Randomized Algorithms (Spring 2010)/The probabilistic method

The Basic Idea

Counting or sampling

Circuit complexity

A boolean function is a function is the form [math]\displaystyle{ f:\{0,1\}^n\rightarrow \{0,1\} }[/math].

Formally, a boolean circuit is a directed acyclic graph. Nodes with indegree zero are input nodes, labeled [math]\displaystyle{ x_1, x_2, \ldots , x_n }[/math]. A circuit has a unique node with outdegree zero, called the output node. Every other node is a gate. There are three types of gates: AND, OR (both with indegree two), and NOT (with indegree one).

Computations in Turing machines can be simulated by circuits, and any boolean function in P can be computed by a circuit with polynomially many gates. Thus, if we can find a function in NP that cannot be computed by any circuit with polynomially many gates, then NP[math]\displaystyle{ \neq }[/math]P.

The following theorem due to Shannon says that functions with exponentially large circuit complexity do exist.

Theorem (Shannon 1949) There is a boolean function [math]\displaystyle{ f:\{0,1\}^n\rightarrow \{0,1\} }[/math] with circuit complexity greater than [math]\displaystyle{ \frac{2^n}{3n} }[/math].

Proof: There are [math]\displaystyle{ 2^{2^n} }[/math] boolean functions [math]\displaystyle{ f:\{0,1\}^n\rightarrow \{0,1\} }[/math].

Fix an integer [math]\displaystyle{ t }[/math], we then count the number of circuits with [math]\displaystyle{ t }[/math] gates. By the De Morgan's laws, we can assume that all NOTs are pushed back to the inputs. Each gate has one of the two types (AND or OR), and has two inputs. Each of the inputs to a gate is either a constant 0 or 1, an input variable [math]\displaystyle{ x_i }[/math], an inverted input variable [math]\displaystyle{ \neg x_i }[/math], or the output of another gate; thus, there are at most [math]\displaystyle{ 2+2n+t-1 }[/math] possible gate inputs. It follows that the number of circuits with [math]\displaystyle{ t }[/math] gates is at most [math]\displaystyle{ 2^t(t+2n+1)^{2t} }[/math].

Uniformly choose a boolean function [math]\displaystyle{ f }[/math] at random. Note that each circuit can compute one boolean function (the converse is not true). The probability that [math]\displaystyle{ f }[/math] can be computed by a circuit with [math]\displaystyle{ t }[/math] gates is at most

[math]\displaystyle{ \frac{2^t(t+2n+1)^{2t}}{2^{2^n}}. }[/math]

If [math]\displaystyle{ t=2^n/3n }[/math], then

[math]\displaystyle{ \frac{2^t(t+2n+1)^{2t}}{2^{2^n}}=o(1)\lt 1. }[/math]

Therefore, there exists a boolean function [math]\displaystyle{ f }[/math] which cannot be computed by any circuits with [math]\displaystyle{ 2^n/3n }[/math] gates.

[math]\displaystyle{ \square }[/math]

Note that by Shannon's theorem, not only there exists a boolean function with exponentially large circuit complexity, but almost all boolean functions have exponentially large circuit complexity.

Ramsey number

Recall the Ramsey theorem which states that in a meeting of at least six people, there are either three people knowing each other or three people not knowing each other. In graph theoretical terms, this means that no matter how we color the edges of [math]\displaystyle{ K_6 }[/math] (the complete graph on six vertices), there must be a monochromatic [math]\displaystyle{ K_3 }[/math] (a triangle whose edges have the same color).

Generally, the Ramsey number [math]\displaystyle{ R(k,\ell) }[/math] is the smallest integer [math]\displaystyle{ n }[/math] such that in any two-coloring of the edges of a complete graph on [math]\displaystyle{ n }[/math] vertices [math]\displaystyle{ K_n }[/math] by red and blue, either there is a red [math]\displaystyle{ K_k }[/math] or there is a blue [math]\displaystyle{ K_\ell }[/math].

