Chain_rule_(probability)

Chain rule (probability)

Probability theory concept

In probability theory, the chain rule^[1] (also called the general product rule^[2]^[3]) describes how to calculate the probability of the intersection of, not necessarily independent, events or the joint distribution of random variables respectively, using conditional probabilities. The rule is notably used in the context of discrete stochastic processes and in applications, e.g. the study of Bayesian networks, which describe a probability distribution in terms of conditional probabilities.

Chain rule for events

Two events

For two events $A$ and $B$ , the chain rule states that

\mathbb {P} (A\cap B)=\mathbb {P} (B\mid A)\mathbb {P} (A)

,

where $\mathbb {P} (B\mid A)$ denotes the conditional probability of $B$ given $A$ .

Example

An Urn A has 1 black ball and 2 white balls and another Urn B has 1 black ball and 3 white balls. Suppose we pick an urn at random and then select a ball from that urn. Let event $A$ be choosing the first urn, i.e. $\mathbb {P} (A)=\mathbb {P} ({\overline {A}})=1/2$ , where ${\overline {A}}$ is the complementary event of $A$ . Let event $B$ be the chance we choose a white ball. The chance of choosing a white ball, given that we have chosen the first urn, is $\mathbb {P} (B|A)=2/3.$ The intersection $A\cap B$ then describes choosing the first urn and a white ball from it. The probability can be calculated by the chain rule as follows:

\mathbb {P} (A\cap B)=\mathbb {P} (B\mid A)\mathbb {P} (A)={\frac {2}{3}}\cdot {\frac {1}{2}}={\frac {1}{3}}.

Finitely many events

For events $A_{1},\ldots ,A_{n}$ whose intersection has not probability zero, the chain rule states

{\begin{aligned}\mathbb {P} \left(A_{1}\cap A_{2}\cap \ldots \cap A_{n}\right)&=\mathbb {P} \left(A_{n}\mid A_{1}\cap \ldots \cap A_{n-1}\right)\mathbb {P} \left(A_{1}\cap \ldots \cap A_{n-1}\right)\\&=\mathbb {P} \left(A_{n}\mid A_{1}\cap \ldots \cap A_{n-1}\right)\mathbb {P} \left(A_{n-1}\mid A_{1}\cap \ldots \cap A_{n-2}\right)\mathbb {P} \left(A_{1}\cap \ldots \cap A_{n-2}\right)\\&=\mathbb {P} \left(A_{n}\mid A_{1}\cap \ldots \cap A_{n-1}\right)\mathbb {P} \left(A_{n-1}\mid A_{1}\cap \ldots \cap A_{n-2}\right)\cdot \ldots \cdot \mathbb {P} (A_{3}\mid A_{1}\cap A_{2})\mathbb {P} (A_{2}\mid A_{1})\mathbb {P} (A_{1})\\&=\mathbb {P} (A_{1})\mathbb {P} (A_{2}\mid A_{1})\mathbb {P} (A_{3}\mid A_{1}\cap A_{2})\cdot \ldots \cdot \mathbb {P} (A_{n}\mid A_{1}\cap \dots \cap A_{n-1})\\&=\prod _{k=1}^{n}\mathbb {P} (A_{k}\mid A_{1}\cap \dots \cap A_{k-1})\\&=\prod _{k=1}^{n}\mathbb {P} \left(A_{k}\,{\Bigg |}\,\bigcap _{j=1}^{k-1}A_{j}\right).\end{aligned}}

Example 1

For $n=4$ , i.e. four events, the chain rule reads

{\begin{aligned}\mathbb {P} (A_{1}\cap A_{2}\cap A_{3}\cap A_{4})&=\mathbb {P} (A_{4}\mid A_{3}\cap A_{2}\cap A_{1})\mathbb {P} (A_{3}\cap A_{2}\cap A_{1})\\&=\mathbb {P} (A_{4}\mid A_{3}\cap A_{2}\cap A_{1})\mathbb {P} (A_{3}\mid A_{2}\cap A_{1})\mathbb {P} (A_{2}\cap A_{1})\\&=\mathbb {P} (A_{4}\mid A_{3}\cap A_{2}\cap A_{1})\mathbb {P} (A_{3}\mid A_{2}\cap A_{1})\mathbb {P} (A_{2}\mid A_{1})\mathbb {P} (A_{1})\end{aligned}}

.

