in the calculation of both linear Stokes parameters. Division of amplitude, aperture, or wavefront polarimeters traditionally use independent measurements to estimate each linear Stokes parameter. Traditional wire-grid polarizers also produce linear Stokes parameters with measurement noise that is uncorrelated since a different pair of independent measurements are used to calculate each.

If the Stokes parameters are calculated by combining a weighted sum of numerous independent measurements then, owing to the central limit theorem, a Gaussian probability density function (PDF) is expected with increasing confidence as the number of measurements used in the calculation increases.^{2} For example, modulated polarimeters collect a series of measurements while simultaneously changing the instrument’s polarimetric response. Using this strategy, the object’s polarization can be encoded temporally, spatially, and/or spectrally in the measurements. Then, in postprocessing numerous independent measurements are combined, usually by fitting to a model, to form an estimate of the object’s polarization.

Physical models of polarization are often specified in polar coordinates (e.g., astronomy and material scattering properties), therefore, characterizing AoLP statistics is of interest.^{3}^{,}^{4} Although an integral form of the PDF of the AoLP is known, this is the first report, to our knowledge, on an exact analytic expression for the central moments of the AoLP and their relation to the measurement uncertainty of the linear Stokes vector. When the DoLP is high relative to the measurement uncertainty of the linear Stokes vector, AoLP statistics have been shown to be well approximated by a Gaussian distribution;^{5} this is consistent with the results presented in this paper. As the DoLP approaches the measurement uncertainty of the linear Stoke parameters, the distribution on AoLP is no longer well approximated by a Gaussian distribution; this is also consistent with the results presented in this paper. This low DoLP limit is of interest and importance to researchers in astrophysics,^{5} reconnaissance,^{6} and atmospheric aerosol retrieval.^{7}

## 2.

## Mathematical Results

Consider the two linear Stokes parameters $q$ and $u$ as independent and normally distributed random variables with equal variance, $\mathrm{pr}(q)=\mathcal{N}(\overline{q},{\sigma}_{u,q}^{2})$ and $\mathrm{pr}(u)=\mathcal{N}(\overline{u},{\sigma}_{u,q}^{2})$. Here, all quantities are normalized by the intensity (i.e., the first linear Stokes component), as in $q=Q/I$ and $u=U/I$ where $I$ denotes the intensity. In practice, the PDF on $q$ and $u$ will depend upon how these quantities are measured. If in postprocessing the Stokes parameters are calculated from a sum, or weighted sum, of raw measurements then we can argue from the central limit theorem that the $\mathrm{pr}(u)$ and $\mathrm{pr}(u)$ will be approximately Gaussian if the raw measurements are sufficiently independent. From $\mathrm{pr}(u)$ and $\mathrm{pr}(u)$, a transformation of random variables is used to obtain $\mathrm{pr}(\theta )$ as a function of the means and variance of the two linear Stokes parameters. Beginning with the joint PDF

## (1)

$${\mathrm{pr}}_{\theta ,d}(\theta ,d)={\mathrm{pr}}_{q,u}[d\text{\hspace{0.17em}}\mathrm{cos}(2\theta ),d\text{\hspace{0.17em}}\mathrm{sin}(2\theta )]|\phantom{\rule{0ex}{0ex}}\mathrm{det}[\begin{array}{cc}\mathrm{cos}(2\theta )& 2d\text{\hspace{0.17em}}\mathrm{sin}(2\theta )\\ \mathrm{sin}(2\theta )& -2d\text{\hspace{0.17em}}\mathrm{cos}(2\theta )\end{array}\left]\right|=\frac{2d}{2\pi {\sigma}_{u,q}^{2}}\text{\hspace{0.17em}}\phantom{\rule{0ex}{0ex}}\mathrm{exp}\{-\frac{{[d\text{\hspace{0.17em}}\mathrm{cos}(2\theta )-\overline{q}]}^{2}+{[d\text{\hspace{0.17em}}\mathrm{sin}(2\theta )-\overline{u}]}^{2}}{2{\sigma}_{u,q}^{2}}\},$$^{8}Marginalizing over the DoLP to obtain the PDF of AoLP