Ramsey showed in 1929 that [math]\displaystyle{ R(k,\ell) }[/math] is finite for any [math]\displaystyle{ k }[/math] and [math]\displaystyle{ \ell }[/math]. It is extremely hard to compute the exact value of [math]\displaystyle{ R(k,\ell) }[/math]. Here we give a lower bound of [math]\displaystyle{ R(k,k) }[/math] by the probabilistic method.

Theorem (Erdős 1947) If [math]\displaystyle{ {n\choose k}\cdot 2^{1-{k\choose 2}}\lt 1 }[/math] then it is possible to color the edges of [math]\displaystyle{ K_n }[/math] with two colors so that there is no monochromatic [math]\displaystyle{ K_k }[/math] subgraph.

Proof: Consider a random two-coloring of edges of [math]\displaystyle{ K_n }[/math] obtained as follows:

• For each edge of [math]\displaystyle{ K_n }[/math], independently flip a fair coin to decide the color of the edge.

For any fixed set [math]\displaystyle{ S }[/math] of [math]\displaystyle{ k }[/math] vertices, let [math]\displaystyle{ \mathcal{E}_S }[/math] be the event that the [math]\displaystyle{ K_k }[/math] subgraph induced by [math]\displaystyle{ S }[/math] is monochromatic. There are [math]\displaystyle{ {k\choose 2} }[/math] many edges in [math]\displaystyle{ K_k }[/math], therefore

[math]\displaystyle{ \Pr[\mathcal{E}_S]=2\cdot 2^{-{k\choose 2}}=2^{1-{k\choose 2}}. }[/math]

Since there are [math]\displaystyle{ {n\choose k} }[/math] possible choices of [math]\displaystyle{ S }[/math], by the union bound

[math]\displaystyle{ \Pr[\exists S, \mathcal{E}_S]\le {n\choose k}\cdot\Pr[\mathcal{E}_S]={n\choose k}\cdot 2^{1-{k\choose 2}}. }[/math]

Due to the assumption, [math]\displaystyle{ {n\choose k}\cdot 2^{1-{k\choose 2}}\lt 1 }[/math], thus there exists a two coloring that none of [math]\displaystyle{ \mathcal{E}_S }[/math] occurs, which means there is no monochromatic [math]\displaystyle{ K_k }[/math] subgraph.

[math]\displaystyle{ \square }[/math]

For [math]\displaystyle{ k\ge 3 }[/math] and we take [math]\displaystyle{ n=\lfloor2^{k/2}\rfloor }[/math], then

[math]\displaystyle{ \begin{align} {n\choose k}\cdot 2^{1-{k\choose 2}} &\lt \frac{n^k}{k!}\cdot\frac{2^{1+\frac{k}{2}}}{2^{k^2/2}}\\ &\le \frac{2^{k^2/2}}{k!}\cdot\frac{2^{1+\frac{k}{2}}}{2^{k^2/2}}\\ &= \frac{2^{1+\frac{k}{2}}}{k!}\\ &\lt 1. \end{align} }[/math]

By the above theorem, there exists a two-coloring of [math]\displaystyle{ K_n }[/math] that there is no monochromatic [math]\displaystyle{ K_k }[/math]. Therefore, the Ramsey number [math]\displaystyle{ R(k,k)\gt \lfloor2^{k/2}\rfloor }[/math] for all [math]\displaystyle{ k\ge 3 }[/math].

Note that for sufficiently large [math]\displaystyle{ k }[/math], if [math]\displaystyle{ n= \lfloor 2^{k/2}\rfloor }[/math], then the probability that there exists a monochromatic [math]\displaystyle{ K_k }[/math] is bounded by

[math]\displaystyle{ {n\choose k}\cdot 2^{1-{k\choose 2}} \lt \frac{2^{1+\frac{k}{2}}}{k!} \ll 1, }[/math]

which means that a random two-coloring of [math]\displaystyle{ K_n }[/math] is very likely not to contain a monochromatic [math]\displaystyle{ K_{2\log n} }[/math]. This gives us a very simple randomized algorithm for finding a two-coloring of [math]\displaystyle{ K_n }[/math] without monochromatic [math]\displaystyle{ K_{2\log n} }[/math].

