Branching Processes

A single bacterium divides, or fails to. Its offspring divide or fail, generation after generation. Will the family line survive forever, or is extinction certain? This question is simple to state, but subtle to answer. It is the subject of branching processes. Its consequences reach far beyond biology: the fate of surnames, the spread of an epidemic, the growth of a nuclear chain reaction, and the survival of a mutant gene all obey the same mathematical skeleton. The Galton–Watson process is named for the two Victorians who first studied the extinction of family surnames. It models a population in which each individual independently produces a random number of offspring, according to a fixed distribution. The remarkable fact is this: the entire long-run behavior of this process is governed by a single number. That number is the mean number of offspring per individual. It determines whether the population dies out with probability one, or survives with positive probability. This is a strikingly clean dichotomy. It is proved using an equally clean tool: the probability generating function of the offspring distribution, iterated once per generation. The big picture is that branching processes sit at the crossroads of two ideas the reader already knows. They are Markov chains, since the population size at generation n+1n+1 depends on the past only through the population size at generation nn. But their state space is unbounded. Their transition structure is generated by a sum of i.i.d. random variables. This is exactly where generating functions become indispensable. They turn a probabilistic recursion into an algebraic one (iteration of a fixed function). This article builds the Galton–Watson process from its probabilistic definition. It develops the generating-function machinery that makes it tractable. It proves the central extinction theorem in full: extinction is certain if and only if the mean offspring number is at most 1. This excludes the degenerate case of no variability. Along the way, we compute extinction probabilities exactly in two asymmetric examples. We exhibit the boundary (critical) case where the naive intuition breaks. Finally, we point toward the martingale viewpoint that unifies and extends everything here.

Key takeaways
  • A Galton–Watson process models a population where each individual independently has a random number ξ\xi of children, i.i.d. across all individuals and generations.
  • Population sizes ZnZ_n form a Markov chain on {0,1,2,… }\{0,1,2,\dots\} with 00 an absorbing state.
  • The probability generating function ϕ\phi of the offspring law controls everything: the pgf of ZnZ_n is the nn-fold iterate ϕ(n)\phi^{(n)}.
  • The extinction probability qq is the smallest fixed point in [0,1][0,1] of s=ϕ(s)s = \phi(s).
  • Extinction Theorem: if the mean offspring m=E[ξ]≤1m=\mathbb E[\xi]\le 1 (and ξ\xi is not a.s. equal to 11) then q=1q=1; if m>1m>1 then q<1q<1.
  • Key idea: iterating a single generating function replaces an intractable probabilistic recursion with a tractable algebraic fixed-point problem.

Where this lives today

Branching processes are a genuine working tool, not just a historical curiosity. In epidemiology, the basic reproduction number R0R_0 of an infectious disease plays exactly the role of mm: if R0≤1R_0 \le 1 an outbreak dies out with certainty (in the idealized branching approximation), while R0>1R_0>1 allows a positive-probability major epidemic, with the same extinction-probability equation used to estimate the chance a single imported case fizzles out. In nuclear physics, the same mathematics (originally analyzed via Monte Carlo methods by Ulam and von Neumann) governs whether a chain reaction of neutron-induced fissions is sub-critical, critical, or super-critical — the terminology is inherited directly. In genetics, the survival probability of a new mutant allele in a large population is computed via the extinction probability of an associated branching process (Haldane's classical approximation q≈1−2/mq\approx 1-2/m near criticality for slightly advantageous mutants uses exactly this framework). In computer science, branching processes model the size of search trees (e.g., in randomized algorithms and parsing), and the analysis of random recursive trees and random graphs (e.g. component sizes in Erdős–Rényi random graphs near the phase transition) reduces to Galton–Watson extinction/survival dichotomies. The natural next step in the theory — recasting Wn=Zn/mnW_n = Z_n/m^n as a martingale — gives sharp almost-sure growth-rate theorems (the Kesten–Stigum theorem) refining everything proved here.

Ask the tutor: Can you walk through why the extinction probability equals qkq^k when starting from kk ancestors instead of 11?

DefinitionGalton–Watson branching process

Let ξ,ξ1,ξ2,…\xi, \xi_1, \xi_2, \dots be independent and identically distributed random variables taking values in {0,1,2,… }\{0,1,2,\dots\}, with common probability mass function pk=Pr⁡(ξ=k)p_k = \Pr(\xi = k), k≥0k \ge 0. Assume p0<1p_0 < 1 (offspring are not deterministically zero) to avoid triviality. Define a stochastic process (Zn)n≥0(Z_n)_{n \ge 0} by Z0=1Z_0 = 1 and, for n≥0n \ge 0,

Zn+1=∑i=1Znξn,i,Z_{n+1} = \sum_{i=1}^{Z_n} \xi_{n,i},

where (ξn,i)i≥1(\xi_{n,i})_{i\ge1} for each nn is an independent family of i.i.d. copies of ξ\xi, independent across nn as well, and the empty sum (Zn=0Z_n = 0) is 00. Interpretation: ZnZ_n is the population size at generation nn; each of the ZnZ_n individuals alive at generation nn independently produces ξ\xi-many offspring, and Zn+1Z_{n+1} is the total. The process (Zn)(Z_n) is called a Galton–Watson process with offspring distribution (pk)k≥0(p_k)_{k\ge0}. Extinction is the event

E={Zn=0 for some n≥1}E = \{ Z_n = 0 \text{ for some } n \ge 1 \}

and the extinction probability is q=Pr⁡(E)q = \Pr(E).