## (2)

$$\mathrm{pr}(\theta )={\int}_{0}^{1}\mathrm{d}p{\mathrm{pr}}_{\theta ,d}(\theta ,p)\phantom{\rule{0ex}{0ex}}=\frac{1}{\pi}{\mathrm{e}}^{\frac{-{\overline{d}}^{2}}{2}}{\int}_{0}^{\infty}\mathrm{d}\tilde{p}\tilde{p}{\mathrm{e}}^{\frac{-{\tilde{p}}^{2}}{2}}{\mathrm{e}}^{\tilde{p}[\overline{q}\text{\hspace{0.17em}}\text{\hspace{0.17em}}\mathrm{cos}(2\theta )+\overline{u}\text{\hspace{0.17em}}\mathrm{sin}(2\theta )]},$$The definition of the $\alpha $-order central moment of the AoLP is

## (3)

$$\langle {(\theta -\overline{\varphi})}^{\alpha}\rangle ={\int}_{\overline{\varphi}-\pi /2}^{\overline{\varphi}+\pi /2}\mathrm{d}\theta \text{\hspace{0.17em}}\mathrm{pr}(\theta ){(\theta -\overline{\varphi})}^{\alpha}.$$In the Appendix, we show that the $\alpha $-order central moment of the AoLP can be equivalently expressed as

## (4)

$$\langle {(\theta -\overline{\varphi})}^{\alpha}\rangle =\frac{1}{{2}^{\alpha +1}\pi}\sum _{n=-\infty}^{\infty}{B}_{n}^{\alpha}{f}_{n}(\tilde{\overline{d}}),$$## (5)

$${B}_{n}^{\alpha}=\frac{1}{2\pi}{\int}_{-\pi}^{\pi}{\beta}^{\alpha}{\mathrm{e}}^{-\text{in}\beta}\mathrm{d}\beta ,$$## (6)

$${B}_{n}^{1}=\{\begin{array}{ll}\frac{{(-1)}^{n}i}{n}& \forall \text{\hspace{0.17em}}\text{\hspace{0.17em}}n\ne 0\\ 0& \text{otherwise}\end{array},$$## (7)

$${B}_{n}^{2}=\{\begin{array}{ll}\frac{2{(-1)}^{n}}{{n}^{2}}& \forall \text{\hspace{0.17em}}\text{\hspace{0.17em}}n\ne 0.1\text{\hspace{0.17em}}cm\\ \frac{{\pi}^{2}}{3}& \text{otherwise}.\end{array}$$## (8)

$${f}_{n}(\tilde{\overline{d}})=\phantom{\rule{0ex}{0ex}}\{\begin{array}{ll}\sqrt{\frac{{\pi}^{3}}{2}}{\mathrm{e}}^{\frac{-{\overline{d}}^{2}}{4}}\overline{d}\left[{I}_{\frac{n-1}{2}}\right(\frac{{\overline{d}}^{2}}{4})+{I}_{\frac{n+1}{2}}(\frac{{\overline{d}}^{2}}{4}\left)\right]& \forall \text{\hspace{0.17em}}\text{\hspace{0.17em}}n\ne 0\\ 2\pi & \text{otherwise}.\end{array}$$The analytic expression for the AoLP central moments is an infinite sum which, in practice, must be truncated, therefore, the computed value depends upon the number of terms retained

## (9)

$$\langle {(\theta -\overline{\varphi})}^{\alpha}\rangle \approx \langle \widehat{{(\theta -\overline{\varphi})}^{\alpha}}\rangle (K)=\frac{1}{{2}^{\alpha +1}\pi}\sum _{n=-K}^{K}{B}_{n}^{\alpha}{f}_{n}(\tilde{\overline{d}}).$$## 3.

## Computational Results

To verify the precision of the new analytic expression for the central moments of the AoLP, the square root of the second central moment (i.e., $\alpha =2$) is compared to two other numerical methods for calculating the AoLP standard deviation.