Blocking number

Let [math]\displaystyle{ S }[/math] be a set. Let [math]\displaystyle{ 2^{S}=\{A\mid A\subseteq S\} }[/math] be the power set of [math]\displaystyle{ S }[/math], and let [math]\displaystyle{ {S\choose k}=\{A\mid A\subseteq S\mbox{ and }|A|=k\} }[/math] be the [math]\displaystyle{ k }[/math]-uniform of [math]\displaystyle{ S }[/math].

We call [math]\displaystyle{ \mathcal{F} }[/math] a set family (or a set system) with ground set [math]\displaystyle{ S }[/math] if [math]\displaystyle{ \mathcal{F}\subseteq 2^{S} }[/math]. The members of [math]\displaystyle{ \mathcal{F} }[/math] are subsets of [math]\displaystyle{ S }[/math].

Given a set family [math]\displaystyle{ \mathcal{F} }[/math] with ground set [math]\displaystyle{ S }[/math], a set [math]\displaystyle{ T\subseteq S }[/math] is a blocking set of [math]\displaystyle{ \mathcal{F} }[/math] if all [math]\displaystyle{ A\in\mathcal{F} }[/math] have [math]\displaystyle{ A\cap T\neq \emptyset }[/math], i.e. [math]\displaystyle{ T }[/math] intersects (blocks) all member set of [math]\displaystyle{ \mathcal{F} }[/math].

Theorem Given a set family [math]\displaystyle{ \mathcal{F}\subseteq{S\choose k} }[/math], where [math]\displaystyle{ m=|\mathcal{F}| }[/math] and [math]\displaystyle{ n=|S| }[/math], [math]\displaystyle{ \mathcal{F} }[/math] has a blocking set of size [math]\displaystyle{ \left\lceil\frac{n\ln m}{k}\right\rceil }[/math].

Proof: Let [math]\displaystyle{ \tau=\left\lceil\frac{n\ln m}{k}\right\rceil }[/math]. Let [math]\displaystyle{ T }[/math] be a set chosen uniformly at random from [math]\displaystyle{ {S\choose \tau} }[/math]. We show that [math]\displaystyle{ T }[/math] is a blocking set of [math]\displaystyle{ \mathcal{F} }[/math] with a probability >0.

Fix any [math]\displaystyle{ A\in\mathcal{F} }[/math]. Recall that [math]\displaystyle{ \mathcal{F}\subseteq{S\choose k} }[/math], thus [math]\displaystyle{ |A|=k }[/math]. And

[math]\displaystyle{ \begin{align} \Pr[A\cap T=\emptyset] &= \frac{\left|{S-T\choose \tau}\right|}{\left|{S\choose \tau}\right|}\\ &= \frac{{n-k\choose \tau}}{{n\choose\tau}}\\ &= \frac{(n-k)\cdot(n-k-1)\cdots(n-k-\tau+1)}{n\cdot(n-1)\cdots(n-\tau+1)}\\ &\lt \left(1-\frac{k}{n}\right)^{\tau}\\ &\le \exp\left(-\frac{k\tau}{n}\right)\\ &\le \frac{1}{m}. \end{align} }[/math]

By the union bound, the probability that there exists an [math]\displaystyle{ A\in\mathcal{F} }[/math] that misses [math]\displaystyle{ T }[/math]

[math]\displaystyle{ \Pr[\exists A\in\mathcal{F}, A\cap T=\emptyset]\le m\Pr[A\cap T=\emptyset]\lt m\cdot\frac{1}{m}=1. }[/math]

Thus, the probability that [math]\displaystyle{ T }[/math] is a blocking set

[math]\displaystyle{ \Pr[\forall A\in\mathcal{F}, A\cap T\neq\emptyset]\gt 0. }[/math]

There exists a blocking set of size [math]\displaystyle{ \tau=\left\lceil\frac{n\ln m}{k}\right\rceil }[/math].

