Many facts about the useful, boring, ubiquitous Gaussian. Djalil Chafaï lists Three reasons for Gaussians, emphasising more abstract, not-necessarily generative reasons.

- Gaussians as isotropic distributions — a Gaussian is the only distribution that can be both marginally independent and isotropic.
- Entropy maximizing (the Gaussian has the highest entropy out of any distribution wath fixed variance and finite entropy)
- The only stable distribution with finite variance

Many other things give rise to Gaussians;
sampling distributions for test statistics, bootstrap samples, low dimensional projections, anything with the right Stein-type symmetries…
There are also many *post hoc* rationalisations that use the Gaussian in the hope that it is close enough to the real distribution: such as when we assume something is a Gaussian process or seek a noise distribution that will justify quadratic loss, when we use Brownian motions in stochastic calculus because it comes out neatly, and so on.

## Density, CDF

The standard (univariate) Gaussian pdf is \[ \psi:x\mapsto \frac{1}{\sqrt{2\pi}}\text{exp}\left(-\frac{x^2}{2}\right) \] Typically we allow a scale-location parameterised version \[ \phi(x; \mu,\sigma ^{2})={\frac {1}{\sqrt {2\pi \sigma ^{2}}}}e^{-{\frac {(x-\mu )^{2}}{2\sigma ^{2}}}} \] We will call the CDF \[ \Psi:x\mapsto \int_{-\infty}^x\psi(t) dt. \] In the multivariate case, where the covariance \(\Sigma\) is strictly positive definite we can write a density of the general normal distribution over \(\mathbb{R}^k\) as \[ \psi({x}; \mu, \Sigma) = (2\pi )^{-{\frac {k}{2}}}\det({ {\Sigma }})^{-{\frac {1}{2}}}\,e^{-{\frac {1}{2}}( {x} -{ {\mu }})^{\!{\top}}{ {\Sigma }}^{-1}( {x} -{ {\mu }})} \] If a random variable \(Y\) has a Gaussian distribution with parameters \(\mu, \Sigma\), we write \[Y \sim \mathcal{N}(\mu, \Sigma)\]

Taylor expansion of \(e^{-x^2/2}\) \[ e^(-x^2/2) = \sum_{k=0}^{\infty} (2^(-k) (-x^2)^k)/(k!). \]

### Mills ratio

Mills’ ratio is \((1 - \Phi(x))/\phi(x)\) and is a workhorse for tail inequalities for Gaussians. See the review and extensions of classic results in Dümbgen (2010), found via Mike Spivey.

He gives an extended justification for the classic identity

\[ \int_x^{\infty} \frac{1}{\sqrt{2\pi}} e^{-t^2/2} dt \leq \int_x^{\infty} \frac{t}{x} \frac{1}{\sqrt{2\pi}} e^{-t^2/2} dt = \frac{e^{-x^2/2}}{x\sqrt{2\pi}}.\]

## Differential representations

First, trivially, \(\phi'(x)=-\frac{e^{-\frac{x^2}{2}} x}{\sqrt{2 \pi }}.\)

### Stein’s lemma

Meckes (2009) explains Stein (1972)’s characterisation:

The normal distribution is the unique probability measure \(\mu\) for which \[ \int\left[f^{\prime}(x)-x f(x)\right] \mu(d x)=0 \] for all \(f\) for which the left-hand side exists and is finite.

This is incredibly useful in probability approximation by Gaussians where it justifies Stein’s method.

### ODE representation for the univariate density

\[\begin{aligned} \sigma ^2 \phi'(x)+\phi(x) (x-\mu )&=0, \text{ i.e.}\\ L(x) &=(\sigma^2 D+x-\mu)\\ \end{aligned}\]

With initial conditions

\[\begin{aligned} \phi(0) &=\frac{e^{-\mu ^2/(2\sigma ^2)}}{\sqrt{2 \sigma^2\pi } }\\ \phi'(0) &=0 \end{aligned}\]

🏗 note where I learned this.

### ODE representation for the univariate icdf

From (Steinbrecher and Shaw 2008) via Wikipedia.