When a random variable of unknown variance has a nonlinear relationship to random variables of known variance the propagation of error (PE) method approximates the unknown variance by a truncated Taylor series as described in Ref. 10. When the linear Stokes parameters are uncorrelated, the PE approximation of the AoLP variance is

## (10)

$${\sigma}_{\theta}^{2}\approx {\sigma}_{u}^{2}{\left(\frac{\partial \theta}{\partial u}\right)}^{2}+{\sigma}_{q}^{2}{\left(\frac{\partial \theta}{\partial q}\right)}^{2}.$$The AoLP variance can also be calculated directly from ${N}_{\mathrm{samp}}$ linear Stokes parameter samples

## (12)

$${\widehat{\sigma}}_{\theta}^{2}({N}_{\mathrm{samp}})=\frac{1}{{N}_{\mathrm{samp}}}\sum _{n=1}^{{N}_{\mathrm{samp}}}{\Vert ({\theta}_{n}-\overline{\varphi})\Vert}^{2}\phantom{\rule{0ex}{0ex}}=\frac{1}{{N}_{\mathrm{samp}}}\sum _{n=1}^{{N}_{\mathrm{samp}}}{\left[\frac{1}{2}\text{\hspace{0.17em}}\mathrm{acos}\right(\frac{\overline{\mathbf{r}}\xb7{\mathbf{r}}_{n}}{|\overline{\mathbf{r}}||{\mathbf{r}}_{n}|}\left)\right]}^{2},$$To investigate the sensitivity between number of terms retained in Eq. (9) and the AoLP variance, a comparison is shown in Fig. 3(a). The number of terms required for convergence depends upon the AoLP variance. Accuracy at low AoLP variances (i.e., high DoLP) requires retaining more terms. For low DoLP environments and ${\sigma}_{\theta}>10\text{\hspace{0.17em}}\text{\hspace{0.17em}}\mathrm{deg}$, convergence is achieved at even 20 terms. This convergence behavior is advantageous since the analytic expression for AoLP variance is most useful in low DoLP environments. In relatively high DoLP environments, the analytic expression is not necessary because simpler approximations for the variance of AoLP, such as the PE method, are valid.

Figure 3(b) is a comparison between the PE estimate and the analytic expression for the AoLP variance at low DoLP. For ${\sigma}_{u,q}=0.005$, the two methods agree above about 2% DoLP. For DoLP lower than 2%, the methods begin to disagree and the PE analysis predicts lower values for ${\sigma}_{\theta}$. At 1% DoLP, the difference between the two methods is approximately 5 deg. This difference is potentially significant because statistical testing becomes most useful when the DoLP is low.

## 4.

## Example Application in Imaging Polarimetry

Figure 4 shows a cloud measurement from the Ground-based Multiangle SpectroPolarimetric Imager (GroundMSPI).^{11} This is an ideal application for our analytic AoLP variance since 47% of the pixels in the scene are at or below 2% DoLP; see Fig. 4(b). AoLP statistical analysis can be used to test GroundMSPI’s sensitivity in distinguishing single from multiple scattering events. In the case of single scattering, the AoLP of the cloud will either be the same as the AoLP of the sky or 90 deg from it as described in Refs. 12 and 13. Given GroundMSPI’s measurement uncertainty in the Stokes parameters of $\pm 0.005$,^{14} the analytic form presented in this paper is used to calculate the standard deviation of the AoLP measured at each image pixel. Pixels are selected from the GroundMSPI image based on three different ${\sigma}_{\mathrm{AoLP}}$ thresholds of: 3 deg, 6 deg, and 9 deg. These thresholds result in including 40%, 48%, and 60% of the image pixels; respectively. In Fig. 5, these AoLP values are plotted versus DoLP to separate sky from cloud pixels. The AoLP is plotted with error bars $\pm 2{\sigma}_{\theta}$ from the measured value. The $\pm 2{\sigma}_{\theta}$ interval has been shown in Ref. 5 to produce a 95.45% confidence level on AoLP. The AoLP uncertainty is lowest for the sky measurements since these have a higher DoLP value than the cloud [see Figs. 4(b) and 4(d)]. As the ${\sigma}_{\mathrm{AoLP}}$ threshold is increased, more low DoLP cloud pixels are included and a majority of these are $\pm 90\text{\hspace{0.17em}}\text{\hspace{0.17em}}\mathrm{deg}$ from the sky’s AoLP, which indicates single scattering. Multiple scattering would further decrease the DoLP, and at the lowest ${\sigma}_{\mathrm{AoLP}}$ threshold, more low DoLP points that are intermediate to sky and $\pm 90\text{\hspace{0.17em}}\text{\hspace{0.17em}}\mathrm{deg}$ sky AoLP appear.