[math]\displaystyle{ \square }[/math]

The theorem also hints us to a randomized algorithm. In order to make the algorithm efficient, we relax the size of [math]\displaystyle{ T }[/math] to [math]\displaystyle{ \tau=\frac{2n\ln m}{k} }[/math]. Uniformly choose [math]\displaystyle{ \tau }[/math] elements from [math]\displaystyle{ S }[/math] to form the set [math]\displaystyle{ T }[/math], by the above analysis, the probability that [math]\displaystyle{ T }[/math] is NOT a blocking set is at most

[math]\displaystyle{ m\exp\left(-\frac{n\tau}{k}\right)=m\exp(-2\ln m)=\frac{1}{m}. }[/math]

Thus, a blocking set is found with high probability.

Linearity of expectation

Maximum cut

Given an undirected graph [math]\displaystyle{ G(V,E) }[/math], a set [math]\displaystyle{ C }[/math] of edges of [math]\displaystyle{ G }[/math] is called a cut if [math]\displaystyle{ G }[/math] is disconnected after removing the edges in [math]\displaystyle{ C }[/math]. We can represent a cut by [math]\displaystyle{ c(S,T) }[/math] where [math]\displaystyle{ (S,T) }[/math] is a bipartition of the vertex set [math]\displaystyle{ V }[/math], and [math]\displaystyle{ c(S,T)=\{uv\in E\mid u\in S,v\in T\} }[/math] is the set of edges crossing between [math]\displaystyle{ S }[/math] and [math]\displaystyle{ T }[/math].

We have seen how to compute min-cut: either by deterministic max-flow algorithm, or by Karger's randomized algorithm. On the other hand, max-cut is hard to compute, because it is NP-complete. Actually, the weighted version of max-cut is among the Karp's 21 NP-complete problems.

We now show by the probabilistic method that a max-cut always has at least half the edges.

Theorem Given an undirected graph [math]\displaystyle{ G }[/math] with [math]\displaystyle{ n }[/math] vertices and [math]\displaystyle{ m }[/math] edges, there is a cut of size at least [math]\displaystyle{ \frac{m}{2} }[/math].

Proof: Enumerate the vertices in an arbitrary order. Partition the vertex set [math]\displaystyle{ V }[/math] into two disjoint sets [math]\displaystyle{ S }[/math] and [math]\displaystyle{ T }[/math] as follows.

For each vertex [math]\displaystyle{ v\in V }[/math],

• independently choose one of [math]\displaystyle{ S }[/math] and [math]\displaystyle{ T }[/math] with equal probability, and let [math]\displaystyle{ v }[/math] join the chosen set.

For each vertex [math]\displaystyle{ v\in V }[/math], let [math]\displaystyle{ X_v\in\{S,T\} }[/math] be the random variable which represents the set that [math]\displaystyle{ v }[/math] joins. For each edge [math]\displaystyle{ uv\in E }[/math], let [math]\displaystyle{ Y_{uv} }[/math] be the 0-1 random variable which indicates whether [math]\displaystyle{ uv }[/math] crosses between [math]\displaystyle{ S }[/math] and [math]\displaystyle{ T }[/math]. Clearly,

[math]\displaystyle{ \Pr[Y_{uv}=1]=\Pr[X_u=X_v]=\frac{1}{2}. }[/math]

The size of [math]\displaystyle{ c(S,T) }[/math] is given by [math]\displaystyle{ Y=\sum_{uv\in E}Y_{uv} }[/math]. By the linearity of expectation,

[math]\displaystyle{ \mathbf{E}[Y]=\sum_{uv\in E}\mathbf{E}[Y_{uv}]=\sum_{uv\in E}\Pr[Y_{uv}=1]=\frac{m}{2}. }[/math]

Therefore, there exist a bipartition [math]\displaystyle{ (S,T) }[/math] of [math]\displaystyle{ V }[/math] such that [math]\displaystyle{ |c(S,T)|\ge\frac{m}{2} }[/math], i.e. there exists a cut of [math]\displaystyle{ G }[/math] which contains at least [math]\displaystyle{ \frac{m}{2} }[/math] edges.