Let us write \(w:=\Psi^{-1}\) to suppress keep notation clear.

\[\begin{aligned} {\frac {d^{2}w}{dp^{2}}} &=w\left({\frac {dw}{dp}}\right)^{2}\\ \end{aligned}\]

With initial conditions

\[\begin{aligned} w\left(1/2\right)&=0,\\ w'\left(1/2\right)&={\sqrt {2\pi }}. \end{aligned}\]

### Density PDE representation as a diffusion equation

Z. I. Botev, Grotowski, and Kroese (2010) notes

\[\begin{aligned} \frac{\partial}{\partial t}\phi(x;t) &=\frac{1}{2}\frac{\partial^2}{\partial x^2}\phi(x;t)\\ \phi(x;0)&=\delta(x-\mu) \end{aligned}\]

Look, it’s the diffusion equation of Wiener process. Surprise! If you think about this for a while you end up discovering Feynman-Kac formulate.

## Extremes

For small \(p\), the quantile function has the asymptotic expansion \[ \Phi^{-1}(p) = -\sqrt{\ln\frac{1}{p^2} - \ln\ln\frac{1}{p^2} - \ln(2\pi)} + \mathcal{o}(1). \]

## Orthogonal basis

Polynomial basis? You want the Hermite polynomials.

## Rational function approximations

🏗

## Roughness

Univariate -

\[\begin{aligned} \left\| \frac{d}{dx}\phi_\sigma \right\|_2 &= \frac{1}{4\sqrt{\pi}\sigma^3}\\ \left\| \left(\frac{d}{dx}\right)^n \phi_\sigma \right\|_2 &= \frac{\prod_{i<n}2n-1}{2^{n+1}\sqrt{\pi}\sigma^{2n+1}} \end{aligned}\]

## Entropy

The normal distribution is the least “surprising” distribution in the sense that out of all distributions with a given mean and variance the Gaussian has the maximum entropy. Or maybe that is the most surprising, depending on your definition.

## Multidimensional marginals and conditionals

Linear transforms of Gaussians are especially convenient. You could say that this is a definitional property of the Gaussian, in fact, and it arises conveniently from linear superposition. As made famous by Wiener processes in finance and Gaussian process regression in Bayesian nonparametrics.

See, e.g. these lectures, or Michael I Jordan’s backgrounders.

In practice I look up my favourite useful Gaussian identities in Petersen and Pedersen (2012) and so does everyone else I know.

## Fourier representation

The Fourier transform/Characteristic function of a Gaussian is still Gaussian.

\[\mathbb{E}\exp (i\mathbf{t}\cdot \mathbf {X}) =\exp \left( i\mathbf {t} ^{\top}{\boldsymbol {\mu }}-{\tfrac {1}{2}}\mathbf {t} ^{\top}{\boldsymbol {\Sigma }}\mathbf {t} \right).\]

## Transformed variables

Special case.

\[ Y \sim \mathcal{N}(X\beta, I) \]

implies

\[ W^{1/2}Y \sim \mathcal{N}(W^{1/2}X\beta, W) \]

For more general transforms you could try polynomial chaos.

## Metrics

Since Gaussian approximations pop up a lot in e.g. variational approximation problems, it is nice to know how to approximate them in probability metrics.

### Wasserstein

Useful: Two Gaussians may be related thusly in Wasserstein-2 distance, i.e. \(W_2(\mu;\nu):=\inf\mathbb{E}(\Vert X-Y\Vert_2^2)^{1/2}\) for \(X\sim\nu\), \(Y\sim\mu\).

\[\begin{aligned} d&:= W_2(\mathcal{N}(\mu_1,\Sigma_1);\mathcal{N}(\mu_2,\Sigma_2))\\ \Rightarrow d^2&= \Vert \mu_1-\mu_2\Vert_2^2 + \operatorname{tr}(\Sigma_1+\Sigma_2-2(\Sigma_1^{1/2}\Sigma_2\Sigma_1^{1/2})^{1/2}). \end{aligned}\]

In the centred case this is simply (Givens and Shortt 1984)

\[\begin{aligned} d&:= W_2(\mathcal{N}(0,\Sigma_1);\mathcal{N}(0,\Sigma_2))\\ \Rightarrow d^2&= \operatorname{tr}(\Sigma_1+\Sigma_2-2(\Sigma_1^{1/2}\Sigma_2\Sigma_1^{1/2})^{1/2}). \end{aligned}\]