Intuition

Picture the process as a tree growing downward. The root is the single ancestor at generation 00. Each node sprouts a random number of children, drawn independently from the offspring law, and the process continues layer by layer. If at some generation every individual has zero children, the tree stops growing there and the population is extinct forever, because 00 is an absorbing state: once Zn=0Z_n = 0, every subsequent Zn+k=0Z_{n+k} = 0 automatically, since summing zero copies of anything gives zero. The key quantity is the mean offspring number m=E[ξ]=∑kk pkm = \mathbb E[\xi] = \sum_k k\,p_k. Intuitively, E[Zn]=mn\mathbb E[Z_n] = m^n (proved below), so if m<1m<1 the expected population shrinks geometrically to 00, if m=1m=1 it stays constant at 11, and if m>1m>1 it grows geometrically. One might guess naively that m≤1m \le 1 forces extinction and m>1m>1 prevents it — and the first half of that guess is right, but the second needs care: even when m>1m>1 the population can still die out, just not with certainty. The precise threshold is captured not by the mean directly, but by a fixed point of the generating function ϕ(s)=E[sξ]\phi(s) = \mathbb E[s^\xi]. The picture below shows the graph of ϕ\phi for a fixed offspring law, together with the "staircase" (cobweb) construction that generates the iterates ϕ(0),ϕ(ϕ(0)),…\phi(0), \phi(\phi(0)), \dots, converging to the smallest root of ϕ(s)=s\phi(s)=s in [0,1][0,1] — precisely the extinction probability.

Figure
Cobweb iteration of the pgf ϕ\phi converging to the extinction probability qq
s y y=s y=φ(s) 0 q ≈ 0.55 q

The central theorem

TheoremExtinction Theorem for Galton–Watson processes

Let (Zn)n≥0(Z_n)_{n\ge0} be a Galton–Watson process with offspring pgf ϕ(s)=E[sξ]=∑k≥0pksk\phi(s) = \mathbb E[s^\xi] = \sum_{k\ge0} p_k s^k for s∈[0,1]s\in[0,1], and suppose p0<1p_0 < 1 (non-trivial offspring) and p0+p1<1p_0 + p_1 < 1 (the offspring law is not degenerate at 11, ruling out a trivial process that never changes size). Let

m=E[ξ]=ϕ′(1−)∈[0,∞]m = \mathbb E[\xi] = \phi'(1^-) \in [0,\infty]

and let q=Pr⁡(eventual extinction)q = \Pr(\text{eventual extinction}). Then: 1. qq is the smallest root in [0,1][0,1] of the fixed-point equation s=ϕ(s)s = \phi(s). 2. If m≤1m \le 1, then q=1q = 1 (extinction is certain). 3. If m>1m > 1, then q∈[0,1)q \in [0,1) (extinction is not certain); more precisely qq is the unique root of ϕ(s)=s\phi(s)=s in [0,1)[0,1).

LemmaBranching property and generating function iteration

Let ϕn(s)=E[sZn]\phi_n(s) = \mathbb E[s^{Z_n}] be the pgf of ZnZ_n. Then for all n≥0n \ge 0,

ϕn+1(s)=ϕn(ϕ(s))=ϕ(ϕn(s))=ϕ(n+1)(s),\phi_{n+1}(s) = \phi_n(\phi(s)) = \phi(\phi_n(s)) = \phi^{(n+1)}(s),

where ϕ(n)\phi^{(n)} denotes the nn-fold functional composition of ϕ\phi with itself (ϕ(0)(s)=s\phi^{(0)}(s) = s).

Proof

(Lemma: generating function iteration.) We use the technique of conditioning on ZnZ_n and applying independence of offspring. Condition on Zn=kZ_n = k. Given this event, Zn+1=∑i=1kξn,iZ_{n+1} = \sum_{i=1}^k \xi_{n,i} is a sum of kk i.i.d. copies of ξ\xi, independent of the history up to time nn (this is exactly the defining recursion). By the standard product rule for pgfs of sums of independent random variables,

E[sZn+1∣Zn=k]=(E[sξ])k=ϕ(s)k.\mathbb E\big[s^{Z_{n+1}} \mid Z_n = k\big] = \big(\mathbb E[s^{\xi}]\big)^k = \phi(s)^k.

