Stable

Probability density function Symmetric ${\displaystyle \alpha }$-stable distributions with unit scale factor Skewed centered stable distributions with unit scale factor
Cumulative distribution function CDFs for symmetric ${\displaystyle \alpha }$-stable distributions CDFs for skewed centered stable distributions
Parameters	${\displaystyle \alpha \in (0,2]}$ — stability parameter ${\displaystyle \beta }$ ∈ [−1, 1] — skewness parameter (note that skewness is undefined) c ∈ (0, ∞) — scale parameter μ ∈ (−∞, ∞) — location parameter
Support	x ∈ [μ, +∞) if ${\displaystyle \alpha <1}$ and ${\displaystyle \beta =1}$ x ∈ (-∞, μ] if ${\displaystyle \alpha <1}$ and ${\displaystyle \beta =-1}$ x ∈ R otherwise
PDF	not analytically expressible, except for some parameter values
CDF	not analytically expressible, except for certain parameter values
Mean	μ when ${\displaystyle \alpha >1}$, otherwise undefined
Median	μ when ${\displaystyle \beta =0}$, otherwise not analytically expressible
Mode	μ when ${\displaystyle \beta =0}$, otherwise not analytically expressible
Variance	2c2 when ${\displaystyle \alpha =2}$, otherwise infinite
Skewness	0 when ${\displaystyle \alpha =2}$, otherwise undefined
Excess kurtosis	0 when ${\displaystyle \alpha =2}$, otherwise undefined
Entropy	not analytically expressible, except for certain parameter values
MGF	${\displaystyle \exp \!{\big (}t\mu +c^{2}t^{2}{\big )))$ when ${\displaystyle \alpha =2}$, ${\displaystyle \exp \!{\big (}t\mu -c^{\alpha }t^{\alpha }\sec(\pi \alpha /2){\big )))$ when ${\displaystyle \alpha \neq 1,\beta =-1,t>0}$, ${\displaystyle \exp \!{\big (}t\mu -c2\pi ^{-1}t\ln t{\big )))$ when ${\displaystyle \alpha =1,\beta =-1,t>0}$, otherwise undefined
CF	${\displaystyle \exp \!{\Big [}\;it\mu -|c\,t|^{\alpha }\,(1-i\beta \operatorname {sgn}(t)\Phi )\;{\Big ]},}$ where ${\displaystyle \Phi ={\begin{cases}\tan {\tfrac {\pi \alpha }{2))&{\text{if ))\alpha \neq 1\\-{\tfrac {2}{\pi ))\log |t|&{\text{if ))\alpha =1\end{cases))}$

In probability theory, a distribution is said to be stable if a linear combination of two independent random variables with this distribution has the same distribution, up to location and scale parameters. A random variable is said to be stable if its distribution is stable. The stable distribution family is also sometimes referred to as the Lévy alpha-stable distribution, after Paul Lévy, the first mathematician to have studied it.^[1][2]

Of the four parameters defining the family, most attention has been focused on the stability parameter, ${\displaystyle \alpha }$ (see panel). Stable distributions have ${\displaystyle 0<\alpha \leq 2}$, with the upper bound corresponding to the normal distribution, and ${\displaystyle \alpha =1}$ to the Cauchy distribution. The distributions have undefined variance for ${\displaystyle \alpha <2}$, and undefined mean for ${\displaystyle \alpha \leq 1}$. The importance of stable probability distributions is that they are "attractors" for properly normed sums of independent and identically distributed (iid) random variables. The normal distribution defines a family of stable distributions. By the classical central limit theorem the properly normed sum of a set of random variables, each with finite variance, will tend toward a normal distribution as the number of variables increases. Without the finite variance assumption, the limit may be a stable distribution that is not normal. Mandelbrot referred to such distributions as "stable Paretian distributions",^[3][4][5] after Vilfredo Pareto. In particular, he referred to those maximally skewed in the positive direction with ${\displaystyle 1<\alpha <2}$ as "Pareto–Lévy distributions",^[1] which he regarded as better descriptions of stock and commodity prices than normal distributions.^[6]

Definition

A non-degenerate distribution is a stable distribution if it satisfies the following property:

Since the normal distribution, the Cauchy distribution, and the Lévy distribution all have the above property, it follows that they are special cases of stable distributions.

Such distributions form a four-parameter family of continuous probability distributions parametrized by location and scale parameters μ and c, respectively, and two shape parameters ${\displaystyle \beta }$ and ${\displaystyle \alpha }$, roughly corresponding to measures of asymmetry and concentration, respectively (see the figures).