Example 2

We randomly draw 4 cards without replacement from deck with 52 cards. What is the probability that we have picked 4 aces?

First, we set ${\textstyle A_{n}:=\left\{{\text{draw an ace in the }}n^{\text{th}}{\text{ try}}\right\}}$ . Obviously, we get the following probabilities

\mathbb {P} (A_{1})={\frac {4}{52}},\qquad \mathbb {P} (A_{2}\mid A_{1})={\frac {3}{51}},\qquad \mathbb {P} (A_{3}\mid A_{1}\cap A_{2})={\frac {2}{50}},\qquad \mathbb {P} (A_{4}\mid A_{1}\cap A_{2}\cap A_{3})={\frac {1}{49}}

.

Applying the chain rule,

\mathbb {P} (A_{1}\cap A_{2}\cap A_{3}\cap A_{4})={\frac {4}{52}}\cdot {\frac {3}{51}}\cdot {\frac {2}{50}}\cdot {\frac {1}{49}}

.

Statement of the theorem and proof

Let $(\Omega ,{\mathcal {A}},\mathbb {P} )$ be a probability space. Recall that the conditional probability of an $A\in {\mathcal {A}}$ given $B\in {\mathcal {A}}$ is defined as

{\begin{aligned}\mathbb {P} (A\mid B):={\begin{cases}{\frac {\mathbb {P} (A\cap B)}{\mathbb {P} (B)}},&\mathbb {P} (B)>0,\\0&\mathbb {P} (B)=0.\end{cases}}\end{aligned}}

Then we have the following theorem.

Chain rule — Let $(\Omega ,{\mathcal {A}},\mathbb {P} )$ be a probability space. Let $A_{1},...,A_{n}\in {\mathcal {A}}$ . Then

{\begin{aligned}\mathbb {P} \left(A_{1}\cap A_{2}\cap \ldots \cap A_{n}\right)&=\mathbb {P} (A_{1})\mathbb {P} (A_{2}\mid A_{1})\mathbb {P} (A_{3}\mid A_{1}\cap A_{2})\cdot \ldots \cdot \mathbb {P} (A_{n}\mid A_{1}\cap \dots \cap A_{n-1})\\&=\mathbb {P} (A_{1})\prod _{j=2}^{n}\mathbb {P} (A_{j}\mid A_{1}\cap \dots \cap A_{j-1}).\end{aligned}}

Proof

The formula follows immediately by recursion

{\begin{aligned}(1)&&&\mathbb {P} (A_{1})\mathbb {P} (A_{2}\mid A_{1})&=&\qquad \mathbb {P} (A_{1}\cap A_{2})\\(2)&&&\mathbb {P} (A_{1})\mathbb {P} (A_{2}\mid A_{1})\mathbb {P} (A_{3}\mid A_{1}\cap A_{2})&=&\qquad \mathbb {P} (A_{1}\cap A_{2})\mathbb {P} (A_{3}\mid A_{1}\cap A_{2})\\&&&&=&\qquad \mathbb {P} (A_{1}\cap A_{2}\cap A_{3}),\end{aligned}}

where we used the definition of the conditional probability in the first step.

Chain rule for discrete random variables

Two random variables

For two discrete random variables $X,Y$ , we use the events $A:=\{X=x\}$ and $B:=\{Y=y\}$ in the definition above, and find the joint distribution as

\mathbb {P} (X=x,Y=y)=\mathbb {P} (X=x\mid Y=y)\mathbb {P} (Y=y),

or

\mathbb {P} _{(X,Y)}(x,y)=\mathbb {P} _{X\mid Y}(x\mid y)\mathbb {P} _{Y}(y),

where $\mathbb {P} _{X}(x):=\mathbb {P} (X=x)$ is the probability distribution of $X$ and $\mathbb {P} _{X\mid Y}(x\mid y)$ conditional probability distribution of $X$ given $Y$ .