[math]\displaystyle{ \square }[/math]

Maximum satisfiability

Suppose that we have a number of boolean variables [math]\displaystyle{ x_1,x_2,\ldots,\in\{\mathrm{true},\mathrm{false}\} }[/math]. A literal is either a variable [math]\displaystyle{ x_i }[/math] itself or its negation [math]\displaystyle{ \neg x_i }[/math]. A logic expression is a conjunctive normal form (CNF) if it is written as the conjunction(AND) of a set of clauses, where each clause is a disjunction(OR) of literals. For example:

[math]\displaystyle{ (x_1\vee \neg x_2 \vee \neg x_3)\wedge (\neg x_1\vee \neg x_3)\wedge (x_1\vee x_2\vee x_4)\wedge (x_4\vee \neg x_3)\wedge (x_4\vee \neg x_1). }[/math]

The satisfiability (SAT) problem ask whether the CNF is satisfiable, i.e. there exists an assignment of variables to the values of true and false so that all clauses are true. The maximum satisfiability (MAXSAT) is the optimization version of SAT, which ask for an assignment that the number of satisfied clauses is maximized.

SAT is the first problem known to be NP-complete (the Cook-Levin theorem). MAXSAT is also NP-complete. We then see that there always exists a roughly good truth assignment which satisfies half the clauses.

Theorem For any set of [math]\displaystyle{ m }[/math] clauses, there is a truth assignment that satisfies at least [math]\displaystyle{ \frac{m}{2} }[/math] clauses.

Proof: For each variable, independently assign a random value in [math]\displaystyle{ \{\mathrm{true},\mathrm{false}\} }[/math] with equal probability. For the [math]\displaystyle{ i }[/math]th clause, let [math]\displaystyle{ X_i }[/math] be the random variable which indicates whether the [math]\displaystyle{ i }[/math]th clause is satisfied. Suppose that there are [math]\displaystyle{ k }[/math] literals in the clause. The probability that the clause is satisfied is

[math]\displaystyle{ \Pr[X_k=1]\ge(1-2^{-k})\ge\frac{1}{2} }[/math].

Let [math]\displaystyle{ X=\sum_{i=1}^m X_i }[/math] be the number of satisfied clauses. By the linearity of expectation,

[math]\displaystyle{ \mathbf{E}[X]=\sum_{i=1}^{m}\mathbf{E}[X_i]\ge \frac{m}{2}. }[/math]

Therefore, there exists an assignment such that at least [math]\displaystyle{ \frac{m}{2} }[/math] clauses are satisfied.

[math]\displaystyle{ \square }[/math]

Alterations

Independent sets

An independent set of a graph is a set of vertices with no edges between them. The following theorem gives a lower bound on the size of the largest independent set.

Theorem Let [math]\displaystyle{ G(V,E) }[/math] be a graph on [math]\displaystyle{ n }[/math] vertices with [math]\displaystyle{ m }[/math] edges. Then [math]\displaystyle{ G }[/math] has an independent set with at least [math]\displaystyle{ \frac{n^2}{4m} }[/math] vertices.

Proof: Let [math]\displaystyle{ S }[/math] be a set of vertices constructed as follows:

For each vertex [math]\displaystyle{ v\in V }[/math]:

• [math]\displaystyle{ v }[/math] is included in [math]\displaystyle{ S }[/math] independently with probability [math]\displaystyle{ p }[/math],

[math]\displaystyle{ p }[/math] to be determined.

Let [math]\displaystyle{ X=|S| }[/math]. It is obvious that [math]\displaystyle{ \mathbf{E}[X]=np }[/math].

For each edge [math]\displaystyle{ e\in E }[/math], let [math]\displaystyle{ Y_{e} }[/math] be the random variable which indicates whether both endpoints of [math]\displaystyle{ }[/math] are in [math]\displaystyle{ S }[/math].