Hence, by the law of total expectation,

ϕn+1(s)=E[sZn+1]=∑k=0∞Pr⁡(Zn=k) ϕ(s)k=E[ϕ(s)Zn]=ϕn(ϕ(s)).\phi_{n+1}(s) = \mathbb E[s^{Z_{n+1}}] = \sum_{k=0}^\infty \Pr(Z_n = k)\,\phi(s)^k = \mathbb E\big[\phi(s)^{Z_n}\big] = \phi_n(\phi(s)).

This proves ϕn+1=ϕn∘ϕ\phi_{n+1} = \phi_n \circ \phi. We now show separately that ϕn∘ϕ=ϕ∘ϕn\phi_n \circ \phi = \phi \circ \phi_n, i.e. that composition in the other order also works, by induction on nn. For n=0n=0: ϕ0(s)=E[sZ0]=s\phi_0(s) = \mathbb E[s^{Z_0}] = s since Z0≡1Z_0 \equiv 1, so ϕ0(ϕ(s))=ϕ(s)=ϕ(ϕ0(s))\phi_0(\phi(s)) = \phi(s) = \phi(\phi_0(s)). Assume ϕn(ϕ(s))=ϕ(ϕn(s))\phi_n(\phi(s)) = \phi(\phi_n(s)) for some nn. Then using the recursion just derived twice,

ϕn+1(ϕ(s))=ϕn(ϕ(ϕ(s)))=ϕn(ϕ(ϕ(s))),\phi_{n+1}(\phi(s)) = \phi_n(\phi(\phi(s))) = \phi_n(\phi(\phi(s))),

and separately

ϕ(ϕn+1(s))=ϕ(ϕn(ϕ(s)))=ϕ(ϕ(ϕn(s)))\phi(\phi_{n+1}(s)) = \phi(\phi_n(\phi(s))) = \phi(\phi(\phi_n(s)))

by the inductive hypothesis applied inside. Since composition of functions is associative, ϕn(ϕ(ϕ(s)))=ϕ(ϕ(ϕn(s)))\phi_n(\phi(\phi(s))) = \phi(\phi(\phi_n(s))) trivially (both denote applying ϕn\phi_n then ϕ∘ϕ\phi\circ\phi, versus ϕ∘ϕ\phi\circ\phi then... to avoid confusion we verify directly): write ψ=ϕ∘ϕ\psi = \phi\circ\phi. By the base recursion ϕn+1=ϕn∘ϕ\phi_{n+1} = \phi_n\circ\phi applied with the whole process shifted, one instead argues more directly as follows. A cleaner induction: define ϕn\phi_n as above and prove ϕn=ϕ(n)\phi_n = \phi^{(n)} (the nn-fold self-composition) directly by induction on nn, which immediately gives both composition identities since ϕ(n)∘ϕ=ϕ∘ϕ(n)=ϕ(n+1)\phi^{(n)}\circ\phi = \phi\circ\phi^{(n)} = \phi^{(n+1)} for iterates of a single fixed function ϕ\phi (iterates of one function always commute with themselves). Base case n=0n=0: ϕ0(s)=s=ϕ(0)(s)\phi_0(s)=s=\phi^{(0)}(s). Inductive step: assuming ϕn=ϕ(n)\phi_n = \phi^{(n)}, the relation ϕn+1=ϕn∘ϕ\phi_{n+1} = \phi_n\circ\phi proved above gives

ϕn+1=ϕ(n)∘ϕ=ϕ(n+1).\phi_{n+1} = \phi^{(n)}\circ\phi = \phi^{(n+1)}.

This completes the induction and proves ϕn=ϕ(n)\phi_n = \phi^{(n)} for all nn, from which both stated identities ϕn+1=ϕn(ϕ(s))=ϕ(ϕn(s))=ϕ(n+1)(s)\phi_{n+1}=\phi_n(\phi(s))=\phi(\phi_n(s))=\phi^{(n+1)}(s) follow immediately, the second equality because self-iterates of one function commute with one more application of that function on either side. ■\blacksquare

∎
Proof

(Theorem, part 1: qq is the smallest fixed point of ϕ\phi.) We use the technique of monotone limits together with continuity of pgfs. Let qn=Pr⁡(Zn=0)q_n = \Pr(Z_n = 0). Since {Z0=0}\{Z_0=0\} is impossible (Z0≡1Z_0\equiv1), q0=0q_0 = 0. The event {Zn=0}\{Z_n = 0\} implies {Zn+1=0}\{Z_{n+1}=0\}, because 00 is absorbing (if generation nn is already extinct, generation n+1n+1 is too, as the empty sum is 00). Hence {Zn=0}\{Z_n=0\} is an increasing sequence of events in nn, so qnq_n is non-decreasing, and

lim⁡n→∞qn=Pr⁡(⋃n{Zn=0})=Pr⁡(E)=q\lim_{n\to\infty} q_n = \Pr\Big(\bigcup_n \{Z_n = 0\}\Big) = \Pr(E) = q