To further investigate the presence of multiple scattering, Fig. 6(a) shows all AoLP measurements with a $\pm 2{\sigma}_{\mathrm{AoLP}}$ confidence interval that does not overlap the sky’s AoLP within a 12 deg boundary. This thresholding results in including 4% of the pixels and the location of these are displayed in Fig. 6(b). A higher density of intermediate AoLP values are seen as the DoLP decreases which would be expected for the AoLP of multiple scattering events.^{13} This analysis suggests the possibility that GroundMSPI is capable of detecting multiple scattering events and that a very low number of multiple scattering events is present in this scene but is not comprehensive enough to conclude that the intermediate population of AoLP values is caused by multiple scattering. Instead this analysis motivates further statistical AoLP studies on more polarimetric cloud images, as well as inspection of instrument calibration data to check whether the Gaussian noise assumption is valid. This cursory statistical analysis of MSPI cloud images is presented to motivate the usefulness of an analytic form for the AoLP variance when the linear Stokes parameters are uncorrelated and normally distributed with equal variance.

## 5.

## Conclusion

Here, we have provided an analytic form which relates the central moments of the AoLP to the Gaussian statistics of the linear Stokes vector. This expression yields a functional relationship between the measurement uncertainty in AoLP and the measurement uncertainty in DoLP. This is especially useful for high fidelity imaging polarimetry measurements of low DoLP scenes. In such an environment, simple Gaussian assumptions on the statistics of the AoLP are not valid because the high measurement precision of the AoLP statistics may contain useful information about the scene. Additionally, we have shown that a simple PE analysis underestimates the AoLP variance at extremely low DoLP values, but is accurate at DoLP values that are high relative to the Stokes measurement uncertainty. An example use of the analytic form on AoLP variance is presented for an example in imaging polarimetry.

## Appendices

## Appendix

Substituting Eq. (2) into Eq. (3) yields an expression for the AoLP central moments involving two integrals

## (13)

$$\langle {(\theta -\overline{\varphi})}^{\alpha}\rangle \phantom{\rule{0ex}{0ex}}=\frac{1}{\pi}{\mathrm{e}}^{\frac{-{\tilde{\overline{d}}}^{2}}{2}}{\int}_{0}^{\infty}\mathrm{d}\tilde{p}\tilde{p}{e}^{\frac{-{\tilde{p}}^{2}}{2}}{\int}_{\overline{\varphi}-\pi /2}^{\overline{\varphi}+\pi /2}\mathrm{d}\theta {\mathrm{e}}^{\tilde{p}(\tilde{\overline{q}}\text{\hspace{0.17em}}\mathrm{cos}(2\theta )+\tilde{\overline{u}}\text{\hspace{0.17em}}\mathrm{sin}(2\theta ))}{(\theta -\overline{\varphi})}^{\alpha}.$$## (14)

$$\frac{1}{{2}^{\alpha +1}}{\int}_{-\pi}^{\pi}\mathrm{d}\beta {\beta}^{\alpha}{\mathrm{e}}^{\tilde{p}\tilde{\overline{d}}\text{\hspace{0.17em}}\mathrm{cos}(\beta )}.$$## (16)

$${B}_{n}^{\alpha}=\frac{1}{2\pi}{\int}_{-\pi}^{\pi}\mathrm{d}\beta {\beta}^{\alpha}{\mathrm{e}}^{-\text{in}\beta}.$$## (17)

$${B}_{n}^{\alpha}=\frac{{(-1)}^{n}{\pi}^{\alpha -1}i}{2n}[1-{(-1)}^{\alpha}]+\frac{\alpha}{\text{in}}{B}_{n}^{\alpha -1}$$## (19)