[math]\displaystyle{ \mathbf{E}[Y_{uv}]=\Pr[u\in S\wedge v\in S]=p^2. }[/math]

Let [math]\displaystyle{ Y }[/math] be the number of edges in the subgraph of [math]\displaystyle{ G }[/math] induced by [math]\displaystyle{ S }[/math]. It holds that [math]\displaystyle{ Y=\sum_{e\in E}Y_e }[/math]. By linearity of expectation,

[math]\displaystyle{ \mathbf{E}[Y]=\sum_{e\in E}\mathbf{E}[Y_e]=mp^2 }[/math].

Note that although [math]\displaystyle{ S }[/math] is not necessary an independent set, it can be modified to one if for each edge [math]\displaystyle{ e }[/math] of the induced subgraph [math]\displaystyle{ G(S) }[/math], we delete one of the endpoint of [math]\displaystyle{ e }[/math] from [math]\displaystyle{ S }[/math]. Let [math]\displaystyle{ S^* }[/math] be the resulting set. It is obvious that [math]\displaystyle{ S^* }[/math] is an independent set since there is no edge left in the induced subgraph [math]\displaystyle{ G(S^*) }[/math].

Since there are [math]\displaystyle{ Y }[/math] edges in [math]\displaystyle{ G(S) }[/math], there are at most [math]\displaystyle{ Y }[/math] vertices in [math]\displaystyle{ S }[/math] are deleted to make it become [math]\displaystyle{ S^* }[/math]. Therefore, [math]\displaystyle{ |S^*|\ge X-Y }[/math]. By linearity of expectation,

[math]\displaystyle{ \mathbf{E}[|S^*|]\ge\mathbf{E}[X-Y]=\mathbf{E}[X]-\mathbf{E}[Y]=np-mp^2. }[/math]

The expectation is maximized when [math]\displaystyle{ p=\frac{n}{2m} }[/math], thus

[math]\displaystyle{ \mathbf{E}[|S^*|]\ge n\cdot\frac{n}{2m}-m\left(\frac{n}{2m}\right)^2=\frac{n^2}{4m}. }[/math]

There exists an independent set which contains at least [math]\displaystyle{ \frac{n}{4m} }[/math] vertices.

[math]\displaystyle{ \square }[/math]

The proof actually propose a randomized algorithm for constructing large independent set:

Given a graph on [math]\displaystyle{ n }[/math] vertices with [math]\displaystyle{ m }[/math] edges, let [math]\displaystyle{ d=\frac{2m}{n} }[/math] be the average degree. For each vertex [math]\displaystyle{ v\in S }[/math], [math]\displaystyle{ v }[/math] is included in [math]\displaystyle{ S }[/math] independently with probability [math]\displaystyle{ \frac{1}{d} }[/math]. For each remaining edge in the induced subgraph [math]\displaystyle{ G(S) }[/math], remove one of the endpoints from [math]\displaystyle{ S }[/math].

Let [math]\displaystyle{ S^* }[/math] be the resulting set. We have shown that [math]\displaystyle{ S^* }[/math] is an independent set and [math]\displaystyle{ \mathbf{E}[|S^*|]\ge\frac{n^2}{4m} }[/math].

Intersecting families

An [math]\displaystyle{ \mathcal{F}\subseteq 2^S }[/math] is an intersecting family if for any [math]\displaystyle{ A,B\in\mathcal{F} }[/math] it holds that [math]\displaystyle{ A\cap B\neq\emptyset }[/math].

Suppose that [math]\displaystyle{ n\ge 2k }[/math]. For [math]\displaystyle{ \mathcal{F}\subseteq{S\choose k} }[/math], where [math]\displaystyle{ |S|=n }[/math], we can let all [math]\displaystyle{ A\in \mathcal{F} }[/math] contain one common element [math]\displaystyle{ a\in S }[/math] and [math]\displaystyle{ A-\{a\} }[/math] enumerates all [math]\displaystyle{ {n-1\choose k-1} }[/math] possible combinations of [math]\displaystyle{ (k-1) }[/math] elements in [math]\displaystyle{ S }[/math]. This gives us an intersecting family of size [math]\displaystyle{ |\mathcal{F}|={n-1\choose k-1} }[/math].