by continuity of probability measures along increasing unions. By the Lemma, qn=Pr⁡(Zn=0)=ϕn(0)=ϕ(n)(0)q_n = \Pr(Z_n=0) = \phi_n(0) = \phi^{(n)}(0), i.e. qnq_n is obtained by starting at 00 and applying ϕ\phi nn times: qn+1=ϕ(qn)q_{n+1} = \phi(q_n), with q0=0q_0=0. Since ϕ\phi is a power series with non-negative coefficients summing to ϕ(1)=1\phi(1)=1, it is continuous on [0,1][0,1] (indeed real-analytic on [0,1)[0,1) and continuous up to s=1s=1 by Abel's theorem for power series with non-negative coefficients and finite value at 11). Taking n→∞n\to\infty in qn+1=ϕ(qn)q_{n+1}=\phi(q_n) and using continuity of ϕ\phi,

q=lim⁡nqn+1=lim⁡nϕ(qn)=ϕ(lim⁡nqn)=ϕ(q).q = \lim_n q_{n+1} = \lim_n \phi(q_n) = \phi\Big(\lim_n q_n\Big) = \phi(q).

So qq is a fixed point of ϕ\phi in [0,1][0,1]. To see qq is the smallest such fixed point, let s∗∈[0,1]s^* \in [0,1] be any fixed point, ϕ(s∗)=s∗\phi(s^*) = s^*. We show qn≤s∗q_n \le s^* for all nn by induction. Base case: q0=0≤s∗q_0 = 0 \le s^*. Inductive step: if qn≤s∗q_n \le s^*, then since ϕ\phi is non-decreasing on [0,1][0,1] (all coefficients pk≥0p_k \ge 0, so ϕ′(s)=∑kkpksk−1≥0\phi'(s) = \sum_k k p_k s^{k-1} \ge 0 for s∈[0,1)s\in[0,1)),

qn+1=ϕ(qn)≤ϕ(s∗)=s∗.q_{n+1} = \phi(q_n) \le \phi(s^*) = s^*.

By induction qn≤s∗q_n \le s^* for all nn, hence q=lim⁡nqn≤s∗q = \lim_n q_n \le s^*. So qq is ≤\le every fixed point in [0,1][0,1], i.e. qq is the smallest one. This proves part 1. ■\blacksquare

(Theorem, part 2 and 3: the role of m=ϕ′(1−)m = \phi'(1^-).) We use the technique of convexity analysis of ϕ\phi on [0,1][0,1]. Since all pk≥0p_k \ge 0 and ϕ(s)=∑kpksk\phi(s) = \sum_k p_k s^k, differentiating termwise (valid inside the radius of convergence, which is at least 11 since ∑pk=1\sum p_k = 1) gives

ϕ′(s)=∑k≥1kpksk−1,ϕ′′(s)=∑k≥2k(k−1)pksk−2≥0 for s∈[0,1).\phi'(s) = \sum_{k\ge1} k p_k s^{k-1}, \qquad \phi''(s) = \sum_{k\ge2} k(k-1) p_k s^{k-2} \ge 0 \text{ for } s \in [0,1).