$${B}_{n}^{0}=\frac{1}{2\pi}{\int}_{-\pi}^{\pi}\mathrm{d}\beta {\mathrm{e}}^{-\text{in}\beta}={\delta}_{n0},$$## (20)

$$\frac{1}{{2}^{\alpha +1}}\sum _{n=-\infty}^{\infty}{B}_{n}^{\alpha}{\int}_{-\pi}^{\pi}\mathrm{d}\beta {\mathrm{e}}^{\text{in}\beta}{\mathrm{e}}^{\tilde{p}\tilde{\overline{d}}\text{\hspace{0.17em}}\mathrm{cos}(\beta )}$$## (21)

$${I}_{n}(x)=\frac{1}{2\pi}{\int}_{-\pi}^{\pi}{\mathrm{e}}^{x\text{\hspace{0.17em}}\mathrm{cos}(\theta )}{\mathrm{e}}^{\text{in}\theta}\mathrm{d}\theta .$$## (22)

$$\frac{2\pi}{{2}^{\alpha +1}}\sum _{n=-\infty}^{\infty}{B}_{n}^{\alpha}{I}_{n}(\tilde{p}\tilde{\overline{d}}).$$## (23)

$$\langle {(\theta -\overline{\varphi})}^{\alpha}\rangle =\frac{1}{{2}^{\alpha}}{\mathrm{e}}^{\frac{-{\tilde{\overline{d}}}^{2}}{2}}\sum _{n=-\infty}^{\infty}{B}_{n}^{\alpha}{\int}_{0}^{\infty}\mathrm{d}\tilde{p}\tilde{p}{e}^{\frac{-{\tilde{p}}^{2}}{2}}{I}_{n}(\tilde{p}\tilde{\overline{d}}).$$## (25)

$${\int}_{0}^{\infty}\mathrm{d}\tilde{p}\tilde{p}{e}^{\frac{-{\tilde{p}}^{2}}{2}}{I}_{n}(\tilde{p}\tilde{\overline{d}})=\frac{\tilde{\overline{d}}}{2}\sqrt{\frac{\pi}{2}}{\mathrm{e}}^{\frac{{\tilde{\overline{d}}}^{2}}{4}}\left[{I}_{\frac{n-1}{2}}\right(\frac{{\tilde{\overline{d}}}^{2}}{4})\phantom{\rule{0ex}{0ex}}+{I}_{\frac{n+1}{2}}(\frac{{\tilde{\overline{d}}}^{2}}{4}\left)\right]\forall \text{\hspace{0.17em}}\text{\hspace{0.17em}}n\ne 0.$$For $n=0$, relating the modified Bessel function to a Bessel function with a purely complex argument allows a solution using integration by parts

## (26)

$${\int}_{0}^{\infty}\mathrm{d}\tilde{p}\tilde{p}{\mathrm{e}}^{\frac{-{\tilde{p}}^{2}}{2}}{I}_{0}(\tilde{p}\tilde{\overline{d}})={\int}_{0}^{\infty}\mathrm{d}\tilde{p}\tilde{p}{\mathrm{e}}^{\frac{-{\tilde{p}}^{2}}{2}}{J}_{0}(i\tilde{p}\tilde{\overline{d}})={\mathrm{e}}^{\frac{{\tilde{\overline{d}}}^{2}}{2}}$$## Acknowledgments

This work is supported by NSF/CHE-1313892. Christine Bradley provided the GroundMSPI images and brought the application of AoLP analysis to distinguish single and multiple scattering to our attention. Discussions with Michael Garay, Anthony Davis, and David Diner of the Jet Propulsion Laboratory, California Institute of Technology improved the interpretation of GroundMSPI data.