The following theorem says that this is the largest possible cardinality an intersecting [math]\displaystyle{ \mathcal{F} }[/math] can achieve. The theorem was first proved by Erdős, Ko, and Rado in 1938, but published 23 years later. It is a fundamental result in the area of extremal set theory, which studies the maximum (or minimum) possible cardinality of a set system satisfying certain structural assumption. In this example, the structural assumption is intersecting.

Here we present a probabilistic proof by Katona.

Theorem (Erdős-Ko-Rado 1961) Let [math]\displaystyle{ \mathcal{F}\subseteq{S\choose k} }[/math], where [math]\displaystyle{ |S|=n }[/math] and [math]\displaystyle{ n\ge 2k }[/math]. If [math]\displaystyle{ \mathcal{F} }[/math] is an intersecting family then [math]\displaystyle{ |\mathcal{F}|\le{n-1\choose k-1} }[/math].

Proof (due to Katona 1972).

Without loss of generality, let [math]\displaystyle{ S=[n] }[/math]. For [math]\displaystyle{ i\in[n] }[/math], let [math]\displaystyle{ A_i=\{(i+j)\bmod n\mid j\in[k]\} }[/math]. Then we make the following claim.

Claim 1: [math]\displaystyle{ \mathcal{F} }[/math] can contain at most [math]\displaystyle{ k }[/math] many [math]\displaystyle{ A_i }[/math].

The claim can be easily proved by observing that for any [math]\displaystyle{ i,j\in[n] }[/math] that [math]\displaystyle{ i\lt j }[/math], [math]\displaystyle{ A_i }[/math] and [math]\displaystyle{ A_j }[/math] are disjoint if [math]\displaystyle{ j-i\gt k }[/math], thus in order to make [math]\displaystyle{ \mathcal{F} }[/math] intersecting, all [math]\displaystyle{ A_i,A_j\in\mathcal{F} }[/math] have [math]\displaystyle{ |i-j|\le k }[/math]. This is violated once there are more than [math]\displaystyle{ k }[/math] many [math]\displaystyle{ A_i }[/math] in [math]\displaystyle{ \mathcal{F} }[/math].

Now we prove the Erdős-Ko-Rado theorem. Let a permutation [math]\displaystyle{ \sigma }[/math] of [math]\displaystyle{ [n] }[/math] and an integer [math]\displaystyle{ i\in[n] }[/math] be chosen uniformly and independently at random. Let

[math]\displaystyle{ R=\{\sigma((i+j)\bmod n)\mid j\in[k]\}, \quad\mbox{ or equivalently }R=\sigma(A_i) }[/math].

By Claim 1, for any fixed permutation [math]\displaystyle{ \sigma }[/math], the family [math]\displaystyle{ \mathcal{F} }[/math] can contain at most [math]\displaystyle{ k }[/math] of the sets [math]\displaystyle{ \sigma(A_i) }[/math], thus conditioning on any particular [math]\displaystyle{ \sigma }[/math], [math]\displaystyle{ \Pr[R\in\mathcal{F}\mid \sigma]\le\frac{k}{n} }[/math]. Hence

[math]\displaystyle{ \Pr[R\in\mathcal{F}]\le\frac{k}{n}. }[/math]

On the other hand, by our construction, [math]\displaystyle{ R }[/math] is uniformly chosen from [math]\displaystyle{ {S\choose k} }[/math], thus

[math]\displaystyle{ \Pr[R\in\mathcal{F}]=\frac{|\mathcal{F}|}{{n\choose k}}. }[/math]

Therefore, [math]\displaystyle{ |\mathcal{F}|\le\frac{k}{n}{n\choose k}={n-1\choose k-1}. }[/math]

[math]\displaystyle{ \square }[/math]

The Lovász Local Lemma

Consider a set of "bad" events [math]\displaystyle{ A_1,A_2,\ldots,A_n }[/math]. Suppose that [math]\displaystyle{ \Pr[A_i]\le p }[/math] for all [math]\displaystyle{ 1\le i\le n }[/math]. We want to show that there is a situation that none of the bad events occurs. Due to the probabilistic method, we need to prove that

[math]\displaystyle{ \Pr\left[\bigwedge_{i=1}^n\overline{A_i}\right]\gt 0. }[/math]

If all the bad events [math]\displaystyle{ A_1,A_2,\ldots,A_n }[/math] are mutually independent, then

[math]\displaystyle{ \Pr\left[\bigwedge_{i=1}^n\overline{A_i}\right]\ge(1-p)^n\gt 0, }[/math]

for any [math]\displaystyle{ p\lt 1 }[/math].