So ϕ\phi is convex and non-decreasing on [0,1)[0,1), and by monotone convergence, ϕ′(s)→ϕ′(1−)=m\phi'(s) \to \phi'(1^-) = m as s↑1s\uparrow 1 (allowing m=∞m=\infty if the offspring distribution has infinite mean). Also ϕ(1)=∑kpk=1\phi(1) = \sum_k p_k = 1, so s=1s=1 is always a fixed point of ϕ\phi. We must determine whether there is a smaller fixed point in [0,1)[0,1), and the answer is governed by the slope of ϕ\phi at 11. Case m≤1m \le 1. We claim ϕ(s)>s\phi(s) > s for all s∈[0,1)s \in [0,1), which forces the smallest fixed point in [0,1][0,1] to be s=1s=1 itself (if ϕ(s)>s\phi(s)>s throughout [0,1)[0,1), no point there can be a fixed point, so qn<1q_n < 1 for finite nn but the increasing sequence qnq_n can only converge to the fixed point 11, by part 1's characterization — more directly, since qq is a fixed point of ϕ\phi by part 1, and no point in [0,1)[0,1) is a fixed point in this case, we must have q=1q=1). To prove the claim, define g(s)=ϕ(s)−sg(s) = \phi(s) - s on [0,1][0,1]. Then g(1)=0g(1) = 0 and g′(s)=ϕ′(s)−1g'(s) = \phi'(s) - 1. Since ϕ′\phi' is non-decreasing (as ϕ′′≥0\phi''\ge0) and ϕ′(1−)=m≤1\phi'(1^-) = m \le 1, we get ϕ′(s)≤m≤1\phi'(s) \le m \le 1 for all s∈[0,1)s \in [0,1), hence g′(s)≤0g'(s) \le 0 on [0,1)[0,1), so gg is non-increasing on [0,1][0,1]. Since g(1)=0g(1)=0 and gg is non-increasing, g(s)≥g(1)=0g(s) \ge g(1) = 0 for s≤1s \le 1, i.e. ϕ(s)≥s\phi(s) \ge s for s∈[0,1)s\in[0,1). We need the strict inequality ϕ(s)>s\phi(s) > s to rule out other fixed points. Suppose for contradiction g(s0)=0g(s_0) = 0 for some s0∈[0,1)s_0 \in [0,1). Since gg is non-increasing and g(s0)=g(1)=0g(s_0)=g(1)=0, gg must be identically 00 on [s0,1][s_0,1] (a non-increasing function that returns to its starting value must be constant on the interval). Then g′(s)=0g'(s) = 0 for all s∈(s0,1)s\in(s_0,1), i.e. ϕ′(s)=1\phi'(s) = 1 identically there. Since ϕ′\phi' is non-decreasing and equals 11 on this whole subinterval while ϕ′(1−)=m≤1\phi'(1^-)=m\le1, and ϕ′\phi' is analytic (a power series), ϕ′(s)≡1\phi'(s)\equiv 1 forces ϕ′\phi' constant =1=1 on all of [0,1)[0,1) by analytic continuation (a power series agreeing with a constant on an interval has all higher coefficients zero). But ϕ′(s)=∑k≥1kpksk−1\phi'(s) = \sum_{k\ge1} kp_k s^{k-1}; if this is identically 11 then p1=1p_1 = 1 and pk=0p_k=0 for k≥2k\ge2, i.e. ϕ(s)=s\phi(s) = s, meaning ξ≡1\xi \equiv 1 almost surely — excluded by our hypothesis p0+p1<1p_0+p_1<1 (this hypothesis says Pr⁡(ξ≥2)>0\Pr(\xi\ge2)>0, incompatible with ξ≡1\xi\equiv1; note also p0<1p_0<1 rules out the other degenerate case separately handled). Contradiction. Hence no such s0s_0 exists, proving ϕ(s)>s\phi(s) > s strictly on [0,1)[0,1), and therefore q=1q=1. Case m>1m > 1. Now ϕ′(1−)=m>1\phi'(1^-) = m > 1, so since ϕ′\phi' is continuous and non-decreasing near 1−1^- with limit m>1m>1, there exists δ>0\delta>0 such that ϕ′(s)>1\phi'(s) > 1 for s∈(1−δ,1)s \in (1-\delta, 1), hence g′(s)=ϕ′(s)−1>0g'(s) = \phi'(s)-1 > 0 there, so gg is strictly increasing just to the left of 11. Since g(1)=0g(1)=0, strict increase just before 11 forces g(s)<0g(s) < 0, i.e. ϕ(s)<s\phi(s) < s, for ss slightly less than 11. On the other hand, g(0)=ϕ(0)−0=p0≥0g(0) = \phi(0) - 0 = p_0 \ge 0 (and p0<1p_0<1 by hypothesis, with the boundary case p0=0p_0=0 handled below). By the Intermediate Value Theorem applied to the continuous function gg on [0,1][0,1], since g(0)=p0≥0g(0) = p_0 \ge 0 and g(s)<0g(s)<0 for some s<1s<1 close to 11, there exists a point q∗∈[0,1)q^* \in [0,1) with g(q∗)=0g(q^*) = 0, i.e. ϕ(q∗)=q∗\phi(q^*) = q^*. (If p0=0p_0=0 exactly, note g(0)=0g(0)=0 already gives a fixed point at 00 itself, and the argument below shows it is not the smallest fixed point strictly less than 11 is still attained since we need the smallest root; we handle uniqueness next which resolves this cleanly regardless.) We now show this fixed point in [0,1)[0,1) is unique, using strict convexity. Since m>1m>1, ϕ\phi is not the identity, so (as argued above) ϕ\phi has at least one term pk>0p_k>0 for some k≥2k\ge2 or the mean could not exceed the p1p_1 coefficient alone in the required way — more directly: ϕ′′(s)=∑k≥2k(k−1)pksk−2\phi''(s) = \sum_{k\ge2}k(k-1)p_k s^{k-2}, and if ϕ′′≡0\phi''\equiv 0 on [0,1)[0,1) then ϕ\phi is affine, ϕ(s)=p0+p1s\phi(s)=p_0+p_1s with p0+p1=1p_0+p_1=1, giving m=p1=1−p0≤1m=p_1=1-p_0\le1, contradicting m>1m>1. So ϕ′′(s)>0\phi''(s)>0 for some, hence (since it's a power series with non-negative coefficients) for all ss in some interval (s1,1)(s_1,1), actually for all s∈(0,1)s \in (0,1) once any coefficient pk>0p_k>0 for k≥2k\ge 2 is active, making ϕ\phi strictly convex on (0,1)(0,1). A strictly convex function ϕ\phi on [0,1][0,1] with ϕ(1)=1\phi(1)=1 can cross the line y=sy=s at most twice on [0,1][0,1] (a strictly convex function minus a linear function, g(s)=ϕ(s)−sg(s)=\phi(s)-s, is itself strictly convex, and a strictly convex function has at most two zeros). We have exhibited one crossing at s=1s=1 and one crossing at q∗<1q^*<1; strict convexity of gg forbids a third, so q∗q^* is the unique fixed point in [0,1)[0,1). Finally we confirm q=q∗q = q^* using part 1 (smallest fixed point) together with monotonicity. Since qq is the smallest fixed point in [0,1][0,1] by part 1, and the only fixed points are q∗q^* and 11, with q∗<1q^*<1, we conclude q=q∗<1q=q^*<1. This proves parts 2 and 3. ■\blacksquare