### Kullback-Leibler

Pulled from wikipedia:

\[ D_{\text{KL}}(\mathcal{N}(\mu_1,\Sigma_1)\parallel \mathcal{N}(\mu_2,\Sigma_2)) ={\frac {1}{2}}\left(\operatorname {tr} \left(\Sigma _{2}^{-1}\Sigma _{1}\right)+(\mu_{2}-\mu_{1})^{\mathsf {T}}\Sigma _{2}^{-1}(\mu_{2}-\mu_{1})-k+\ln \left({\frac {\det \Sigma _{2}}{\det \Sigma _{1}}}\right)\right).\]

In the centred case this reduces to

\[ D_{\text{KL}}(\mathcal{N}(0,\Sigma_1)\parallel \mathcal{N}(0, \Sigma_2)) ={\frac {1}{2}}\left(\operatorname{tr} \left(\Sigma _{2}^{-1}\Sigma _{1}\right)-k+\ln \left({\frac {\det \Sigma _{2}}{\det \Sigma _{1}}}\right)\right).\]

### Hellinger

Djalil
defines both Hellinger *distance*

\[\mathrm{H}(\mu,\nu) ={\Vert\sqrt{f}-\sqrt{g}\Vert}_{\mathrm{L}^2(\lambda)} =\Bigr(\int(\sqrt{f}-\sqrt{g})^2\mathrm{d}\lambda\Bigr)^{1/2}.\]

and Hellinger *affinity*

\[\mathrm{A}(\mu,\nu) =\int\sqrt{fg}\mathrm{d}\lambda, \quad \mathrm{H}(\mu,\nu)^2 =2-2A(\mu,\nu).\]

For Gaussians we can find this exactly:

\[\mathrm{A}(\mathcal{N}(m_1,\sigma_1^2),\mathcal{N}(m_2,\sigma_2^2)) =\sqrt{2\frac{\sigma_1\sigma_2}{\sigma_1^2+\sigma_2^2}} \exp\Bigr(-\frac{(m_1-m_2)^2}{4(\sigma_1^2+\sigma_2^2)}\Bigr),\]

In multiple dimensions:

\[\mathrm{A}(\mathcal{N}(m_1,\Sigma_1),\mathcal{N}(m_2,\Sigma_2)) =\frac{\det(\Sigma_1\Sigma_2)^{1/4}}{\det(\frac{\Sigma_1+\Sigma_2}{2})^{1/2}} \exp\Bigr(-\frac{\langle\Delta m,(\Sigma_1+\Sigma_2)^{-1}\Delta m)\rangle}{4}\Bigr).\]

## What is Erf again?

This *erf*, or *error function*, is a rebranding and reparameterisation of the
standard univariate normal cdf popular in computer science, to provide a slightly differently ambiguity to the one you are used to with the “normal” density.
There are scaling factors tacked on.

\[ \operatorname{erf}(x) = \frac{1}{\sqrt{\pi}} \int_{-x}^x e^{-t^2} \, dt \] which is to say \[\begin{aligned} \Phi(x) &={\frac {1}{2}}\left[1+\operatorname {erf} \left({\frac {x}{\sqrt {2}}}\right)\right]\\ \operatorname {erf}(x) &=2\Phi (\sqrt{2}x)-1\\ \end{aligned}\]

## Matrix Gaussian

See Gupta and Nagar (2018).

## Incoming

## References

*Journal of the Royal Statistical Society: Series B (Statistical Methodology)*79 (1): 125–48.

*The Annals of Statistics*38 (5): 2916–57.

*arXiv:1012.2063 [Math, Stat]*, December.

*The Michigan Mathematical Journal*31 (2): 231–40.

*Matrix Variate Distributions*. CRC Press.

*Matrix Differential Calculus with Applications in Statistics and Econometrics*. Rev. ed. New York: John Wiley.

*High Dimensional Probability V: The Luminy Volume*, 153–78. Beachwood, Ohio, USA: Institute of Mathematical Statistics.

*Old and new matrix algebra useful for statistics*.

*Journal of Mathematics Research*2 (4): p47.

*Electronic Journal of Applied Statistical Analysis*5 (1).

*Proceedings of the Sixth Berkeley Symposium on Mathematical Statistics and Probability, Volume 2: Probability Theory*, January, 583–602.

*Approximate Computation of Expectations*. Vol. 7. IMS.

*European Journal of Applied Mathematics*19 (2): 87–112.

*Mathematics of Computation*22 (101): 144–58.

*Journal of the Royal Statistical Society. Series C (Applied Statistics)*37 (3): 477–84.

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