The characteristic function ${\displaystyle \varphi (t)}$ of any probability distribution is the Fourier transform of its probability density function ${\displaystyle f(x)}$. The density function is therefore the inverse Fourier transform of the characteristic function:^[8]

$${\displaystyle \varphi (t)={\frac {1}{2\pi ))\int _{-\infty }^{\infty }f(x)e^{-ixt}\,dt.}$$

Although the probability density function for a general stable distribution cannot be written analytically, the general characteristic function can be expressed analytically. A random variable X is called stable if its characteristic function can be written as^[7][9]

$${\displaystyle \varphi (t;\alpha ,\beta ,c,\mu )=\exp \left(it\mu -|ct|^{\alpha }\left(1-i\beta \operatorname {sgn}(t)\Phi \right)\right)}$$

$${\displaystyle \Phi ={\begin{cases}\tan \left({\frac {\pi \alpha }{2))\right)&\alpha \neq 1\\-{\frac {2}{\pi ))\log |t|&\alpha =1\end{cases))}$$

${\displaystyle \beta \in [-1,1]}$

${\displaystyle \alpha <2}$

The reason this gives a stable distribution is that the characteristic function for the sum of two independent random variables equals the product of the two corresponding characteristic functions. Adding two random variables from a stable distribution gives something with the same values of ${\displaystyle \alpha }$ and ${\displaystyle \beta }$, but possibly different values of μ and c.

Not every function is the characteristic function of a legitimate probability distribution (that is, one whose cumulative distribution function is real and goes from 0 to 1 without decreasing), but the characteristic functions given above will be legitimate so long as the parameters are in their ranges. The value of the characteristic function at some value t is the complex conjugate of its value at −t as it should be so that the probability distribution function will be real.

In the simplest case ${\displaystyle \beta =0}$, the characteristic function is just a stretched exponential function; the distribution is symmetric about μ and is referred to as a (Lévy) symmetric alpha-stable distribution, often abbreviated SαS.

When ${\displaystyle \alpha <1}$ and ${\displaystyle \beta =1}$, the distribution is supported on [μ, ∞).

The parameter c > 0 is a scale factor which is a measure of the width of the distribution while ${\displaystyle \alpha }$ is the exponent or index of the distribution and specifies the asymptotic behavior of the distribution.

Parametrizations

The above definition is only one of the parametrizations in use for stable distributions; it is the most common but its probability density is not continuous in the parameters at ${\displaystyle \alpha =1}$.^[10]

A continuous parametrization is^[7]

$${\displaystyle \varphi (t;\alpha ,\beta ,\gamma ,\delta )=\exp \left(it\delta -|\gamma t|^{\alpha }\left(1-i\beta \operatorname {sgn}(t)\Phi \right)\right)}$$

$${\displaystyle \Phi ={\begin{cases}\left(|\gamma t|^{1-\alpha }-1\right)\tan \left({\tfrac {\pi \alpha }{2))\right)&\alpha \neq 1\\-{\frac {2}{\pi ))\log |\gamma t|&\alpha =1\end{cases))}$$

The ranges of ${\displaystyle \alpha }$ and ${\displaystyle \beta }$ are the same as before, γ (like c) should be positive, and δ (like μ) should be real.

In either parametrization one can make a linear transformation of the random variable to get a random variable whose density is ${\displaystyle f(y;\alpha ,\beta ,1,0)}$. In the first parametrization, this is done by defining the new variable:

$${\displaystyle y={\begin{cases}{\frac {x-\mu }{\gamma ))&\alpha \neq 1\\{\frac {x-\mu }{\gamma ))-\beta {\frac {2}{\pi ))\ln \gamma &\alpha =1\end{cases))}$$

For the second parametrization, simply use

$${\displaystyle y={\frac {x-\delta }{\gamma ))}$$

${\displaystyle \alpha }$

${\displaystyle \alpha >1}$

${\displaystyle \delta -\beta \gamma \tan \left({\tfrac {\pi \alpha }{2))\right).}$

The distribution

A stable distribution is therefore specified by the above four parameters. It can be shown that any non-degenerate stable distribution has a smooth (infinitely differentiable) density function.^[7] If ${\displaystyle f(x;\alpha ,\beta ,c,\mu )}$ denotes the density of X and Y is the sum of independent copies of X:

$${\displaystyle Y=\sum _{i=1}^{N}k_{i}(X_{i}-\mu )}$$

${\displaystyle {\tfrac {1}{s))f(y/s;\alpha ,\beta ,c,0)}$

$${\displaystyle s=\left(\sum _{i=1}^{N}|k_{i}|^{\alpha }\right)^{\frac {1}{\alpha ))}$$

The asymptotic behavior is described, for ${\displaystyle \alpha <2}$, by:^[7]

$${\displaystyle f(x)\sim {\frac {1}{|x|^{1+\alpha ))}\left(c^{\alpha }(1+\operatorname {sgn}(x)\beta )\sin \left({\frac {\pi \alpha }{2))\right){\frac {\Gamma (\alpha +1)}{\pi ))\right)}$$

${\displaystyle \alpha \geq 1}$

${\displaystyle \beta =\pm 1}$

${\displaystyle \alpha <2}$

When ${\displaystyle \alpha =2}$, the distribution is Gaussian (see below), with tails asymptotic to exp(−x²/4c²)/(2c√π).