∎

Worked examples

Example 1 — Asymmetric geometric offspring, supercritical. Let the offspring distribution be geometric-shifted: pk=(1−θ)θkp_k = (1-\theta)\theta^k for k=0,1,2,…k=0,1,2,\dots, with θ=0.6\theta = 0.6. So an individual has kk children with probability 0.4×0.6k0.4 \times 0.6^k: p0=0.4, p1=0.24, p2=0.144,…p_0=0.4,\ p_1=0.24,\ p_2=0.144,\dots The pgf is

ϕ(s)=∑k=0∞(1−θ)θksk=1−θ1−θs=0.41−0.6s.\phi(s) = \sum_{k=0}^\infty (1-\theta)\theta^k s^k = \frac{1-\theta}{1-\theta s} = \frac{0.4}{1-0.6s}.

The mean is

m=ϕ′(1)=(1−θ)θ(1−θ)2=θ1−θ=0.60.4=1.5>1,m = \phi'(1) = \frac{(1-\theta)\theta}{(1-\theta)^2}=\frac{\theta}{1-\theta} = \frac{0.6}{0.4} = 1.5 > 1,

so by the theorem this is a supercritical process: extinction is not certain, and qq is the unique root in [0,1)[0,1) of ϕ(s)=s\phi(s)=s. Solve 0.41−0.6s=s\dfrac{0.4}{1-0.6s} = s, i.e. 0.4=s(1−0.6s)=s−0.6s20.4 = s(1-0.6s) = s - 0.6s^2, i.e.

0.6s2−s+0.4=0⟺3s2−5s+2=0.0.6 s^2 - s + 0.4 = 0 \quad\Longleftrightarrow\quad 3s^2 - 5s + 2 = 0.

Factor: 3s2−5s+2=(3s−2)(s−1)3s^2-5s+2 = (3s-2)(s-1), giving roots s=2/3s = 2/3 and s=1s=1. The smallest root is q=2/3q = 2/3. So starting from a single ancestor, this population goes extinct with probability 2/3≈0.6672/3 \approx 0.667 and survives forever (population size →∞\to\infty) with probability 1/31/3, despite each individual expecting 1.51.5 children on average. This illustrates that m>1m>1 only makes survival possible, not certain — extinction can still be the more likely outcome.

Example 2 — Asymmetric finite support, subcritical, exact extinction probability at every generation. Let ξ\xi take values in {0,1,3}\{0,1,3\} with p0=0.5p_0 = 0.5, p1=0.3p_1=0.3, p3=0.2p_3=0.2 (so p2=0p_2=0; note the support need not be consecutive integers). The pgf is

ϕ(s)=0.5+0.3s+0.2s3.\phi(s) = 0.5 + 0.3s + 0.2s^3.

The mean is m=ϕ′(1)=0.3+0.6(1)2=0.3+0.6=0.9<1m = \phi'(1) = 0.3 + 0.6(1)^2 = 0.3+0.6 = 0.9 < 1. This is subcritical: by the theorem q=1q=1, extinction is certain regardless of any finer detail of the distribution. We can still extract quantitative information before extinction is reached. Compute Pr⁡(Z1=0)=ϕ(0)=0.5\Pr(Z_1=0)=\phi(0)=0.5. Compute Pr⁡(Z2=0)=ϕ(ϕ(0))=ϕ(0.5)=0.5+0.3(0.5)+0.2(0.5)3=0.5+0.15+0.025=0.675\Pr(Z_2=0) = \phi(\phi(0)) = \phi(0.5) = 0.5+0.3(0.5)+0.2(0.5)^3 = 0.5+0.15+0.025 = 0.675. Compute Pr⁡(Z3=0)=ϕ(0.675)=0.5+0.3(0.675)+0.2(0.675)3=0.5+0.2025+0.2(0.307547)=0.5+0.2025+0.061509=0.764009\Pr(Z_3=0)=\phi(0.675) = 0.5+0.3(0.675)+0.2(0.675)^3=0.5+0.2025+0.2(0.307547)=0.5+0.2025+0.061509=0.764009. These values 0.5,0.675,0.764…0.5, 0.675, 0.764\ldots increase monotonically toward q=1q=1, as guaranteed by part 1 of the theorem (qn↑qq_n\uparrow q), illustrating the cobweb picture concretely: each new value is ϕ\phi applied to the previous one, climbing the staircase toward the fixed point at s=1s=1. Also, E[Zn]=mn=0.9n→0\mathbb E[Z_n] = m^n = 0.9^n \to 0 exponentially, consistent with — but a strictly weaker fact than — almost-sure extinction; the mean going to zero does not by itself prove q=1q=1 in general unbounded settings, though here the full theorem gives the stronger conclusion directly.

