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Statistical modelling constructs, fits, checks, and interprets a statistical model for observed data.

A statistical parameter indexes a family of probability distributions in a statistical model. It is fixed in a frequentist sampling model; a prior distribution makes it random for Bayesian statistics. Different statistical parameter values should produce different observable distributions when identifiability is claimed.

A statistical path is a one-dimensional family of probability measures inside a statistical model, passing through a specified baseline $P$. A differentiability in quadratic mean condition gives its score function, the first-order direction of the family in square-root-density coordinates. The path must respect all restrictions of the statistical model, including normalization and any fixed moments.

A collection of observed random variables used to infer a statistical model or its parameters. A common assumption is that the observations are independent and identically distributed random variables; dependence must otherwise be included in the model. Its randomness induces the sampling distribution of a statistic.

Statistical sampling selects observations from a target statistical population through an explicit selection procedure or statistical model. It links observed values to the larger collection about which conclusions are sought. The accessible sampling frame and the statistical population need not coincide, which can cause sampling bias even in a large statistical sample.

For a finite statistical population with values $y_1,\dots ,y_N$, suppose every unit has known positive inclusion probability ${\pi }_i$. If $s$ is the selected statistical sample, thenis an unbiased estimator of the total $Y={\sum }_i{y}_i$. Indeed, writing the sum with inclusion indicator functions gives $\mathbb{E}\hat{Y}={\sum }_i{y}_i{\pi }_i/{\pi }_i=Y$. Under simple random sampling without replacement of size $n$, ${\pi }_i=n/N$, so $\hat{Y}/N$ is the sample mean. The selection procedure also determines dependence between selected units and the resulting sampling variability; unbiasedness alone does not specify its size.

A statistician develops or applies methods for collecting data and learning from it under uncertainty. The work connects experimental design, probability models, estimation and statistical hypothesis testing. For example, deciding how many independent observations to collect requires linking the desired precision of a confidence interval to the variation expected under a statistical model. Interpreting results also requires examining sampling bias, missing data and assumptions about dependence.

Statistics studies how to learn from data while accounting for variation and uncertainty. Descriptive statistics summarizes observations; statistical inference uses an explicit statistical model to estimate unknown quantities or assess claims. For example, the sample mean estimates a population mean, while its standard error describes variation across hypothetical repeated statistical samples. A large dataset does not automatically remove bias from statistical sampling or confounding. The design generating the observations is part of the reasoning, rather than an optional prelude to calculating a formula.

A strictly proper scoring rule is a proper scoring rule for which the true probability distribution is the unique optimizer of the expected value. Equivalently, any different admissible probability distribution gives strictly larger expected loss. For probability density functions, two densities that agree almost everywhere represent the same probability distribution. Ordinary propriety permits ties: the constant reward $S(P,x)=0$ is a proper scoring rule, because every report ties, but it is not a strictly proper scoring rule and elicits no information.

Strict propriety concerns expectation, not guaranteed success on each observation or each realized dataset. With the stipulated Bernoulli distribution $q=0.7$, suppose the outcome is $Y=0$. The honest report $p=0.7$ then has Brier score loss $0.49$, while $p=0.2$ has loss $0.04$. The logarithmic loss similarly gives losses $-\ln (0.3)\approx 1.203973$ and $-\ln (0.8)\approx 0.223144$. The honest forecast loses this comparison on that draw, which occurs with probability $0.3$ in the stipulated statistical model.

The $Y=0$ loss curves favor $p=0$, and the $Y=1$ loss curves favor $p=1$. Their weighted average, with weights $0.3$ and $0.7$, favors $p=0.7$. Choosing a report after observing $Y$ would use information unavailable at forecast time. Even an average loss on a finite dataset can rank an honest forecast below a competing forecast through outcome variation; strict propriety guarantees the ranking in expected value under the specified information and true predictive distribution.

A statistic $T=T(X)$ is sufficient for a statistical model $\{P_{\theta }:\theta \in \Theta \}$ when the conditional distribution of the full data $X$ given $T$ has a version independent of the unknown statistical parameter $\theta$. Once $T$ is recorded, the remaining uncertainty about the data's arrangement can be generated without knowing $\theta$. ^[ref]

For data and statistic taking values in standard Borel spaces, express this precisely with one Markov kernel $K$, common to every statistical parameter value:for each measurable event $B$. Thus $K(t,\cdot )$ is a regular conditional distribution of $X$ given $T=t$. Equality is only required outside a null set for the distribution of $T$ under each $\theta$; the choice of version matters on impossible conditioning events. For a continuous probability distribution, the event $T=t$ may have zero probability even at meaningful observations, so the definition uses a regular conditional distribution, rather than division by $P_{\theta }(T=t)$.

A sufficient statistic is a property of a specified statistical model, rather than of a formula for summarizing data in isolation. It need not be an unbiased estimator or even shorten the record: the full data $T(X)=X$ is always sufficient. An estimator instead targets a quantity such as a mean. An ancillary statistic has a parameter-independent marginal probability distribution, whereas a sufficient statistic has a parameter-independent conditional full-data law. A minimal sufficient statistic permits the greatest reduction among sufficient statistics. A complete statistic satisfies a separate condition about zero expectations; a complete sufficient statistic must satisfy both conditions.

Thomas S. Richardson develops graphical approaches to causal inference and statistical models, including ways to reason when some variables are hidden. His institutional research description lists graphical models, model selection, Bayesian inference and causal models.^[ref]

He is a coauthor of Nested Markov Properties for Acyclic Directed Mixed Graphs by Thomas S. Richardson and others. The work represents observable constraints of hidden-variable directed graphs using a nested Markov model. Its motivation is that eliminating a hidden cause can leave more than ordinary conditional independence restrictions among the measured variables.^[ref]

For example, a hidden common cause of two observed variables can be represented by a bidirected edge in a latent projection. The graph records a possible dependence source without pretending that the common cause itself was measured. Such representations separate what observations constrain from what remains unidentifiable.

Trevor Hastie develops methods in statistical learning, including generalized additive models and regularized regression. His research page describes the interaction between interpretable statistical models, flexible prediction and efficient computation.^[ref]

His joint Graphical Lasso work with Jerome H. Friedman and Robert Tibshirani turns sparse precision matrix estimation into repeated Lasso subproblems. A blockwise algorithm updates parts of the estimate while solving the penalized likelihood problem, making large conditional-dependence models computationally feasible.^[ref]

rounding an unclipped voltage to equally spaced levels of separation $\Delta$ leaves error in $[-\Delta /2,\Delta /2]$. If the fractional position within a conversion interval is uniformly distributed, direct integration gives zero mean and expectation value $⟨{ϵ}^2⟩={\Delta }^2/12$. This is a statistical model for the error, not a claim that the converter adds independent white noise for every possible input.