Here is a hint.
Consider carefully the term $\mathbb P( X \leq z Y \mid z Y < 1 )$. In particular, for concreteness, choose $z = 2$, so that we are considering the event $\mathbb P( X \leq 2 Y \mid Y < 1/2 )$.
Now, look at this picture (which is very closely related to the above probability).
Now, does that conditional probability depend on our particular choice of $z$?
We wish to show that $\hat \theta_n \xrightarrow{P} \theta_0$. By definition,
this states that given $\epsilon > 0$
$$
P(|\hat \theta_n - \theta_0| > \epsilon) \rightarrow 0 \text{ as } n \rightarrow \infty.
$$
Given $X_1,..., X_n$ are iid with finite $n$, we see that if we were to
reorder $\{X_i\}$ in ascending order, the definition of
$\hat \theta_n$ gives
$\hat \theta_n = X_{\lceil n/2 \rceil}$.
From this we have that
$$
\hat F_n(\hat \theta_n) = \left \{
\begin{array}{ll}
1/2 & \text{ if n is even} \\
\frac{1}{2} + \frac{1}{2n} & \text{ if n is odd.}
\end{array}
\right.
$$
Using this, we can calculate
\begin{align}
P(|\hat \theta_n - \theta_0| > \epsilon)
&\leq P(|\hat \theta_n - \theta_0| \geq \epsilon) \\
&= P(\hat \theta_n \leq \theta_0 - \epsilon) + P(\theta_n +
\epsilon \leq \hat \theta_n) \\
&= P(\hat F_n(\hat \theta_n) \leq \hat F_n(\theta_0 - \epsilon)) +
P(\hat F_n(\theta_n + \epsilon) \leq \hat F_n(\hat \theta_n))
\end{align}
where the last equality is due to the fact that $\hat F_n(x)$ is non-decreasing.
Notice that because $\hat F_n(x)$ is non-decreasing and not strictly
increasing, it can only preserve weak inequalities.
We continue by analyzing the terms individually. First, consider the term
$$
P(\hat F_n(\hat \theta_n) \leq \hat F_n(\theta_0 - \epsilon)).
$$
When $n$ is even,
\begin{align*}
P(1/2 \leq \hat F_n(\theta_0 - \epsilon))
&= P(1/2 - F(\theta_0 - \epsilon)) \leq \hat F_n(\theta_0 - \epsilon) -
F(\theta_0 - \epsilon))\\
&\rightarrow 0 \text{ as } n \rightarrow \infty
\end{align*}
where this last fact follows from the fact that
$1/2 - F(\theta_0 - \epsilon) > 0 $ (we can see this from the defintion of the median) and that
$\hat F_n(x) \xrightarrow{p} F(x)$, as we demonstrated previously.
Similarly, when $n$ is odd,
\begin{align*}
P(1/2 + \frac{1}{2n} \leq \hat F_n(\theta_0 - \epsilon))
&= P(1/2 + \frac{1}{2n} - F(\theta_0 - \epsilon)) \leq \hat F_n(\theta_0 - \epsilon) -
F(\theta_0 - \epsilon))\\
&\rightarrow 0 \text{ as } n \rightarrow \infty.
\end{align*}
Now consider the term
$$
P(\hat F_n(\theta_n + \epsilon) \leq \hat F_n(\hat \theta_n)).
$$
Similar to before, we have
\begin{align*}
P(\hat F_n(\theta_n + \epsilon) \leq \hat F_n(\hat \theta_n))
&= P(-\hat F_n(\theta_n + \epsilon) \geq -\hat F_n(\hat \theta_n)) \\
&= P(F(\theta_n + \epsilon) -\hat F_n(\theta_n + \epsilon) \geq
F(\theta_n + \epsilon) -\hat F_n(\hat \theta_n)) \\
&\rightarrow 0 \text{ as } n \rightarrow \infty.
\end{align*}
This last fact comes again from the fact that that $\hat F_n(x) \xrightarrow{p} F(x)$ and that $F(\theta_n + \epsilon) -\hat F_n(\hat \theta_n) > 0$, which we have because the uniqueness of the median gives that for $\epsilon > 0$ we have $F(\theta_0 + \epsilon) > .5$.
These two results, applied back give
\begin{align*}
P(|\hat \theta_n - \theta_0| > \epsilon)
&\leq P(|\hat \theta_n - \theta_0| \geq \epsilon) \nonumber \\
&\rightarrow 0 \text{ as } n \rightarrow \infty
\end{align*}
and thus
$$
\hat \theta_n \xrightarrow{p} \theta_0.
$$
Best Answer
Let $X \sim \mathsf{Bern}(p=.2)\equiv\mathsf{Binom}(n=1, p=.2).$ In R, where
qbinom
is the inverse CDF (quantile function) of a binomial distribution a median $\eta = 0.$$P(X \le 0) = P(X = 0) = 0.8 \ge 1/2.$
And obviously, $P(X \ge 0) = 1 \ge 1/2.$
The CDF of $X$ is plotted below. The median of $X$ is taken to be the value at which the CDF 'curve' is (or 'crosses') $1/2.$
Also, for context, if we simulate $1000$ observations from this distribution, we get $805$ Failures (0) and $195$ Successes. According to R, the sample median is also $0.$