One-sided stable distribution and stable count distribution

When ${\displaystyle \alpha <1}$ and ${\displaystyle \beta =1}$, the distribution is supported on [μ, ∞). This family is called one-sided stable distribution.^[11] Its standard distribution (μ=0) is defined as

${\displaystyle L_{\alpha }(x)=f{\left(x;\alpha ,1,\cos \left({\frac {\alpha \pi }{2))\right)^{1/\alpha },0\right)))$, where ${\displaystyle \alpha <1}$.

Let ${\displaystyle q=\exp(-i\alpha \pi /2)}$, its characteristic function is ${\displaystyle \varphi (t;\alpha )=\exp \left(-q|t|^{\alpha }\right)}$. Thus the integral form of its PDF is (note: ${\displaystyle \operatorname {Im} (q)<0}$)

$${\displaystyle {\begin{aligned}L_{\alpha }(x)&={\frac {1}{\pi ))\Re \left[\int _{-\infty }^{\infty }e^{itx}e^{-q|t|^{\alpha ))\,dt\right]\\&={\frac {2}{\pi ))\int _{0}^{\infty }e^{-\operatorname {Re} (q)\,t^{\alpha ))\sin(tx)\sin(-\operatorname {Im} (q)\,t^{\alpha })\,dt,{\text{ or ))\\&={\frac {2}{\pi ))\int _{0}^{\infty }e^{-{\text{Re))(q)\,t^{\alpha ))\cos(tx)\cos(\operatorname {Im} (q)\,t^{\alpha })\,dt.\end{aligned))}$$

The double-sine integral is more effective for very small ${\displaystyle x}$.

Consider the Lévy sum ${\textstyle Y=\sum _{i=1}^{N}X_{i))$ where ${\textstyle X_{i}\sim L_{\alpha }(x)}$, then Y has the density ${\textstyle {\frac {1}{\nu ))L_{\alpha }{\left({\frac {x}{\nu ))\right)))$ where ${\textstyle \nu =N^{1/\alpha ))$. Set ${\textstyle x=1}$ to arrive at the stable count distribution.^[12] Its standard distribution is defined as

${\displaystyle {\mathfrak {N))_{\alpha }(\nu )={\frac {\alpha }{\Gamma \left({\frac {1}{\alpha ))\right))){\frac {1}{\nu ))L_{\alpha }{\left({\frac {1}{\nu ))\right)))$, where ${\displaystyle \nu >0}$ and ${\displaystyle \alpha <1}$.

The stable count distribution is the conjugate prior of the one-sided stable distribution. Its location-scale family is defined as

${\displaystyle {\mathfrak {N))_{\alpha }(\nu ;\nu _{0},\theta )={\frac {\alpha }{\Gamma ({\frac {1}{\alpha ))))){\frac {1}{\nu -\nu _{0))}L_{\alpha }{\left({\frac {\theta }{\nu -\nu _{0))}\right)))$, where ${\displaystyle \nu >\nu _{0))$, ${\displaystyle \theta >0}$, and ${\displaystyle \alpha <1}$.

It is also a one-sided distribution supported on ${\displaystyle [\nu _{0},\infty )}$. The location parameter ${\displaystyle \nu _{0))$ is the cut-off location, while ${\displaystyle \theta }$ defines its scale.

When ${\textstyle \alpha ={\frac {1}{2))}$, ${\textstyle L_{\frac {1}{2))(x)}$ is the Lévy distribution which is an inverse gamma distribution. Thus ${\displaystyle {\mathfrak {N))_{\frac {1}{2))(\nu ;\nu _{0},\theta )}$ is a shifted gamma distribution of shape 3/2 and scale ${\displaystyle 4\theta }$,

${\displaystyle {\mathfrak {N))_{\frac {1}{2))(\nu ;\nu _{0},\theta )={\frac {1}{4{\sqrt {\pi ))\theta ^{3/2))}(\nu -\nu _{0})^{1/2}e^{-{\frac {\nu -\nu _{0)){4\theta ))))$, where ${\displaystyle \nu >\nu _{0))$, ${\displaystyle \theta >0}$.

Its mean is ${\displaystyle \nu _{0}+6\theta }$ and its standard deviation is ${\displaystyle {\sqrt {24))\theta }$. It is hypothesized that VIX is distributed like ${\textstyle {\mathfrak {N))_{\frac {1}{2))(\nu ;\nu _{0},\theta )}$ with ${\displaystyle \nu _{0}=10.4}$ and ${\displaystyle \theta =1.6}$ (See Section 7 of ^[12]). Thus the stable count distribution is the first-order marginal distribution of a volatility process. In this context, ${\displaystyle \nu _{0))$ is called the "floor volatility".

Another approach to derive the stable count distribution is to use the Laplace transform of the one-sided stable distribution, (Section 2.4 of ^[12])

${\displaystyle \int _{0}^{\infty }e^{-zx}L_{\alpha }(x)dx=e^{-z^{\alpha ))}$, where ${\displaystyle \alpha <1}$.