Counterexampledropping the non-degeneracy hypothesis p0+p1<1p_0+p_1<1

The theorem assumes p0+p1<1p_0 + p_1 < 1, i.e. Pr⁡(ξ≥2)>0\Pr(\xi \ge 2) > 0, precisely to exclude the degenerate offspring law ξ≡1\xi \equiv 1 (that is, p1=1p_1=1, all other pk=0p_k=0). If instead p1=1p_1 = 1 exactly, then ϕ(s)=s\phi(s) = s identically for all s∈[0,1]s\in[0,1], so m=ϕ′(1)=1m = \phi'(1) = 1, and every s∈[0,1]s\in[0,1] is a fixed point of ϕ(s)=s\phi(s)=s. The theorem's conclusion "m≤1⇒q=1m\le1 \Rightarrow q=1" would be false here: since every individual has exactly one child forever, Zn≡1Z_n \equiv 1 for all nn, so the population never goes extinct, giving q=0q=0, not q=1q=1. Tracing through the proof shows exactly where it breaks: in the case m≤1m\le1, we needed g(s)=ϕ(s)−sg(s)=\phi(s)-s to be strictly negative-sloped-enough to force g>0g>0 strictly on [0,1)[0,1); but here g≡0g\equiv 0 everywhere, so qn=ϕ(n)(0)=0q_n = \phi^{(n)}(0) = 0 for all nn (since ϕ\phi is literally the identity map, qnq_n never moves from q0=0q_0=0), giving q=lim⁡qn=0q=\lim q_n = 0. The "smallest fixed point" is still correctly identified as q=0q=0 by part 1 of the theorem (which needs no non-degeneracy assumption), but part 2's claim that this smallest fixed point equals 11 specifically requires ruling out the totally-degenerate offspring law, which is exactly the hypothesis dropped. This shows the hypothesis is not a technicality: without it, the mean-based dichotomy statement literally fails.

Scope, edge cases & common traps

SituationWhat happensNote
p0=0p_0=0No individual ever has zero childrenZn≥Z0=1Z_n\ge Z_0=1 always if Z0≥1Z_0\ge1, so q=0q=0 automatically (theorem still consistent: ϕ(0)=p0=0\phi(0)=p_0=0 is itself the fixed point when m>1m>1 typically, or check directly)
m=1m=1 exactly (critical case), p1<1p_1<1Extinction still certain, q=1q=1But E[Zn]=1\mathbb E[Z_n]=1 for all nn — the mean does not go to zero, yet extinction is still a.s.; a classic place naive "mean →0\to0" intuition misleads
m=∞m=\infty (infinite mean offspring)Theorem's conclusion q<1q<1 still applies whenever m>1m>1 in the extended sense ϕ′(1−)=∞\phi'(1^-)=\inftyProof goes through since we only used ϕ′(1−)>1\phi'(1^-)>1, and ∞>1\infty>1 trivially
Multiple generations, non-i.i.d. environmentNot covered hereThis is the "branching process in varying/random environment," a genuine generalization
Z0=k>1Z_0 = k > 1 ancestors instead of 11Extinction probability becomes qkq^kBecause the kk initial lines evolve independently, each with individual extinction probability qq

The mathematician behind it

Origins · 1 minFrancis Galton and how this was discovered
FG
Francis Galton
1822–1911 · Victorian polymath, statistics and eugenics era Britain

Francis Galton, a cousin of Charles Darwin, was a prolific Victorian scientist working across meteorology, psychology, and statistics — a founder of regression analysis and correlation, and a controversial pioneer (and namer) of eugenics. In 1873 he posed the "problem of the extinction of families" in an educational journal, worried about the disappearance of aristocratic surnames, and the mathematician Henry William Watson supplied a generating-function solution the following year. Their joint 1875 paper is the origin of the process now bearing both their names, though it contained a subtle error about the extinction probability at m=1m=1 that was only fully corrected decades later.

History
- 1873: Galton poses the surname-extinction problem in the Educational Times.
- 1874: Watson responds with a generating-function approach; the joint Galton–Watson paper appears in 1875.
- 1930s–1940s: Erlang, Steinhaus, and others rediscover the process in demography and nuclear chain reactions (Fermi, Ulam) independently of the surname context.
- 1938–1947: Kolmogorov and Sevastyanov, and later Harris, place the theory on a fully rigorous modern footing, including the critical case m=1m=1.
- 1960s onward: the martingale reformulation (via Wn=Zn/mnW_n = Z_n/m^n) becomes the standard modern tool, connecting branching processes to martingale theory.
Why is the smallest fixed point of ϕ\phi the extinction probability, rather than any other fixed point?

