Rice distribution

In the 2D plane, pick a fixed point at distance ν from the origin. Generate a distribution of 2D points centered around that point, where the x and y coordinates are chosen independently from a Gaussian distribution with standard deviation σ (blue region). If R is the distance from these points to the origin, then R has a Rice distribution.

In probability theory, the Rice distribution or Rician distribution (or, less commonly, Ricean distribution) is the probability distribution of the magnitude of a circularly symmetric bivariate normal random variable, possibly with non-zero mean (noncentral). It was named after Stephen O. Rice (1907–1986).

Characterization

The probability density function is

$f(x\mid \nu ,\sigma )=\frac{x}{{\sigma }^2}\exp \left(\frac{-(x^2+{\nu }^2)}{2{\sigma }^2}\right)I_0\left(\frac{x\nu }{{\sigma }^2}\right)H(x),$

where I₀(z) is the modified Bessel function of the first kind with order zero, and H(x) is the Heaviside unit step.

In the context of Rician fading, the distribution is often also rewritten using the shape parameter $K=\frac{{\nu }^2}{2{\sigma }^2}$, defined as the ratio of the power contributions by line-of-sight path to the remaining multipaths, and the scale parameter $\mathrm{\Omega }={\nu }^2+2{\sigma }^2$, defined as the total power received in all paths.

The characteristic function of the Rice distribution is given as:

$\begin{array}{cc}{\chi }_X(t\mid \nu ,\sigma )=\exp (-\frac{{\nu }^2}{2{\sigma }^2})& [{\mathrm{\Psi }}_2(1;1,\frac{1}{2};\frac{{\nu }^2}{2{\sigma }^2},-\frac{1}{2}{\sigma }^2{t}^2)\\ & +i\sqrt{2}\sigma t{\mathrm{\Psi }}_2(\frac{3}{2};1,\frac{3}{2};\frac{{\nu }^2}{2{\sigma }^2},-\frac{1}{2}{\sigma }^2{t}^2)],\end{array}$

where ${\mathrm{\Psi }}_2(\alpha ;\gamma ,{\gamma }^{\prime };x,y)$ is one of Horn's confluent hypergeometric functions with two variables and convergent for all finite values of $x$ and Template:Tmath. It is given by:

${\mathrm{\Psi }}_2(\alpha ;\gamma ,{\gamma }^{\prime };x,y)=\sum _{n=0}^{\mathrm{\infty }}\sum _{m=0}^{\mathrm{\infty }}\frac{(\alpha {)}_{m+n}}{(\gamma {)}_m({\gamma }^{\prime }{)}_n}\frac{x^m{y}^n}{m!n!},$

where

$(x{)}_n=x(x+1)\cdots (x+n-1)=\frac{\mathrm{\Gamma }(x+n)}{\mathrm{\Gamma }(x)}$

is the rising factorial.

Properties

Moments

The first few raw moments are:

$\begin{array}{cc}{\mu }_1^{\text{'}}& =\sigma \sqrt{\pi /2}{L}_{1/2}(-{\nu }^2/2{\sigma }^2)\\ {\mu }_2^{\text{'}}& =2{\sigma }^2+{\nu }^2\\ {\mu }_3^{\text{'}}& =3{\sigma }^3\sqrt{\pi /2}{L}_{3/2}(-{\nu }^2/2{\sigma }^2)\\ {\mu }_4^{\text{'}}& =8{\sigma }^4+8{\sigma }^2{\nu }^2+{\nu }^4\\ {\mu }_5^{\text{'}}& =15{\sigma }^5\sqrt{\pi /2}{L}_{5/2}(-{\nu }^2/2{\sigma }^2)\\ {\mu }_6^{\text{'}}& =48{\sigma }^6+72{\sigma }^4{\nu }^2+18{\sigma }^2{\nu }^4+{\nu }^6\end{array}$

and, in general, the raw moments are given by

${\mu }_k^{\text{'}}={\sigma }^k{2}^{k/2}\mathrm{\Gamma }(1+k/2)L_{k/2}(-{\nu }^2/2{\sigma }^2).$

Here Template:Tmath denotes a Laguerre polynomial:

$L_q(x)=L_q^{(0)}(x)=M(-q,1,x)={}_1{F}_1(-q;1;x)$

where $M(a,b,z){=}_1{F}_1(a;b;z)$ is the confluent hypergeometric function of the first kind. When Template:Tmath is even, the raw moments become simple polynomials in Template:Tmath and Template:Tmath, as in the examples above.

For the case Template:Tmath:

$\begin{array}{cc}{L}_{1/2}(x)& ={}_1{F}_1(-\frac{1}{2};1;x)\\ & =e^{x/2}[(1-x)I_0(-\frac{x}{2})-x{I}_1(-\frac{x}{2})].\end{array}$

The second central moment, the variance, is

${\mu }_2=2{\sigma }^2+{\nu }^2-(\pi {\sigma }^2/2)L_{1/2}^2(-{\nu }^2/2{\sigma }^2).$

Note that $L_{1/2}^2(\cdot )$ indicates the square of the Laguerre polynomial Template:Tmath, not the generalized Laguerre polynomial Template:Tmath.