Finitely many random variables

Let $X_{1},\ldots ,X_{n}$ be random variables and $x_{1},\dots ,x_{n}\in \mathbb {R}$ . By the definition of the conditional probability,

\mathbb {P} \left(X_{n}=x_{n},\ldots ,X_{1}=x_{1}\right)=\mathbb {P} \left(X_{n}=x_{n}|X_{n-1}=x_{n-1},\ldots ,X_{1}=x_{1}\right)\mathbb {P} \left(X_{n-1}=x_{n-1},\ldots ,X_{1}=x_{1}\right)

and using the chain rule, where we set $A_{k}:=\{X_{k}=x_{k}\}$ , we can find the joint distribution as

{\begin{aligned}\mathbb {P} \left(X_{1}=x_{1},\ldots X_{n}=x_{n}\right)&=\mathbb {P} \left(X_{1}=x_{1}\mid X_{2}=x_{2},\ldots ,X_{n}=x_{n}\right)\mathbb {P} \left(X_{2}=x_{2},\ldots ,X_{n}=x_{n}\right)\\&=\mathbb {P} (X_{1}=x_{1})\mathbb {P} (X_{2}=x_{2}\mid X_{1}=x_{1})\mathbb {P} (X_{3}=x_{3}\mid X_{1}=x_{1},X_{2}=x_{2})\cdot \ldots \\&\qquad \cdot \mathbb {P} (X_{n}=x_{n}\mid X_{1}=x_{1},\dots ,X_{n-1}=x_{n-1})\\\end{aligned}}

Example

For $n=3$ , i.e. considering three random variables. Then, the chain rule reads

{\begin{aligned}\mathbb {P} _{(X_{1},X_{2},X_{3})}(x_{1},x_{2},x_{3})&=\mathbb {P} (X_{1}=x_{1},X_{2}=x_{2},X_{3}=x_{3})\\&=\mathbb {P} (X_{3}=x_{3}\mid X_{2}=x_{2},X_{1}=x_{1})\mathbb {P} (X_{2}=x_{2},X_{1}=x_{1})\\&=\mathbb {P} (X_{3}=x_{3}\mid X_{2}=x_{2},X_{1}=x_{1})\mathbb {P} (X_{2}=x_{2}\mid X_{1}=x_{1})\mathbb {P} (X_{1}=x_{1})\\&=\mathbb {P} _{X_{3}\mid X_{2},X_{1}}(x_{3}\mid x_{2},x_{1})\mathbb {P} _{X_{2}\mid X_{1}}(x_{2}\mid x_{1})\mathbb {P} _{X_{1}}(x_{1}).\end{aligned}}

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[1] [1]
Schilling, René L. (2021). Measure, Integral, Probability & Processes - Probab(ilistical)ly the Theoretical Minimum. Technische Universität Dresden, Germany. p. 136ff. ISBN 979-8-5991-0488-9.{{cite book}}: CS1 maint: location missing publisher (link)

[2] [2]
Schum, David A. (1994). The Evidential Foundations of Probabilistic Reasoning. Northwestern University Press. p. 49. ISBN 978-0-8101-1821-8.

[3] [3]
Klugh, Henry E. (2013). Statistics: The Essentials for Research (3rd ed.). Psychology Press. p. 149. ISBN 978-1-134-92862-0.

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Chain_rule_(probability)

Chain rule (probability)

Chain rule for events

Two events

Example

Finitely many events

Example 1

Example 2

Statement of the theorem and proof

Chain rule for discrete random variables

Two random variables

Finitely many random variables

Example

Bibliography

References

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