## References

R. A. Chipman, “Polarimetry,” in OSA Handbook of Optics, pp. 22.21–22.35, McGraw-Hill, New York (1995).Google Scholar

A. DasGupta, Asymptotic Theory of Statistics and Probability, Springer, New York (2008).Google Scholar

D. ClarkB. G. Stewart, “Statistical methods of stellar polarimetry,” Vistas Astron. 29(1), 27–51 (1986).VASTA60083-6656http://dx.doi.org/10.1016/0083-6656(86)90013-9Google Scholar

F. GoudailA. Bénière, “Estimation precision of the degree of linear polarization and of the angle of polarization in the presence of different sources of noise,” Appl. Opt. 49(4), 683–693 (2010).APOPAI0003-6935http://dx.doi.org/10.1364/AO.49.000683Google Scholar

J. Naghizadeh-KhoueiD. Clarke, “On the statistical behavior of the position angle of linear polarization,” Astron. Astrophys. 274, 968 (1993).AAEJAF0004-6361Google Scholar

K. L. Coulson, “Effects of reflection properties of natural surfaces in aerial reconnaissance,” Appl. Opt. 5(6), 905–917 (1966).APOPAI0003-6935http://dx.doi.org/10.1364/AO.5.000905Google Scholar

M. MishchenkoL. Travis, “Satellite retrieval of aerosol properties over the ocean using polarization as well as intensity of reflected sunlight,” J. Geophys. Res. Atmos. 102(D14), 16989–17013 (1997).JGRDE30148-0227http://dx.doi.org/10.1029/96JD02425Google Scholar

S. O. Rice, “Mathematical analysis of random noise,” Bell Syst. Tech. J. 24(1), 46–156 (1945).BSTJAN0005-8580http://dx.doi.org/10.1002/(ISSN)1538-7305cGoogle Scholar

J. L. Quinn, “Bayesian analysis of polarization measurements,” Astron. Astrophys. 538, A65 (2012).AAEJAF0004-6361http://dx.doi.org/10.1051/0004-6361/201015785Google Scholar

P. R. BevingtonD. K. Robinson, Data Reduction and Error Analysis for the Physical Sciences, Vol. 2, McGraw-Hill, New York (1969).Google Scholar

D. Dineret al., “Exploration of a polarized surface bidirectional reflectance model using the ground-based multiangle spectropolarimetric imager,” Atmosphere 3(4), 591–619 (2012).2073-4433http://dx.doi.org/10.3390/atmos3040591Google Scholar

N. PustJ. Shaw, “Digital all-sky polarization imaging of partly cloudy skies,” Appl. Opt. 47(34), H190–H198 (2008).APOPAI0003-6935http://dx.doi.org/10.1364/AO.47.00H190Google Scholar

A. Kokhanovsky, “Optical properties of terrestrial clouds,” Earth Sci. Rev. 64(3), 189–241 (2004).ESREAV0012-8252http://dx.doi.org/10.1016/S0012-8252(03)00042-4Google Scholar

A. MahlerD. DinerR. Chipman, “Analysis of static and time-varying polarization errors in the multiangle spectropolarimetric imager,” Appl. Opt. 50(14), 2080–2087 (2011).APOPAI0003-6935http://dx.doi.org/10.1364/AO.50.002080Google Scholar

F. Olveret al., NIST Handbook of Mathematical Functions, Vol. 256, Cambridge University Press, Cambridge (2010).Google Scholar

## Biography

**Meredith Kupinski** earned a BS degree in imaging technology from the Rochester Institute of Technology and both MS and PhD degrees in optical science from University of Arizona. She is an assistant research professor at the University of Arizona’s College of Optical Sciences working on statistical optics, imaging science, and probabilistic decision theory. She is the recipient of a Science, Engineering, and Education for Sustainability (SEES) fellowship from the National Science Foundation.

**Russell Chipman** received his BS degree from MIT and his MS/PhD degree in optical science from the University of Arizona. He is the co-PI of the Jet Propulsion Labs Multi-Spectral Polarimetric Imager, a candidate instrument for the global monitoring of aerosols from space to support measurements of the global energy balance for climate studies. He is a fellow of both OSA and SPIE and the 2007 recipient of SPIE’s Stokes award for polarimetry.

**Eric Clarkson** obtained a BA degree in mathematics, physics, and philosophy from Rice University, an MS degree in physics and a PhD degree in mathematics from Arizona State University, and an MS degree in optical sciences from the University of Arizona. He is a professor at the University of Arizona with joint appointments in the Department of Medical Imaging and the College of Optical Sciences. His research interests include statistical decision theory, statistical estimation, information theory, and image analysis.