Related distributions

• $R\sim \mathrm{R}\mathrm{i}\mathrm{c}\mathrm{e}(|\nu |,\sigma )$ if $R=\sqrt{X^2+Y^2}$ where $X\sim N(\nu \cos \theta ,{\sigma }^2)$ and $Y\sim N(\nu \sin \theta ,{\sigma }^2)$ are statistically independent normal random variables and $\theta$ is any real number.
• Another case where $R\sim \mathrm{R}\mathrm{i}\mathrm{c}\mathrm{e}(\nu ,\sigma )$ comes from the following steps:
  1. Generate $P$ having a Poisson distribution with parameter (also mean, for a Poisson) Template:Tmath.
  2. Generate $X$ having a chi-squared distribution with Template:Tmath degrees of freedom.
  3. Set $R=\sigma \sqrt{X}.$
• If $R\sim \mathrm{Rice}(\nu ,1)$ then $R^2$ has a noncentral chi-squared distribution with two degrees of freedom and noncentrality parameter Template:Tmath.
• If $R\sim \mathrm{Rice}(\nu ,1)$ then $R$ has a noncentral chi distribution with two degrees of freedom and noncentrality parameter Template:Tmath.
• If $R\sim \mathrm{Rice}(0,\sigma )$ then Template:Tmath, i.e., for the special case of the Rice distribution given by $\nu =0$, the distribution becomes the Rayleigh distribution, for which the variance is Template:Tmath.
• If $R\sim \mathrm{Rice}(0,\sigma )$ then $R^2$ has an exponential distribution.
• If $R\sim \mathrm{Rice}(\nu ,\sigma )$ then $1/R$ has an Inverse Rician distribution.
• The folded normal distribution is the univariate restriction of the Rice distribution.

Limiting cases

For large values of the argument, the Laguerre polynomial becomes

$\underset{x\to -\mathrm{\infty }}{lim}{L}_{\nu }(x)=\frac{|x{|}^{\nu }}{\mathrm{\Gamma }(1+\nu )}.$

It is seen that as Template:Tmath becomes large or Template:Tmath becomes small, the mean becomes Template:Tmath and the variance becomes Template:Tmath.

The transition to a Gaussian approximation proceeds as follows. From Bessel function theory we have

$I_{\alpha }(z)\to \frac{e^z}{\sqrt{2\pi z}}(1-\frac{4{\alpha }^2-1}{8z}+\cdots )\text{ as }z\to \mathrm{\infty }$

so, in the large $x\nu /{\sigma }^2$ region, an asymptotic expansion of the Rician distribution:

$\begin{array}{cc}f(x,\nu ,\sigma )=& \frac{x}{{\sigma }^2}\exp \left(\frac{-(x^2+{\nu }^2)}{2{\sigma }^2}\right)I_0\left(\frac{x\nu }{{\sigma }^2}\right)\\ \text{ is }\\ & \frac{x}{{\sigma }^2}\exp \left(\frac{-(x^2+{\nu }^2)}{2{\sigma }^2}\right)\sqrt{\frac{{\sigma }^2}{2\pi x\nu }}\exp \left(\frac{2x\nu }{2{\sigma }^2}\right)(1+\frac{{\sigma }^2}{8x\nu }+\cdots )\\ \to & \frac{1}{\sigma \sqrt{2\pi }}\exp (-\frac{(x-\nu {)}^2}{2{\sigma }^2})\sqrt{\frac{x}{\nu }},\text{ as }\frac{x\nu }{{\sigma }^2}\to \mathrm{\infty }\end{array}$

Moreover, when the density is concentrated around $\nu$ and $|x-\nu |\ll \sigma$ because of the Gaussian exponent, we can also write $\sqrt{x/\nu }\approx 1$ and finally get the Normal approximation

$f(x,\nu ,\sigma )\approx \frac{1}{\sigma \sqrt{2\pi }}\exp (-\frac{(x-\nu {)}^2}{2{\sigma }^2}),\frac{\nu }{\sigma }\gg 1$

The approximation becomes usable for Template:Tmath.

Parameter estimation (Koay inversion technique)

There are three different methods for estimating the parameters of the Rice distribution, (1) method of moments, (2) method of maximum likelihood, and (3) method of least squares.Template:Citation needed In the first two methods the interest is in estimating the parameters of the distribution, Template:Tmath and Template:Tmath, from a sample of data. This can be done using the method of moments, e.g., the sample mean and the sample standard deviation. The sample mean is an estimate of Template:Tmath and the sample standard deviation is an estimate of Template:Tmath.

The following is an efficient method, known as the "Koay inversion technique". for solving the estimating equations, based on the sample mean and the sample standard deviation, simultaneously . This inversion technique is also known as the fixed point formula of SNR. Earlier works on the method of moments usually use a root-finding method to solve the problem, which is not efficient.