Because the extinction probability is literally defined as a limit of an increasing sequence qn=ϕ(n)(0)q_n=\phi^{(n)}(0) starting at 00. The proof shows this sequence is monotone increasing (since extinction by generation nn implies extinction by generation n+1n+1) and bounded above by 11, so it converges to some fixed point of ϕ\phi. A separate monotonicity argument (using that ϕ\phi is non-decreasing) shows this limit cannot exceed any other fixed point s∗s^*, because qn≤s∗q_n\le s^* propagates inductively through the recursion qn+1=ϕ(qn)q_{n+1}=\phi(q_n). Hence the limit is the smallest fixed point available, not an arbitrary one. Larger fixed points (like s=1s=1, which is always a fixed point) correspond to non-extinction scenarios and are simply not reached by this particular increasing sequence starting from 00.

Does m>1m>1 guarantee the population grows to infinity if it doesn't go extinct?

Yes, in a precise sense, though proving it fully uses the martingale machinery beyond this article's scope. On the survival event (probability 1−q>01-q>0 when m>1m>1), one can show Zn→∞Z_n\to\infty almost surely: a Galton–Watson process either dies out or its size diverges, it cannot hover at a positive finite value forever, because the chain has no other absorbing or recurrent states besides 00 — every positive integer is transient. The martingale Wn=Zn/mnW_n=Z_n/m^n converges almost surely to a non-negative limit WW, and on the survival event W>0W>0 typically (Kesten–Stigum theorem, under a mild extra moment condition), giving the precise exponential growth rate Zn∼WmnZ_n\sim W m^n.

What happens exactly at the critical case m=1m=1?

Extinction is still certain (q=1q=1), by part 2 of the theorem, provided the offspring law is not degenerate at 11. However the rate of extinction is qualitatively different and much slower than in the subcritical case: instead of Pr⁡(Zn>0)\Pr(Z_n>0) decaying geometrically, a classical result (Kolmogorov) shows Pr⁡(Zn>0)∼2/(nσ2)\Pr(Z_n>0)\sim 2/(n\sigma^2) as n→∞n\to\infty, where σ2=Var(ξ)\sigma^2=\mathrm{Var}(\xi), i.e. only a polynomial 1/n1/n decay. This is the borderline, most delicate regime, and its analysis genuinely requires more refined tools (Tauberian theorems or direct recursive estimates on ϕ(n)\phi^{(n)}) beyond the basic fixed-point argument given here.

Can the offspring distribution have infinite mean, and does the theorem still apply?

Yes. If ∑kkpk=∞\sum_k k p_k = \infty, we interpret m=ϕ′(1−)=∞m=\phi'(1^-)=\infty using the monotone limit definition of mm used in the proof (which never assumed finiteness, only that ϕ′\phi' is non-decreasing with some limit in (0,∞](0,\infty] as s↑1s\uparrow1). Since ∞>1\infty>1 trivially, part 3 of the theorem applies verbatim: q<1q<1, and qq is still the unique fixed point of ϕ\phi in [0,1)[0,1). The convexity argument used to prove uniqueness never required mm to be finite, only that ϕ′(1−)>1\phi'(1^-)>1 strictly, so the whole proof survives unchanged.

How is this related to the Markov chain machinery I already know?

A Galton–Watson process is a special Markov chain on the countable state space {0,1,2,… }\{0,1,2,\dots\}, but with two features that make the ordinary finite-chain toolkit (eigenvalues of a finite transition matrix, stationary distributions) inapplicable: the state space is infinite, and the transition mechanism is a sum of i.i.d. offspring rather than an arbitrary stochastic matrix. This special branching structure is exactly what allows generating functions to substitute for the transition-matrix algebra: instead of matrix powers PnP^n, we use functional iterates ϕ(n)\phi^{(n)}, which are far easier to analyze because composition of one-dimensional functions is more tractable than matrix multiplication in infinite dimensions.

Why does the article foreshadow martingales — what's the connection?

The quantity Wn=Zn/mnW_n = Z_n/m^n satisfies E[Wn+1∣Z0,…,Zn]=Wn\mathbb E[W_{n+1}\mid Z_0,\dots,Z_n] = W_n exactly (a direct computation from the branching recursion and E[Zn+1∣Zn]=mZn\mathbb E[Z_{n+1}\mid Z_n]=mZ_n), which is precisely the defining property of a martingale. This reformulation is more powerful than the generating-function approach alone: martingale convergence theorems immediately give almost-sure convergence of WnW_n to a limiting random variable WW, refining the crude dichotomy "extinction vs. survival" into a precise a.s. growth rate Zn≈WmnZ_n \approx W m^n on the survival event. The generating-function extinction theorem proved here is the natural first result; the martingale viewpoint is the natural next chapter.

Before this

Where this leads