Let ${\displaystyle x=1/\nu }$, and one can decompose the integral on the left hand side as a product distribution of a standard Laplace distribution and a standard stable count distribution,f

${\displaystyle \int _{0}^{\infty }{\frac {1}{\nu ))\left({\frac {1}{2))e^{-{\frac {|z|}{\nu ))}\right)\left({\frac {\alpha }{\Gamma ({\frac {1}{\alpha ))))){\frac {1}{\nu ))L_{\alpha }{\left({\frac {1}{\nu ))\right)}\right)d\nu ={\frac {1}{2)){\frac {\alpha }{\Gamma ({\frac {1}{\alpha )))))e^{-|z|^{\alpha ))}$, where ${\displaystyle \alpha <1}$.

This is called the "lambda decomposition" (See Section 4 of ^[12]) since the right hand side was named as "symmetric lambda distribution" in Lihn's former works. However, it has several more popular names such as "exponential power distribution", or the "generalized error/normal distribution", often referred to when ${\displaystyle \alpha >1}$.

The n-th moment of ${\displaystyle {\mathfrak {N))_{\alpha }(\nu )}$ is the ${\displaystyle -(n+1)}$-th moment of ${\displaystyle L_{\alpha }(x)}$, and all positive moments are finite.

Properties

• All stable distributions are infinitely divisible.
• With the exception of the normal distribution (${\displaystyle \alpha =2}$), stable distributions are leptokurtotic and heavy-tailed distributions.
• Closure under convolution

Stable distributions are closed under convolution for a fixed value of ${\displaystyle \alpha }$. Since convolution is equivalent to multiplication of the Fourier-transformed function, it follows that the product of two stable characteristic functions with the same ${\displaystyle \alpha }$ will yield another such characteristic function. The product of two stable characteristic functions is given by:

$${\displaystyle \exp \left(it\mu _{1}+it\mu _{2}-|c_{1}t|^{\alpha }-|c_{2}t|^{\alpha }+i\beta _{1}|c_{1}t|^{\alpha }\operatorname {sgn}(t)\Phi +i\beta _{2}|c_{2}t|^{\alpha }\operatorname {sgn}(t)\Phi \right)}$$

Since Φ is not a function of the μ, c or ${\displaystyle \beta }$ variables it follows that these parameters for the convolved function are given by:

$${\displaystyle {\begin{aligned}\mu &=\mu _{1}+\mu _{2}\\|c|&=\left(|c_{1}|^{\alpha }+|c_{2}|^{\alpha }\right)^{\frac {1}{\alpha ))\\[6pt]\beta &={\frac {\beta _{1}|c_{1}|^{\alpha }+\beta _{2}|c_{2}|^{\alpha )){|c_{1}|^{\alpha }+|c_{2}|^{\alpha ))}\end{aligned))}$$

In each case, it can be shown that the resulting parameters lie within the required intervals for a stable distribution.

The Generalized Central Limit Theorem

The Generalized Central Limit Theorem (GCLT) was an effort of multiple mathematicians (Berstein, Lindeberg, Lévy, Feller, Kolmogorov, and others) over the period from 1920 to 1937. ^[13] The first published complete proof (in French) of the GCLT was in 1937 by Paul Lévy.^[14] An English language version of the complete proof of the GCLT is available in the translation of Gnedenko and Kolmogorov's 1954 book.^[15]

The statement of the GLCT is as follows:^[16]

A non-degenerate random variable Z is α-stable for some 0 < α ≤ 2 if and only if there is an independent, identically distributed sequence of random variables X₁, X₂, X₃, ... and constants a_n > 0, b_n ∈ ℝ with

a_n (X₁ + ... + X_n) - b_n → Z.

Here → means the sequence of random variable sums converges in distribution; i.e., the corresponding distributions satisfy F_n(y) → F(y) at all continuity points of F.

In other words, if sums of independent, identically distributed random variables converge in distribution to some Z, then Z must be a stable distribution.

A generalized central limit theorem

General reference: ^[17] by Gnedenko.

Another important property of stable distributions is the role that they play in a generalized central limit theorem. The central limit theorem states that the sum of a number of independent and identically distributed (i.i.d.) random variables with finite non-zero variances will tend to a normal distribution as the number of variables grows.

A generalization due to Gnedenko and Kolmogorov states that the sum of a number of random variables with symmetric distributions having power-law tails (Paretian tails), decreasing as ${\displaystyle |x|^{-\alpha -1))$ where ${\displaystyle 0<\alpha \leqslant 2}$ (and therefore having infinite variance), will tend to a stable distribution ${\displaystyle f(x;\alpha ,0,c,0)}$ as the number of summands grows.^[18] If ${\displaystyle \alpha >2}$ then the sum converges to a stable distribution with stability parameter equal to 2, i.e. a Gaussian distribution.^[19]

^[20]

There are other possibilities as well. For example, if the characteristic function of the random variable is asymptotic to ${\displaystyle 1+a|t|^{\alpha }\ln |t|}$ for small t (positive or negative), then we may ask how t varies with n when the value of the characteristic function for the sum of n such random variables equals a given value u:

$${\displaystyle \varphi _{\text{sum))=\varphi ^{n}=u}$$

Assuming for the moment that t → 0, take the limit of the above as n → ∞:

$${\displaystyle \ln u=\lim _{n\to \infty }n\ln \varphi =\lim _{n\to \infty }na|t|^{\alpha }\ln |t|.}$$

