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Lectures on Stochastic Processes

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Lectures on Stochastic Processes Lectures on Stochastic Processes William G. Faris November 8, 2001 2 Contents 1 Random walk 7 1.1 Symmetric simple random walk . 7 1.2 Simple random walk . 9 1.3 Problems . 11 2 Gambler's ruin and martingales 13 2.1 Gambler's ruin: fair game . 13 2.2 Gambler's ruin: unfair game . 14 2.3 The dominated convergence theorem . 15 2.4 Martingales . 16 2.5 Problems . 18 3 The single server queue 19 3.1 A discrete time queue . 19 3.2 Emptying the queue . 19 3.3 The monotone convergence theorem . 21 3.4 The stationary distribution . 22 3.5 Problems . 24 4 The branching process 25 4.1 The branching model . 25 4.2 Explosion . 25 4.3 Extinction . 27 4.4 Problems . 28 5 Markov chains 29 5.1 The Markov property . 29 5.2 The strong Markov property . 30 5.3 Transient and recurrent states . 31 5.4 Recurrent classes . 32 5.5 Martingales . 33 5.6 The first passage time . 34 5.7 Problems . 34 3 4 CONTENTS 6 Markov chains: stationary distributions 35 6.1 Stationary distributions . 35 6.2 Detailed balance . 36 6.3 Positive recurrence and stationary distributions . 36 6.4 The average time in a state . 37 6.5 Examples . 38 6.6 Convergence to a stationary distribution . 38 6.7 Problems . 40 7 The Poisson process 41 7.1 The Bernoulli process . 41 7.2 The Poisson process . 42 7.3 The Poisson paradox . 43 7.4 Combining Poisson processes . 43 7.5 Problems . 44 8 Markov jump processes 45 8.1 Jump rates . 45 8.2 Hitting probabilities . 46 8.3 Stationary distributions . 46 8.4 The branching process . 47 8.5 The N server queue . 47 8.6 The Ehrenfest chain . 48 8.7 Transition probabilities . 49 8.8 The embedded Markov chain . 50 8.9 Problems . 50 9 The Wiener process 51 9.1 The symmetric random walk . 51 9.2 The Wiener process . 51 9.3 Continuity and differentiability . 52 9.4 Stochastic integrals . 52 9.5 Equilibrium statistical mechanics . 53 9.6 The Einstein model of Brownian motion . 54 9.7 Problems . 56 10 The Ornstein-Uhlenbeck process 57 10.1 The velocity process . 57 10.2 The Ornstein-Uhlenbeck position process . 59 10.3 Stationary Gaussian Markov processes . 59 10.4 Problems . 60 11 Diffusion and drift 61 11.1 Stochastic differential equation . 61 11.2 Diffusion equations . 61 11.3 Stationary distributions . 62 CONTENTS 5 11.4 Boundary conditions . 63 11.5 Martingales and hitting probabilities . 64 11.6 Problems . 65 12 Stationary processes 67 12.1 Mean and covariance . 67 12.2 Gaussian processes . 68 12.3 Mean and covariance of stationary processes . 68 12.4 Convolution . 69 12.5 Impulse response functions . 69 12.6 Problems . 71 13 Spectral analysis 73 13.1 Fourier transforms . 73 13.2 Convolution and Fourier transforms . 74 13.3 Smoothness and decay . 74 13.4 Some transforms . 76 13.5 Spectral densities . 77 13.6 Frequency response functions . 78 13.7 Causal response functions . 80 13.8 White noise . 82 13.9 1=f noise . 83 13.10Problems . 84 6 CONTENTS Chapter 1 Random walk 1.1 Symmetric simple random walk Let X0 = x and Xn+1 = Xn + ξn+1: (1.1) The ξi are independent, identically distributed random variables such that P [ξi = ±1] = 1=2. The probabilities for this random walk also depend on x, and we shall denote them by Px. We can think of this as a fair gambling game, where at each stage one either wins or loses a fixed amount. Let Ty be the first time n ≥ 1 when Xn = y. Let ρxy = Px[Ty < 1] be the probability that the walk starting at x ever gets to y at some future time. First we show that ρ12 = 1. This says that in the fair game one is almost sure to eventually get ahead by one unit. This follows from the following three equations. The first equation says that in the first step the walk either goes from 1 to 2 directly, or it goes from 1 to 0 and then must go from 0 to 2. Thus 1 1 ρ = + ρ : (1.2) 12 2 2 02 The second equation says that to go from 0 to 2, the walk has to go from 0 to 1 and then from 1 to 2. Furthermore, these two events are independent. Thus ρ02 = ρ01ρ12: (1.3) The third equation says that ρ01 = ρ12. This is obvious. Thus ρ = ρ12 satisfies 1 1 ρ = ρ2 + : (1.4) 2 2 This is a quadratic equation that can also be written as ρ2 − 2ρ + 1 = 0, or (ρ − 1)2 = 0. Its only solution is ρ = 1. How long does it take, on the average, to get ahead by this amount? Let mxy = Ex[Ty], the expected time that the random walk takes to get to y, 7 8 CHAPTER 1. RANDOM WALK starting at x. We have just seen that if x = 1, then T2 < 1 with probability one. Let us do the same kind of computation for m12 = E1[T2]. The first equation says that in the first step the walk either goes from 1 to 2 directly, or it goes from 1 to 0 and then must go from 0 to 2. Thus 1 1 m = (1 + m ) + 1: (1.5) 12 2 02 2 The second equation says that to go from 0 to 2, the walk has to go from 0 to 1 and then from 1 to 2. Thus m02 = m01 + m12: (1.6) The third equation says that m01 = m12. This is obvious. Thus m = m12 satisfies 1 1 m = (1 + 2m) + : (1.7) 2 2 This is a linear equation that can also be written as m = 1+m. Its only solution is m = 1. Thus we have seen that m01 = 1. At first this seems strange, but it is quite natural. In the fair game there is a small probability of a bad losing streak. It takes a long time to recover from the losing streak and eventually get ahead. Infinitely long, on the average. The calculation above uses a rather subtle property of random walk. Namely, it was assumed that after the walk accomplishes the task of going from 0 to 1, then it has an equally difficult task of going from 1 to 2. Now this is delicate, because the walk going from 1 to 2 starts out at a random time, not at a fixed time. Namely, if we start the walk at 0 and set T = T1 as the first time the walk gets to 1, then from that time on the walk is XT ;XT +1;XT +2;::: with XT = 1 by definition. The point is that this has the same distribution as the walk X0;X1;X2;::: with X0 = 1. This fact is called the strong Markov property. The strong Markov property has the following statement. Start the walk out at x and let T = Ty. Let B be a set of random walk paths. We must prove that Px[(XT ;XT +1;XT +2;:::) 2 B j T < 1] = Py[(X0;X1;X2;:::) 2 B]: (1.8) This says that the walk does not care when and how it got to y for the first time; from that point on it moves just as if it were started there at time zero. The proof is the following. We write X1 Px[(XT ;XT +1;XT +2;:::) 2 B; T < 1] = Px[(XT ;XT +1;XT +2;:::) 2 B; T = n]: n=1 (1.9) However Px[(XT ;XT +1;XT +2;:::) 2 B; T = n] = Px[(Xn;Xn+1;Xn+2 :::) 2 B; T = n]: (1.10) 1.2. SIMPLE RANDOM WALK 9 Now the event T = n depends only on the walk X1;X2;:::;Xn, which depends only on the ξ1; ξ2; : : : ; ξn. On the other hand, the walk Xn;Xn+1;Xn+2;::: with Xn = y depends only on the ξn+1; ξn+1;:::. Thus the events are independent, and we have Px[(XT ;XT +1;XT +2;:::) 2 B; T = n] = Px[(Xn;Xn+1;Xn+2 :::) 2 B]P [T = n]; (1.11) where Xn = y. Finally, this is Px[(XT ;XT +1;XT +2;:::) 2 B; T = n] = Py[(X0;X1;X2 :::) 2 B]P [T = n]: (1.12) The proof is finished by summing over n. The picture of symmetric simple random walk that emerges is the following. Starting from any point, the probability of eventually getting to any other point is one. However the expected time to accomplish this is infinite. Thus an imbalance in one direction is always compensated, but this random process is incredibly inefficient and can take a huge amount of time to do it. 1.2 Simple random walk Let X0 = x and Xn+1 = Xn + ξn+1: (1.13) The ξi are independent, identically distributed random variables such that P [ξi = 1] = p, P [ξi = −1] = q, and P [ξ = 0] = r. Here p + q + r = 1, so the walk can change position by only one step at a time. The probabilities for this random walk depend on x, and we shall denote them by Px. We can think of this as a gambling game, where at each stage one either wins or loses a fixed amount. Let Ty be the first time n ≥ 1 when Xn = y. Let ρxy = Px[Ty < 1] be the probability that the walk starting at x ever gets to y at some future time.
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