On the other hand, if we put no assumption on the dependencies between the events, then by the union bound (which holds unconditionally),

[math]\displaystyle{ \Pr\left[\bigwedge_{i=1}^n\overline{A_i}\right]=1-\Pr\left[\bigvee_{i=1}^n A_i\right]\ge 1-np, }[/math]

which is not an interesting bound for [math]\displaystyle{ p\ge\frac{1}{n} }[/math]. If we make no further assumption on the dependencies between the events, the above bound is tight.

Example

Consider that a ball is uniformly thrown into one of the [math]\displaystyle{ (n+1) }[/math] bins. Let the "bad" events [math]\displaystyle{ A_1,A_2,\ldots,A_n }[/math] be defined as that [math]\displaystyle{ A_i }[/math] represents that the ball falls into the [math]\displaystyle{ i }[/math]th bin. The only good event is that the ball falls into the [math]\displaystyle{ (n+1) }[/math]th bin. Clearly, [math]\displaystyle{ \Pr\left[\bigwedge_{i=1}^n\overline{A_i}\right]=1-n\cdot\frac{1}{n+1} }[/math]. Thus the above union bound is achieved.

This example shows that dependencies between the events could cause troubles.

We would like to know what is going on between the two extreme cases: mutually independent events, and arbitrarily dependent events. The Lovász local lemma provides such a tool.

The local lemma

The local lemma is powerful tool for showing the possibility of rare event under limited dependencies. The structure of dependencies between a set of events can be described by a dependency graph.

Definition Let [math]\displaystyle{ A_1,A_2,\ldots,A_n }[/math] be a set of events. A graph [math]\displaystyle{ D=(V,E) }[/math] on the set of vertices [math]\displaystyle{ V=\{1,2,\ldots,n\} }[/math] is called a dependency graph for the events [math]\displaystyle{ A_1,\ldots,A_n }[/math] if for each [math]\displaystyle{ i }[/math], [math]\displaystyle{ 1\le i\le n }[/math], the event [math]\displaystyle{ A_i }[/math] is mutually independent of all the events [math]\displaystyle{ \{A_j\mid (i,j)\not\in E\} }[/math].

Theorem (The local lemma: symmetric case) Let [math]\displaystyle{ A_1,A_2,\ldots,A_n }[/math] be a set of events, and assume that the following hold: for all [math]\displaystyle{ 1\le i\le n }[/math], [math]\displaystyle{ \Pr[A_i]\le p }[/math]; the maximum degree of the dependency graph for the events [math]\displaystyle{ A_1,A_2,\ldots,A_n }[/math] is [math]\displaystyle{ d }[/math], and [math]\displaystyle{ ep(d+1)\le 1 }[/math]. Then [math]\displaystyle{ \Pr\left[\bigwedge_{i=1}^n\overline{A_i}\right]\gt 0 }[/math].

Theorem (The local lemma: general case) Let [math]\displaystyle{ A_1,A_2,\ldots,A_n }[/math] be a set of events. Suppose that [math]\displaystyle{ D=(V,E) }[/math] is a dependency graph for the events and suppose there are real numbers [math]\displaystyle{ x_1,x_2,\ldots, x_n }[/math] such that [math]\displaystyle{ 0\le x_i\lt 1 }[/math] and for all [math]\displaystyle{ 1\le i\le n }[/math], [math]\displaystyle{ \Pr[A_i]\le x_i\prod_{(i,j)\in E}(1-x_j) }[/math]. Then [math]\displaystyle{ \Pr\left[\bigwedge_{i=1}^n\overline{A_i}\right]\ge\prod_{i=1}^n(1-x_i) }[/math].