Therefore:

$${\displaystyle {\begin{aligned}\ln(\ln u)&=\ln \left(\lim _{n\to \infty }na|t|^{\alpha }\ln |t|\right)\\[5pt]&=\lim _{n\to \infty }\ln \left(na|t|^{\alpha }\ln |t|\right)=\lim _{n\to \infty }\left[\ln(na)+\alpha \ln |t|+\ln(\ln |t|)\right]\end{aligned))}$$

This shows that ${\displaystyle \ln |t|}$ is asymptotic to ${\displaystyle {\tfrac {-1}{\alpha ))\ln n,}$ so using the previous equation this leads to

$${\displaystyle |t|\sim \left({\frac {-\alpha \ln u}{na\ln n))\right)^{1/\alpha }.}$$

This implies that the sum divided by

$${\displaystyle \left({\frac {na\ln n}{\alpha ))\right)^{\frac {1}{\alpha ))}$$

${\displaystyle t'=(-\ln u)^((1}/{\alpha )).}$

${\displaystyle \exp(-(t')^{\alpha })}$

$${\displaystyle \left({\frac {na\ln n}{\alpha ))\right)^{\frac {1}{\alpha ))}$$

converges in distribution to the symmetric alpha-stable distribution with stability parameter ${\displaystyle \alpha }$ and scale parameter 1.

This can be applied to a random variable whose tails decrease as ${\displaystyle |x|^{-3))$. This random variable has a mean but the variance is infinite. Let us take the following distribution:

$${\displaystyle f(x)={\begin{cases}{\frac {1}{3))&|x|\leq 1\\{\frac {1}{3))x^{-3}&|x|>1\end{cases))}$$

This can be written as

$${\displaystyle f(x)=\int _{1}^{\infty }{\frac {2}{w^{4))}h\left({\frac {x}{w))\right)dw}$$

$${\displaystyle h\left({\frac {x}{w))\right)={\begin{cases}{\frac {1}{2))&\left|{\frac {x}{w))\right|<1,\\0&\left|{\frac {x}{w))\right|>1.\end{cases))}$$

We want to find the leading terms of the asymptotic expansion of the characteristic function. The characteristic function of the probability distribution ${\textstyle {\frac {1}{w))h\left({\frac {x}{w))\right)}$ is ${\textstyle {\tfrac {\sin(tw)}{tw)),}$ so the characteristic function for f(x) is

$${\displaystyle \varphi (t)=\int _{1}^{\infty }{\frac {2\sin(tw)}{tw^{4))}dw}$$

$${\displaystyle {\begin{aligned}\varphi (t)-1&=\int _{1}^{\infty }{\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1\right]\,dw\\&=\int _{1}^{\frac {1}{|t|)){\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1\right]\,dw+\int _{\frac {1}{|t|))^{\infty }{\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1\right]\,dw\\&=\int _{1}^{\frac {1}{|t|)){\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1+\left\{-{\frac {t^{2}w^{2)){3!))+{\frac {t^{2}w^{2)){3!))\right\}\right]\,dw+\int _{\frac {1}{|t|))^{\infty }{\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1\right]\,dw\\&=\int _{1}^{\frac {1}{|t|))-{\frac {t^{2}dw}{3w))+\int _{1}^{\frac {1}{|t|)){\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1+{\frac {t^{2}w^{2)){3!))\right]dw+\int _{\frac {1}{|t|))^{\infty }{\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1\right]dw\\&=\int _{1}^{\frac {1}{|t|))-{\frac {t^{2}dw}{3w))+\left\{\int _{0}^{\frac {1}{|t|)){\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1+{\frac {t^{2}w^{2)){3!))\right]dw-\int _{0}^{1}{\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1+{\frac {t^{2}w^{2)){3!))\right]dw\right\}+\int _{\frac {1}{|t|))^{\infty }{\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1\right]dw\\&=\int _{1}^{\frac {1}{|t|))-{\frac {t^{2}dw}{3w))+t^{2}\int _{0}^{1}{\frac {2}{y^{3))}\left[{\frac {\sin(y)}{y))-1+{\frac {y^{2)){6))\right]dy-\int _{0}^{1}{\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1+{\frac {t^{2}w^{2)){6))\right]dw+t^{2}\int _{1}^{\infty }{\frac {2}{y^{3))}\left[{\frac {\sin(y)}{y))-1\right]dy\\&=-{\frac {t^{2)){3))\int _{1}^{\frac {1}{|t|)){\frac {dw}{w))+t^{2}C_{1}-\int _{0}^{1}{\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1+{\frac {t^{2}w^{2)){6))\right]dw+t^{2}C_{2}\\&={\frac {t^{2)){3))\ln |t|+t^{2}C_{3}-\int _{0}^{1}{\frac {2}{w^{3))}\left[{\frac {\sin(tw)}{tw))-1+{\frac {t^{2}w^{2)){6))\right]dw\\&={\frac {t^{2)){3))\ln |t|+t^{2}C_{3}-\int _{0}^{1}{\frac {2}{w^{3))}\left[{\frac {t^{4}w^{4)){5!))+\cdots \right]dw\\&={\frac {t^{2)){3))\ln |t|+t^{2}C_{3}-{\mathcal {O))\left(t^{4}\right)\end{aligned))}$$