First, the ratio of the sample mean to the sample standard deviation is defined as Template:Tmath, i.e., Template:Tmath. The fixed point formula of SNR is expressed as

$g(\theta )=\sqrt{\xi (\theta )[1+r^2]-2},$

where $\theta$ is the ratio of the parameters, i.e., Template:Tmath, and $\xi \left(\theta \right)$ is given by:

$\xi \left(\theta \right)=2+{\theta }^2-\frac{\pi }{8}\exp (-{\theta }^2/2){[(2+{\theta }^2)I_0({\theta }^2/4)+{\theta }^2{I}_1({\theta }^2/4)]}^2,$

where $I_0$ and $I_1$ are modified Bessel functions of the first kind.

Note that $\xi \left(\theta \right)$ is a scaling factor of $\sigma$ and is related to ${\mu }_2$ by:

${\mu }_2=\xi \left(\theta \right){\sigma }^2.$

To find the fixed point, Template:Tmath, of Template:Tmath, an initial solution is selected, Template:Tmath, that is greater than the lower bound, which is ${\theta }_{\text{lower bound}}=0$ and occurs when $r=\sqrt{\pi /(4-\pi )}$ (Notice that this is the $r={\mu }_1^{\text{'}}/{\mu }_2^{1/2}$ of a Rayleigh distribution). This provides a starting point for the iteration, which uses functional composition,Template:Clarify and this continues until $|g^i\left({\theta }_0\right)-{\theta }_{i-1}|$ is less than some small positive value. Here, $g^i$ denotes the composition of the same function, Template:Tmath, $i$ times. In practice, we associate the final ${\theta }_n$ for some integer $n$ as the fixed point, Template:Tmath, i.e., Template:Tmath.

Once the fixed point is found, the estimates $\nu$ and $\sigma$ are found through the scaling function, Template:Tmath, as follows:

$\sigma =\frac{{\mu }_2^{1/2}}{\sqrt{\xi \left({\theta }^{\ast }\right)}},$

and

$\nu =\sqrt{({\mu }_1^{\text{'}2}+(\xi \left({\theta }^{\ast }\right)-2){\sigma }^2)}.$

To speed up the iteration even more, one can use the Newton's method of root-finding. This particular approach is highly efficient.

Applications

• The Euclidean norm of a bivariate circularly symmetric normally distributed random vector.
• Rician fading (for multipath interference))
• Effect of sighting error on target shooting.
• Analysis of diversity receivers in radio communications.
• Distribution of eccentricities for models of the inner Solar System after long-term numerical integration.
• Distribution of noise in magnetic resonance imaging images is rician

See also

• Hoyt distribution
• Rayleigh distribution

Further reading

• Abramowitz, M. and Stegun, I. A. (ed.), Handbook of Mathematical Functions, National Bureau of Standards, 1964; reprinted Dover Publications, 1965. Template:ISBN
• Rice, S. O., Mathematical Analysis of Random Noise. Bell System Technical Journal 24 (1945) 46–156.
• Template:Cite journal
• Template:Cite journal
• Liu, X. and Hanzo, L., A Unified Exact BER Performance Analysis of Asynchronous DS-CDMA Systems Using BPSK Modulation over Fading Channels, IEEE Transactions on Wireless Communications, Volume 6, Issue 10, October 2007, pp. 3504–3509.
• Annamalai, A., Tellambura, C. and Bhargava, V. K., Equal-Gain Diversity Receiver Performance in Wireless Channels, IEEE Transactions on Communications, Volume 48, October 2000, pp. 1732–1745.
• Erdelyi, A., Magnus, W., Oberhettinger, F. and Tricomi, F. G., Higher Transcendental Functions, Volume 1. Template:Webarchive McGraw-Hill Book Company Inc., 1953.
• Srivastava, H. M. and Karlsson, P. W., Multiple Gaussian Hypergeometric Series. Ellis Horwood Ltd., 1985.
• Sijbers J., den Dekker A. J., Scheunders P. and Van Dyck D., "Maximum Likelihood estimation of Rician distribution parameters" Template:Webarchive, IEEE Transactions on Medical Imaging, Vol. 17, Nr. 3, pp. 357–361, (1998)
• Varadarajan D. and Haldar J. P., "A Majorize-Minimize Framework for Rician and Non-Central Chi MR Images", IEEE Transactions on Medical Imaging, Vol. 34, no. 10, pp. 2191–2202, (2015)
• Template:Cite journal
• Koay, C.G. and Basser, P. J., Analytically exact correction scheme for signal extraction from noisy magnitude MR signals, Journal of Magnetic Resonance, Volume 179, Issue = 2, p. 317–322, (2006)
• Abdi, A., Tepedelenlioglu, C., Kaveh, M., and Giannakis, G. On the estimation of the K parameter for the Rice fading distribution, IEEE Communications Letters, Volume 5, Number 3, March 2001, pp. 92–94.
• Template:Cite journal
• Template:Cite journal

External links

• MATLAB code for Rice/Rician distribution (PDF, mean and variance, and generating random samples)