${\displaystyle C_{1},C_{2))$

${\displaystyle C_{3))$

$${\displaystyle \varphi (t)\sim 1+{\frac {t^{2)){3))\ln |t|}$$

${\textstyle {\sqrt {n(\ln n)/12)),}$

Special cases

There is no general analytic solution for the form of f(x). There are, however three special cases which can be expressed in terms of elementary functions as can be seen by inspection of the characteristic function:^[7][9][21]

• For ${\displaystyle \alpha =2}$ the distribution reduces to a Gaussian distribution with variance σ² = 2c² and mean μ; the skewness parameter ${\displaystyle \beta }$ has no effect.
• For ${\displaystyle \alpha =1}$ and ${\displaystyle \beta =0}$ the distribution reduces to a Cauchy distribution with scale parameter c and shift parameter μ.
• For ${\displaystyle \alpha =1/2}$ and ${\displaystyle \beta =1}$ the distribution reduces to a Lévy distribution with scale parameter c and shift parameter μ.

Note that the above three distributions are also connected, in the following way: A standard Cauchy random variable can be viewed as a mixture of Gaussian random variables (all with mean zero), with the variance being drawn from a standard Lévy distribution. And in fact this is a special case of a more general theorem (See p. 59 of ^[22]) which allows any symmetric alpha-stable distribution to be viewed in this way (with the alpha parameter of the mixture distribution equal to twice the alpha parameter of the mixing distribution—and the beta parameter of the mixing distribution always equal to one).

A general closed form expression for stable PDFs with rational values of ${\displaystyle \alpha }$ is available in terms of Meijer G-functions.^[23] Fox H-Functions can also be used to express the stable probability density functions. For simple rational numbers, the closed form expression is often in terms of less complicated special functions. Several closed form expressions having rather simple expressions in terms of special functions are available. In the table below, PDFs expressible by elementary functions are indicated by an E and those that are expressible by special functions are indicated by an s.^[22]

		${\displaystyle \alpha }$
		1/3	1/2	2/3	1	4/3	3/2	2
${\displaystyle \beta }$	0	s	s	s	E	s	s	E
	1	s	E	s	L		s

Some of the special cases are known by particular names:

• For ${\displaystyle \alpha =1}$ and ${\displaystyle \beta =1}$, the distribution is a Landau distribution (L) which has a specific usage in physics under this name.
• For ${\displaystyle \alpha =3/2}$ and ${\displaystyle \beta =0}$ the distribution reduces to a Holtsmark distribution with scale parameter c and shift parameter μ.

Also, in the limit as c approaches zero or as α approaches zero the distribution will approach a Dirac delta function δ(x − μ).

Series representation

The stable distribution can be restated as the real part of a simpler integral:^[24]

$${\displaystyle f(x;\alpha ,\beta ,c,\mu )={\frac {1}{\pi ))\Re \left[\int _{0}^{\infty }e^{it(x-\mu )}e^{-(ct)^{\alpha }(1-i\beta \Phi )}\,dt\right].}$$

Expressing the second exponential as a Taylor series, this leads to:

$${\displaystyle f(x;\alpha ,\beta ,c,\mu )={\frac {1}{\pi ))\Re \left[\int _{0}^{\infty }e^{it(x-\mu )}\sum _{n=0}^{\infty }{\frac {(-qt^{\alpha })^{n)){n!))\,dt\right]}$$

${\displaystyle q=c^{\alpha }(1-i\beta \Phi )}$

$${\displaystyle f(x;\alpha ,\beta ,c,\mu )={\frac {1}{\pi ))\Re \left[\sum _{n=1}^{\infty }{\frac {(-q)^{n)){n!))\left({\frac {i}{x-\mu ))\right)^{\alpha n+1}\Gamma (\alpha n+1)\right]}$$

For one-sided stable distribution, the above series expansion needs to be modified, since ${\displaystyle q=\exp(-i\alpha \pi /2)}$ and ${\displaystyle qi^{\alpha }=1}$. There is no real part to sum. Instead, the integral of the characteristic function should be carried out on the negative axis, which yields:^[25][11]

$${\displaystyle {\begin{aligned}L_{\alpha }(x)&={\frac {1}{\pi ))\Re \left[\sum _{n=1}^{\infty }{\frac {(-q)^{n)){n!))\left({\frac {-i}{x))\right)^{\alpha n+1}\Gamma (\alpha n+1)\right]\\&={\frac {1}{\pi ))\sum _{n=1}^{\infty }{\frac {-\sin(n(\alpha +1)\pi )}{n!))\left({\frac {1}{x))\right)^{\alpha n+1}\Gamma (\alpha n+1)\end{aligned))}$$

Simulation of stable variables

Simulating sequences of stable random variables is not straightforward, since there are no analytic expressions for the inverse ${\displaystyle F^{-1}(x)}$ nor the CDF ${\displaystyle F(x)}$ itself.^[10][12] All standard approaches like the rejection or the inversion methods would require tedious computations. A much more elegant and efficient solution was proposed by Chambers, Mallows and Stuck (CMS),^[26] who noticed that a certain integral formula^[27] yielded the following algorithm:^[28]

• generate a random variable ${\displaystyle U}$ uniformly distributed on ${\displaystyle \left(-{\tfrac {\pi }{2)),{\tfrac {\pi }{2))\right)}$ and an independent exponential random variable ${\displaystyle W}$ with mean 1;
• for ${\displaystyle \alpha \neq 1}$ compute:
  $${\displaystyle X=\left(1+\zeta ^{2}\right)^{\frac {1}{2\alpha )){\frac {\sin(\alpha (U+\xi ))}{(\cos(U))^{\frac {1}{\alpha ))))\left({\frac {\cos(U-\alpha (U+\xi ))}{W))\right)^{\frac {1-\alpha }{\alpha )),}$$

  
• for ${\displaystyle \alpha =1}$ compute:
  $${\displaystyle X={\frac {1}{\xi ))\left\{\left({\frac {\pi }{2))+\beta U\right)\tan U-\beta \log \left({\frac ((\frac {\pi }{2))W\cos U}((\frac {\pi }{2))+\beta U))\right)\right\},}$$

  
  where
  $${\displaystyle \zeta =-\beta \tan {\frac {\pi \alpha }{2)),\qquad \xi ={\begin{cases}{\frac {1}{\alpha ))\arctan(-\zeta )&\alpha \neq 1\\{\frac {\pi }{2))&\alpha =1\end{cases))}$$

  

This algorithm yields a random variable ${\displaystyle X\sim S_{\alpha }(\beta ,1,0)}$. For a detailed proof see.^[29]

Given the formulas for simulation of a standard stable random variable, we can easily simulate a stable random variable for all admissible values of the parameters ${\displaystyle \alpha }$, ${\displaystyle c}$, ${\displaystyle \beta }$ and ${\displaystyle \mu }$ using the following property. If ${\displaystyle X\sim S_{\alpha }(\beta ,1,0)}$ then

$${\displaystyle Y={\begin{cases}cX+\mu &\alpha \neq 1\\cX+{\frac {2}{\pi ))\beta c\log c+\mu &\alpha =1\end{cases))}$$

${\displaystyle S_{\alpha }(\beta ,c,\mu )}$

${\displaystyle \alpha =2}$

${\displaystyle \beta =0}$

Applications

Stable distributions owe their importance in both theory and practice to the generalization of the central limit theorem to random variables without second (and possibly first) order moments and the accompanying self-similarity of the stable family. It was the seeming departure from normality along with the demand for a self-similar model for financial data (i.e. the shape of the distribution for yearly asset price changes should resemble that of the constituent daily or monthly price changes) that led Benoît Mandelbrot to propose that cotton prices follow an alpha-stable distribution with ${\displaystyle \alpha }$ equal to 1.7.^[6] Lévy distributions are frequently found in analysis of critical behavior and financial data.^[9][33]

They are also found in spectroscopy as a general expression for a quasistatically pressure broadened spectral line.^[24]

The Lévy distribution of solar flare waiting time events (time between flare events) was demonstrated for CGRO BATSE hard x-ray solar flares in December 2001. Analysis of the Lévy statistical signature revealed that two different memory signatures were evident; one related to the solar cycle and the second whose origin appears to be associated with a localized or combination of localized solar active region effects.^[34]

Other analytic cases

A number of cases of analytically expressible stable distributions are known. Let the stable distribution be expressed by ${\displaystyle f(x;\alpha ,\beta ,c,\mu )}$, then:

• The Cauchy Distribution is given by ${\displaystyle f(x;1,0,1,0).}$
• The Lévy distribution is given by ${\displaystyle f(x;{\tfrac {1}{2)),1,1,0).}$
• The Normal distribution is given by ${\displaystyle f(x;2,0,1,0).}$
• Let ${\displaystyle S_{\mu ,\nu }(z)}$ be a Lommel function, then:^[35]
  $${\displaystyle f\left(x;{\tfrac {1}{3)),0,1,0\right)=\Re \left({\frac {2e^{-{\frac {i\pi }{4)))){3{\sqrt {3))\pi )){\frac {1}{\sqrt {x^{3))))S_{0,{\frac {1}{3))}\left({\frac {2e^{\frac {i\pi }{4))}{3{\sqrt {3)))){\frac {1}{\sqrt {x))}\right)\right)}$$

  
• Let ${\displaystyle S(x)}$ and ${\displaystyle C(x)}$ denote the Fresnel integrals, then:^[36]
  $${\displaystyle f\left(x;{\tfrac {1}{2)),0,1,0\right)={\frac {1}{\sqrt {2\pi |x|^{3))))\left(\sin \left({\tfrac {1}{4|x|))\right)\left[{\frac {1}{2))-S\left({\tfrac {1}{\sqrt {2\pi |x|))}\right)\right]+\cos \left({\tfrac {1}{4|x|))\right)\left[{\frac {1}{2))-C\left({\tfrac {1}{\sqrt {2\pi |x|))}\right)\right]\right)}$$

  
• Let ${\displaystyle K_{v}(x)}$ be the modified Bessel function of the second kind, then:^[36]
  $${\displaystyle f\left(x;{\tfrac {1}{3)),1,1,0\right)={\frac {1}{\pi )){\frac {2{\sqrt {2))}{3^{\frac {7}{4)))){\frac {1}{\sqrt {x^{3))))K_{\frac {1}{3))\left({\frac {4{\sqrt {2))}{3^{\frac {9}{4)))){\frac {1}{\sqrt {x))}\right)}$$

  
• If the ${\displaystyle {}_{m}F_{n))$ denote the hypergeometric functions, then:^[35]
  $${\displaystyle {\begin{aligned}f\left(x;{\tfrac {4}{3)),0,1,0\right)&={\frac {3^{\frac {5}{4))}{4{\sqrt {2\pi )))){\frac {\Gamma \left({\tfrac {7}{12))\right)\Gamma \left({\tfrac {11}{12))\right)}{\Gamma \left({\tfrac {6}{12))\right)\Gamma \left({\tfrac {8}{12))\right))){}_{2}F_{2}\left({\tfrac {7}{12)),{\tfrac {11}{12));{\tfrac {6}{12)),{\tfrac {8}{12));{\tfrac {3^{3}x^{4)){4^{4))}\right)-{\frac {3^{\frac {11}{4))x^{3)){4^{3}{\sqrt {2\pi )))){\frac {\Gamma \left({\tfrac {13}{12))\right)\Gamma \left({\tfrac {17}{12))\right)}{\Gamma \left({\tfrac {18}{12))\right)\Gamma \left({\tfrac {15}{12))\right))){}_{2}F_{2}\left({\tfrac {13}{12)),{\tfrac {17}{12));{\tfrac {18}{12)),{\tfrac {15}{12));{\tfrac {3^{3}x^{4)){4^{4))}\right)\\[6pt]f\left(x;{\tfrac {3}{2)),0,1,0\right)&={\frac {\Gamma \left({\tfrac {5}{3))\right)}{\pi )){}_{2}F_{3}\left({\tfrac {5}{12)),{\tfrac {11}{12));{\tfrac {1}{3)),{\tfrac {1}{2)),{\tfrac {5}{6));-{\tfrac {2^{2}x^{6)){3^{6))}\right)-{\frac {x^{2)){3\pi )){}_{3}F_{4}\left({\tfrac {3}{4)),1,{\tfrac {5}{4));{\tfrac {2}{3)),{\tfrac {5}{6)),{\tfrac {7}{6)),{\tfrac {4}{3));-{\tfrac {2^{2}x^{6)){3^{6))}\right)+{\frac {7x^{4}\Gamma \left({\tfrac {4}{3))\right)}{3^{4}\pi ^{2))}{}_{2}F_{3}\left({\tfrac {13}{12)),{\tfrac {19}{12));{\tfrac {7}{6)),{\tfrac {3}{2)),{\tfrac {5}{3));-{\tfrac {2^{2}x^{6)){3^{6))}\right)\end{aligned))}$$

  
  with the latter being the Holtsmark distribution.
• Let ${\displaystyle W_{k,\mu }(z)}$ be a Whittaker function, then:^[37][38][39]
  $${\displaystyle {\begin{aligned}f\left(x;{\tfrac {2}{3)),0,1,0\right)&={\frac {\sqrt {3)){6{\sqrt {\pi ))|x|))\exp \left({\tfrac {2}{27))x^{-2}\right)W_{-{\frac {1}{2)),{\frac {1}{6))}\left({\tfrac {4}{27))x^{-2}\right)\\[8pt]f\left(x;{\tfrac {2}{3)),1,1,0\right)&={\frac {\sqrt {3))((\sqrt {\pi ))|x|))\exp \left(-{\tfrac {16}{27))x^{-2}\right)W_((\frac {1}{2)),{\frac {1}{6))}\left({\tfrac {32}{27))x^{-2}\right)\\[8pt]f\left(x;{\tfrac {3}{2)),1,1,0\right)&={\begin{cases}{\frac {\sqrt {3))((\sqrt {\pi ))|x|))\exp \left({\frac {1}{27))x^{3}\right)W_((\frac {1}{2)),{\frac {1}{6))}\left(-{\frac {2}{27))x^{3}\right)&x<0\\{}\\{\frac {\sqrt {3)){6{\sqrt {\pi ))|x|))\exp \left({\frac {1}{27))x^{3}\right)W_{-{\frac {1}{2)),{\frac {1}{6))}\left({\frac {2}{27))x^{3}\right)&x\geq 0\end{cases))\end{aligned))}$$